Planet R

October 14, 2019


New package lss2 with initial version 1.1

Package: lss2
Type: Package
Title: The Accelerated Failure Time Model to Right Censored Data Based on Least-Squares Principle
Version: 1.1
Author: Zhezhen Jin <>, Arvin Satwani <>
Maintainer: Arvin Satwani <>
Description: Due to lack of proper inference procedure and software, the ordinary linear regression model is seldom used in practice for the analysis of right censored data. This paper presents an S-Plus/R program that implements a recently developed inference procedure (Jin, Lin and Ying, 2006) <doi:10.1093/biomet/93.1.147> for the accelerated failure time model based on the least-squares principle.
Depends: R(>= 2.1.0), quantreg
Suggests: survival
License: GPL (>= 2)
Encoding: UTF-8
LazyData: true
RoxygenNote: 6.1.1
NeedsCompilation: no
Packaged: 2019-10-12 16:19:22 UTC; arvinsatwani
Repository: CRAN
Date/Publication: 2019-10-14 14:30:02 UTC

More information about lss2 at CRAN

October 14, 2019 03:02 PM

New package SDEFSR with initial version 0.7.2

Package: SDEFSR
Type: Package
Title: Subgroup Discovery with Evolutionary Fuzzy Systems
Version: 0.7.2
Date: 2019-10-14
Authors@R: c(person("Angel M.", "Garcia", email = "", role = c("aut", "cre")), person("Pedro", "Gonzalez", email = "", role = c("aut", "cph")), person("Cristobal J.", "Carmona", email = "", role = c("aut", "cph")), person("Francisco", "Charte", email = "", role = "ctb"), person("Maria J.", "del Jesus", email = "", role = c("aut", "cph")) )
Maintainer: Angel M. Garcia <>
Description: Implementation of evolutionary fuzzy systems for the data mining task called "subgroup discovery". In particular, the algorithms presented in this package are: M. J. del Jesus, P. Gonzalez, F. Herrera, M. Mesonero (2007) <doi:10.1109/TFUZZ.2006.890662> M. J. del Jesus, P. Gonzalez, F. Herrera (2007) <doi:10.1109/MCDM.2007.369416> C. J. Carmona, P. Gonzalez, M. J. del Jesus, F. Herrera (2010) <doi:10.1109/TFUZZ.2010.2060200> C. J. Carmona, V. Ruiz-Rodado, M. J. del Jesus, A. Weber, M. Grootveld, P. González, D. Elizondo (2015) <doi:10.1016/j.ins.2014.11.030> It also provide a Shiny App to ease the analysis. The algorithms work with data sets provided in KEEL, ARFF and CSV format and also with data.frame objects.
Depends: R (>= 3.0.0)
License: LGPL (>= 3)
LazyData: TRUE
Imports: grDevices, methods, parallel, stats, utils
Suggests: ggplot2, knitr, shiny (>= 0.11)
VignetteBuilder: knitr
RoxygenNote: 6.1.1
NeedsCompilation: no
Author: Angel M. Garcia [aut, cre], Pedro Gonzalez [aut, cph], Cristobal J. Carmona [aut, cph], Francisco Charte [ctb], Maria J. del Jesus [aut, cph]
Packaged: 2019-10-14 09:36:06 UTC; agvico
Encoding: UTF-8
Repository: CRAN
Date/Publication: 2019-10-14 10:10:05 UTC

More information about SDEFSR at CRAN

October 14, 2019 11:02 AM

Package fdaPDE (with last version 0.1-5) was removed from CRAN

Previous versions (as known to CRANberries) which should be available via the Archive link are:

2019-10-13 0.1-5

October 14, 2019 09:02 AM

October 13, 2019


New package fdaPDE with initial version 0.1-5

Package: fdaPDE
Version: 0.1-5
Date: 2019-10-12
Title: Functional Data Analysis and Partial Differential Equations; Statistical Analysis of Functional and Spatial Data, Based on Regression with Partial Differential Regularizations
Authors@R: c(person("Eardi", "Lila", role = c("aut", "cre"), email = ""), person("Laura M.", "Sangalli", role = "aut", email = ""), person("Jim", "Ramsay", role = "aut", email = ""), person("Luca", "Formaggia", role = "aut", email = ""))
Author: Eardi Lila [aut, cre], Laura M. Sangalli [aut], Jim Ramsay [aut], Luca Formaggia [aut]
Maintainer: Eardi Lila <>
Depends: R (>= 3.0.0), stats, grDevices, graphics, rgl
LinkingTo: RcppEigen
Suggests: MASS
Description: An implementation of regression models with partial differential regularizations, making use of the Finite Element Method. The models efficiently handle data distributed over irregularly shaped domains and can comply with various conditions at the boundaries of the domain. A priori information about the spatial structure of the phenomenon under study can be incorporated in the model via the differential regularization.
License: CC BY-NC-SA 4.0
Copyright: See the individual source files for copyrights information
NeedsCompilation: yes
SystemRequirements: C++11
RoxygenNote: 6.1.1
Packaged: 2019-10-13 14:21:44 UTC; eardi
Repository: CRAN
Date/Publication: 2019-10-13 14:50:02 UTC

More information about fdaPDE at CRAN

October 13, 2019 03:02 PM

October 12, 2019

Dirk Eddelbuettel

GitHub Streak: Round Six

Five ago I referenced the Seinfeld Streak used in an earlier post of regular updates to to the Rcpp Gallery:

This is sometimes called Jerry Seinfeld’s secret to productivity: Just keep at it. Don’t break the streak.

and then showed the first chart of GitHub streaking

github activity october 2013 to october 2014github activity october 2013 to october 2014

And four year ago a first follow-up appeared in this post:

github activity october 2014 to october 2015github activity october 2014 to october 2015

And three years ago we had a followup

github activity october 2015 to october 2016github activity october 2015 to october 2016

And two years ago we had another one

github activity october 2016 to october 2017github activity october 2016 to october 2017

And last year another one

github activity october 2017 to october 2018github activity october 2017 to october 2018

As today is October 12, here is the newest one from 2018 to 2019:

github activity october 2018 to october 2019github activity october 2018 to october 2019

Again, special thanks go to Alessandro Pezzè for the Chrome add-on GithubOriginalStreak.

This post by Dirk Eddelbuettel originated on his Thinking inside the box blog. Please report excessive re-aggregation in third-party for-profit settings.

October 12, 2019 03:53 PM

October 10, 2019

Journal of the Royal Statistical Society: Series C

Dirk Eddelbuettel

RcppArmadillo 0.9.800.1.0

armadillo image

Another month, another Armadillo upstream release! Hence a new RcppArmadillo release arrived on CRAN earlier today, and was just shipped to Debian as well. It brings a faster solve() method and other goodies. We also switched to the (awesome) tinytest unit test frameowrk, and Min Kim made the script more portable for the benefit of NetBSD and other non-bash users; see below for more details. One again we ran two full sets of reverse-depends checks, no issues were found, and the packages was auto-admitted similarly at CRAN after less than two hours despite there being 665 reverse depends. Impressive stuff, so a big Thank You! as always to the CRAN team.

Armadillo is a powerful and expressive C++ template library for linear algebra aiming towards a good balance between speed and ease of use with a syntax deliberately close to a Matlab. RcppArmadillo integrates this library with the R environment and language–and is widely used by (currently) 665 other packages on CRAN.

Changes in RcppArmadillo version 0.9.800.1.0 (2019-10-09)

  • Upgraded to Armadillo release 9.800 (Horizon Scraper)

    • faster solve() in default operation; iterative refinement is no longer applied by default; use solve_opts::refine to explicitly enable refinement

    • faster expmat()

    • faster handling of triangular matrices by rcond()

    • added .front() and .back()

    • added .is_trimatu() and .is_trimatl()

    • added .is_diagmat()

  • The package now uses tinytest for unit tests (Dirk in #269).

  • The script is now more careful about shell portability (Min Kim in #270).

Courtesy of CRANberries, there is a diffstat report relative to previous release. More detailed information is on the RcppArmadillo page. Questions, comments etc should go to the rcpp-devel mailing list off the R-Forge page.

This post by Dirk Eddelbuettel originated on his Thinking inside the box blog. Please report excessive re-aggregation in third-party for-profit settings.

October 10, 2019 12:59 AM

September 24, 2019

Dirk Eddelbuettel

RcppAnnoy 0.0.13

annoy image

A new release of RcppAnnoy is now on CRAN.

RcppAnnoy is the Rcpp-based R integration of the nifty Annoy library by Erik Bernhardsson. Annoy is a small and lightweight C++ template header library for very fast approximate nearest neighbours—originally developed to drive the famous Spotify music discovery algorithm.

This release brings several updates. First and foremost, the upstream Annoy C++ code was updated from version 1.12 to 1.16 bringing both speedier code thanks to AVX512 instruction (where available) and new functionality. Which we expose in two new functions of which buildOnDisk() may be of interest for some using the file-back indices. We also corrected a minor wart in which a demo file was saved (via example()) to a user directory; we now use tempfile() as one should, and contributed two small Windows build changes back to Annoy.

Detailed changes follow below.

Changes in version 0.0.13 (2019-09-23)

  • In example(), the saved and loaded filename is now obtained via tempfile() to not touch user directories per CRAN Policy (Dirk).

  • RcppAnnoy was again synchronized with Annoy upstream leading to enhanced performance and more features (Dirk #48).

  • Minor changes made (and send as PRs upstream) to adapt both annoylib.h and mman.h changes (Dirk).

  • A spurious command was removed from one vignette (Peter Hickey in #49).

  • Two new user-facing functions onDiskBuild() and unbuild() were added (Dirk in #50).

  • Minor tweaks were made to two tinytest-using test files (Dirk).

Courtesy of CRANberries, there is also a diffstat report for this release.

This post by Dirk Eddelbuettel originated on his Thinking inside the box blog. Please report excessive re-aggregation in third-party for-profit settings.

September 24, 2019 12:48 AM

September 20, 2019

Dirk Eddelbuettel

digest 0.6.21

A new version of digest is just now arriving at CRAN (following a slight holdup over one likely spurious reverse dependency error), and I will send an updated package to Debian shortly as well.

digest creates hash digests of arbitrary R objects (using the md5, sha-1, sha-256, sha-512, crc32, xxhash32, xxhash64, murmur32, and spookyhash algorithms) permitting easy comparison of R language objects. It is a fairly widely-used package (currently listed at 795k downloads) as many tasks may involve caching of objects for which it provides convenient general-purpose hash key generation.

Every now and then open source work really surprises you. Out of nowhere arrived a very fine pull request by Matthew de Queljoe which adds a very clever function getVDigest() supplying a (much faster) vectorized wrapper for digest creation. We illustrate this in a quick demo vectorized.R that is included too. So if you call digest() in bulk, this will most likely be rather helpful to you. Matthew even did further cleanups and refactorings but we are saving that for a subsequent pull request or two.

CRANberries provides the usual summary of changes to the previous version.

For questions or comments use the issue tracker off the GitHub repo.

This post by Dirk Eddelbuettel originated on his Thinking inside the box blog. Please report excessive re-aggregation in third-party for-profit settings.

September 20, 2019 11:38 PM

August 24, 2019

Journal of Statistical Software

August 22, 2019

Journal of Statistical Software

DClusterm: Model-Based Detection of Disease Clusters

The detection of regions with unusually high risk plays an important role in disease mapping and the analysis of public health data. In particular, the detection of groups of areas (i.e., clusters) where the risk is significantly high is often conducted by public health authorities. Many methods have been proposed for the detection of these disease clusters, most of them based on moving windows, such as Kulldorff's spatial scan statistic. Here we describe a model-based approach for the detection of disease clusters implemented in the DClusterm package. Our model-based approach is based on representing a large number of possible clusters by dummy variables and then fitting many generalized linear models to the data where these covariates are included one at a time. Cluster detection is done by performing a variable or model selection among all fitted models using different criteria. Because of our model-based approach, cluster detection can be performed using different types of likelihoods and latent effects. We cover the detection of spatial and spatiotemporal clusters, as well as how to account for covariates, zero-inflated datasets and overdispersion in the data.

by Virgilio Gómez-Rubio, Paula Moraga, John Molitor, Barry Rowlingson at August 22, 2019 12:00 AM

August 21, 2019

Journal of Statistical Software

Flexible Regression Models for Count Data Based on Renewal Processes: The Countr Package

A new alternative to the standard Poisson regression model for count data is suggested. This new family of models is based on discrete distributions derived from renewal processes, i.e., distributions of the number of events by some time t. Unlike the Poisson model, these models have, in general, time-dependent hazard functions. Any survival distribution can be used to describe the inter-arrival times between events, which gives a rich class of count processes with great flexibility for modelling both underdispersed and overdispersed data. The R package Countr provides a function, renewalCount(), for fitting renewal count regression models and methods for working with the fitted models. The interface is designed to mimic the glm() interface and standard methods for model exploration, diagnosis and prediction are implemented. Package Countr implements stateof-the-art recently developed methods for fast computation of the count probabilities. The package functionalities are illustrated using several datasets.

by Tarak Kharrat, Georgi N. Boshnakov, Ian McHale, Rose Baker at August 21, 2019 12:00 AM

August 14, 2019

Journal of the Royal Statistical Society: Series B

June 28, 2019

Bioconductor Project Working Papers

Generalized interventional approach for causal mediation analysis with causally ordered multiple mediators

Causal mediation analysis has demonstrated the advantage of mechanism investigation. In conditions with causally ordered mediators, path-specific effects (PSEs) are introduced for specifying the effect subject to a certain combination of mediators. However, most PSEs are unidentifiable. To address this, an alternative approach termed interventional analogue of PSE (iPSE), is widely applied to effect decomposition. Previous studies that have considered multiple mediators have mainly focused on two-mediator cases due to the complexity of the mediation formula. This study proposes a generalized interventional approach for the settings, with the arbitrary number of ordered multiple mediators to study the causal parameter identification as well as statistical estimation. It provides a general definition of iPSEs with a recursive formula, assumptions for nonparametric identification, a regression-based method, and a g-computation algorithm to estimate all iPSEs. We demonstrate that each iPSE reduces to the result of linear structural equation modeling subject to linear or log-linear models. This approach is applied to a Taiwanese cohort study for exploring the mechanism by which hepatitis C virus infection affects mortality through hepatitis B virus infection, liver function, and hepatocellular carcinoma. Software based on a g-computation algorithm allows users to easily apply this method for data analysis subject to various model choices according to the substantive knowledge for each variable. All methods and software proposed in this study contribute to comprehensively decompose a causal effect confirmed by data science and help disentangling causal mechanisms when the natural pathways are complicated.

by Sheng-Hsuan Lin at June 28, 2019 02:15 PM

June 13, 2019

Bioconductor Project Working Papers

Unified Methods for Feature Selection in Large-Scale Genomic Studies with Censored Survival Outcomes

One of the major goals in large-scale genomic studies is to identify genes with a prognostic impact on time-to-event outcomes which provide insight into the disease's process. With rapid developments in high-throughput genomic technologies in the past two decades, the scientific community is able to monitor the expression levels of tens of thousands of genes and proteins resulting in enormous data sets where the number of genomic features is far greater than the number of subjects. Methods based on univariate Cox regression are often used to select genomic features related to survival outcome; however, the Cox model assumes proportional hazards (PH), which is unlikely to hold for each feature. When applied to genomic features exhibiting some form of non-proportional hazards (NPH), these methods could lead to an under- or over-estimation of the effects. We propose a broad array of marginal screening techniques that aid in feature ranking and selection by accommodating various forms of NPH. First, we develop an approach based on Kullback-Leibler information divergence and the Yang-Prentice model that includes methods for the PH and proportional odds (PO) models as special cases. Next, we propose R2 indices for the PH and PO models that can be interpreted in terms of explained variation. Lastly, we propose a generalized pseudo-R2 measure that includes PH, PO, crossing hazards and crossing odds models as special cases and can be interpreted as the percentage of separability between subjects experiencing the event and not experiencing the event according to feature expression. We evaluate the performance of our measures using extensive simulation studies and publicly available data sets in cancer genomics. We demonstrate that the proposed methods successfully address the issue of NPH in genomic feature selection and outperform existing methods. The proposed information divergence, R2 and pseudo-R2 measures were implemented in R ( and code is available upon request.

by Lauren Spirko-Burns et al. at June 13, 2019 05:01 PM

May 26, 2019

Journal of the Royal Statistical Society: Series A

April 05, 2019

Bioconductor Project Working Papers

Supervised Dimension Reduction for Large-scale "Omics" Data with Censored Survival Outcomes Under Possible Non-proportional Hazards

The past two decades have witnessed significant advances in high-throughput ``omics" technologies such as genomics, proteomics, metabolomics, transcriptomics and radiomics. These technologies have enabled simultaneous measurement of the expression levels of tens of thousands of features from individual patient samples and have generated enormous amounts of data that require analysis and interpretation. One specific area of interest has been in studying the relationship between these features and patient outcomes, such as overall and recurrence-free survival, with the goal of developing a predictive ``omics" profile. Large-scale studies often suffer from the presence of a large fraction of censored observations and potential time-varying effects of features, and methods for handling them have been lacking. In this paper, we propose supervised methods for feature selection and survival prediction that simultaneously deal with both issues. Our approach utilizes continuum power regression (CPR) - a framework that includes a variety of regression methods - in conjunction with the parametric or semi-parametric accelerated failure time (AFT) model. Both CPR and AFT fall within the linear models framework and, unlike black-box models, the proposed prognostic index has a simple yet useful interpretation. We demonstrate the utility of our methods using simulated and publicly available cancer genomics data.

by Lauren Spirko-Burns et al. at April 05, 2019 07:06 AM

April 01, 2019

Bioconductor Project Working Papers

Power Calculation for Cross-Sectional Stepped Wedge Cluster-Randomized Trials with Variable Cluster Sizes

Standard sample size calculation formulas for Stepped Wedge Cluster Randomized Trials (SW-CRTs) assume that cluster sizes are equal. When cluster sizes vary substantially, ignoring this variation may lead to an under-powered study. We investigate the relative efficiency of a SW-CRT with varying cluster sizes to equal cluster sizes, and derive variance estimators for the intervention effect that account for this variation under the assumption of a mixed effects model; a commonly-used approach for analyzing data from cluster randomized trials. When cluster sizes vary, the power of a SW-CRT depends on the order in which clusters receive the intervention, which is determined through randomization. We first derive a variance formula that corresponds to any particular realization of the randomized sequence and propose efficient algorithms to identify upper and lower bounds of the power. We then obtain an ``expected'' power based on a first-order approximation to the variance formula, where the expectation is taken with respect to all possible randomization sequences. Finally, we provide a variance formula for more general settings where only the mean and coefficient of variation of cluster sizes, instead of exact cluster sizes, are known in the design stage. We evaluate our methods through simulations and illustrate that the power of a SW-CRT decreases as the variation in cluster sizes increases, and the impact is largest when the number of clusters is small.

by Linda J. Harrison et al. at April 01, 2019 01:40 PM

May 05, 2018

R you ready?

Remove password protection from Excel sheets using R

Most data scientists wished that all data lived neatly managed in some DB. However, in reality, Excel files are ubiquitous and often a common way to disseminate results or data within many companies. Every now and then I found myself in the situation where I wanted to protect Excel sheets against users accidentally changing them. A few months later, however, I found that I sometimes had forgotten the password I used. The “good” thing is that protecting Excel sheets by password is far from safe and access can be recovered quite easily. The following works for .xlsx files only (tested with Excel 2016 files), not the older .xls files.

Before implementing the steps in R, I will outline how to remove the password protection “by hand”. The R way is simply the automation of these steps. The first thing one needs to understand is that a .xlsx file is just a collection of folders and files in a zip container. If you unzip a .xlsx file (e.g. using 7-Zip) you get the following folder structure (sorry, German UI):

In the folder ./xl/worksheets we find one XML file for each Excel sheet. The sheet’s password protection is encoded directly in the sheet. While there used to be the plain password text in the XML in former versions, now, we find the hashed password (see part marked in yellow below). In order to get rid of the password protection, we simply can remove the whole sheetProtection node from the XML. We can do that in any text editor and save the file.

As the last step, we need to recreate the .xlsx file by creating a zip folder that contains our modified XML file (German UI again).

Finally, we change the file extension from .zip back to .xlsx and voilá, we get an Excel file without password protected sheets. Programming the steps outlined above in R is quite straightforward. The steps are commented in the GitHub gist below.

by markheckmann at May 05, 2018 11:07 PM

April 18, 2018

RCpp Gallery

Performance considerations with sparse matrices in Armadillo


Besides outstanding support for dense matrices, the Armadillo library also provides a great way to manipulate sparse matrices in C++. However, the performance characteristics of dealing with sparse matrices may be surprising if one is only familiar with dense matrices. This is a collection of observations on getting best performance with sparse matrices in Armadillo.

All the timings in this article were generated using Armadillo version 8.500. This version adds a number of substantial optimisations for sparse matrix operations, in some cases speeding things up by as much as two orders of magnitude.

General considerations: sparsity, row vs column access

Perhaps the most important thing to note is that the efficiency of sparse algorithms can depend strongly on the level of sparsity in the data. If your matrices and vectors are very sparse (most elements equal to zero), you will often see better performance even if the nominal sizes of those matrices remain the same. This isn’t specific to C++ or Armadillo; it applies to sparse algorithms in general, including the code used in the Matrix package for R. By contrast, algorithms for working with dense matrices usually aren’t affected by sparsity.

Similarly, the pattern of accesssing elements, whether by rows or by columns, can have a significant impact on performance. This is due to caching, which modern CPUs use to speed up memory access: accessing elements that are already in the cache is much faster than retrieving them from main memory. If one iterates or loops over the elements of a matrix in Armadillo, one should try to iterate over columns first, then rows, to maximise the benefits of caching. This applies to both dense and sparse matrices. (Technically, at least for dense matrices, whether to iterate over rows or columns first depends on how the data is stored in memory. Both R and Armadillo store matrices in column-major order, meaning that elements in the same column are contiguous in memory. Sparse matrices are more complex but the advice to iterate by columns is basically the same; see below.)

Matrix multiplication

We start with a simple concrete example: multiplying two matrices together. In R, this can be done using the %*% operator which (via the Matrix package) is able to handle any combination of sparse and dense inputs. However, let us assume we want to do the multiplication in Armadillo: for example if the inputs are from other C++ functions, or if we want more precise control of the output.

In Armadillo, the * operator multiplies two matrices together, and this also works for any combination of sparse and dense inputs. However, the speed of the operation can vary tremendously, depending on which of those inputs is sparse. To see this, let us define a few simple functions:

// [[Rcpp::depends(RcppArmadillo)]]
#include <RcppArmadillo.h>

// [[Rcpp::export]]
arma::sp_mat mult_sp_sp_to_sp(const arma::sp_mat& a, const arma::sp_mat& b) {
    // sparse x sparse -> sparse
    arma::sp_mat result(a * b);
    return result;

// [[Rcpp::export]]
arma::sp_mat mult_sp_den_to_sp(const arma::sp_mat& a, const arma::mat& b) {
    // sparse x dense -> sparse
    arma::sp_mat result(a * b);
    return result;

// [[Rcpp::export]]
arma::sp_mat mult_den_sp_to_sp(const arma::mat& a, const arma::sp_mat& b) {
    // dense x sparse -> sparse
    arma::sp_mat result(a * b);
    return result;

The outputs of these functions are all the same, but they take different types of inputs: either two sparse matrices, or a sparse and a dense matrix, or a dense and a sparse matrix (the order matters). Let us call them on some randomly generated data:

n <- 5e3
# 5000 x 5000 matrices, 99% sparse
a <- rsparsematrix(n, n, 0.01, rand.x=function(n) rpois(n, 1) + 1)
b <- rsparsematrix(n, n, 0.01, rand.x=function(n) rpois(n, 1) + 1)

a_den <- as.matrix(a)
b_den <- as.matrix(b)

system.time(m0 <- a %*% b)
   user  system elapsed 
  0.230   0.091   0.322 
system.time(m1 <- mult_sp_sp_to_sp(a, b))
   user  system elapsed 
  0.407   0.036   0.442 
system.time(m2 <- mult_sp_den_to_sp(a, b_den))
   user  system elapsed 
  1.081   0.100   1.181 
system.time(m3 <- mult_den_sp_to_sp(a_den, b))
   user  system elapsed 
  0.826   0.087   0.913 
all(identical(m0, m1), identical(m0, m2), identical(m0, m3))
[1] TRUE

While all the times are within an order of magnitude of each other, multiplying a dense and a sparse matrix takes about twice as long as multiplying two sparse matrices together, and multiplying a sparse and dense matrix takes about three times as long. (The sparse-dense multiply is actually one area where Armadillo 8.500 makes massive gains over previous versions. This operation used to take much longer due to using an unoptimised multiplication algorithm.)

Let us see if we can help the performance of the mixed-type functions by creating a temporary sparse copy of the dense input. This forces Armadillo to use the sparse-sparse version of matrix multiply, which as seen above is much more efficient. For example, here is the result of tweaking the dense-sparse multiply. Creating the sparse copy does take some extra time and memory, but not enough to affect the result.

// [[Rcpp::depends(RcppArmadillo)]]
#include <RcppArmadillo.h>

// [[Rcpp::export]]
arma::sp_mat mult_sp_den_to_sp2(const arma::sp_mat& a, const arma::mat& b) {
    // sparse x dense -> sparse
    // copy dense to sparse, then multiply
    arma::sp_mat temp(b);
    arma::sp_mat result(a * temp);
    return result;
system.time(m4 <- mult_sp_den_to_sp2(a, b_den))
   user  system elapsed 
  0.401   0.047   0.448 
identical(m0, m4)
[1] TRUE

This shows that mixing sparse and dense inputs can have significant effects on the efficiency of your code. To avoid unexpected slowdowns, consider sticking to either sparse or dense classes for all your objects. If one decides to mix them, it is worth remembering to test and profile the code.

Row vs column access

Consider another simple computation: multiply the elements of a matrix by their row number, then sum them up. (The multiply by row number is to make it not completely trivial.) That is, we want to obtain:

Armadillo lets us extract individual rows and columns from a matrix, using the .row() and .col() member functions. We can use row extraction to do this computation:

// [[Rcpp::depends(RcppArmadillo)]]
#include <RcppArmadillo.h>

// [[Rcpp::export]]
arma::sp_mat row_slice(const arma::sp_mat& x, const int n) {
    return x.row(n - 1);
    result <- sapply(1:nrow(a),
        function(i) i * sum(row_slice(a, i)))
[1] 1248361320
   user  system elapsed 
  1.708   0.000   1.707 

For a large matrix, this takes a not-insignificant amount of time, even on a fast machine. To speed it up, we will make use of the fact that Armadillo uses the compressed sparse column (CSC) format for storing sparse matrices. This means that the data for a matrix is stored as three vectors: the nonzero elements; the row indices of these elements (ordered by column); and a vector of offsets for the first row index in each column. Since the vector of row indices is ordered by column, and we have the starting offsets for each column, it turns out that extracting a column slice is actually very fast. We only need to find the offset for that column, and then pull out the elements and row indices up to the next column offset. On the other hand, extracting a row is much more work; we have to search through the indices to find those matching the desired row.

We can put this knowledge to use on our problem. Row slicing a matrix is the same as transposing it and then slicing by columns, so let us define a new function to return a column slice. (Transposing the matrix takes only a tiny fraction of a second.)

// [[Rcpp::depends(RcppArmadillo)]]
#include <RcppArmadillo.h>

// [[Rcpp::export]]
arma::sp_mat col_slice(const arma::sp_mat& x, const int n) {
    return x.col(n - 1);
a_t <- t(a)
    result <- sapply(1:nrow(a_t),
        function(i) i * sum(col_slice(a_t, i)))
[1] 1248361320
   user  system elapsed 
  0.766   0.000   0.766 

The time taken has come down by quite a substantial margin. This reflects the ease of obtaining column slices for sparse matrices.

The R–C++ interface

We can take the previous example further. Each time R calls a C++ function that takes a sparse matrix as input, it makes a copy of the data. Similarly, when the C++ function returns, its sparse outputs are copied into R objects. When the function itself is very simple—as it is here—all this copying and memory shuffling can be a significant proportion of the time taken.

Rather than calling sapply in R to iterate over rows, let us do the same entirely in C++:

// [[Rcpp::depends(RcppArmadillo)]]
#include <RcppArmadillo.h>

// [[Rcpp::export]]
double sum_by_row(const arma::sp_mat& x) {
    double result = 0;
    for (size_t i = 0; i < x.n_rows; i++) {
        arma::sp_mat row(x.row(i));
        for (arma::sp_mat::iterator j = row.begin(); j != row.end(); ++j) {
            result += *j * (i + 1);
    return result;
[1] 1248361320
   user  system elapsed 
  0.933   0.000   0.935 

This is again a large improvement. But what if we do the same with column slicing?

// [[Rcpp::depends(RcppArmadillo)]]
#include <RcppArmadillo.h>

// [[Rcpp::export]]
double sum_by_col(const arma::sp_mat& x) {
    double result = 0;
    for (size_t i = 0; i < x.n_cols; i++) {
        arma::sp_mat col(x.col(i));
        for (arma::sp_mat::iterator j = col.begin(); j != col.end(); ++j) {
            result += *j * (i + 1);
    return result;
[1] 1248361320
   user  system elapsed 
  0.005   0.000   0.006 

Now the time is less than a tenth of a second, which is faster than the original code by roughly three orders of magnitude. The moral to the story is: rather than constantly switching between C++ and R, you should try to stay in one environment for as long as possible. If your code involves a loop with a C++ call inside (including functional maps like lapply and friends), consider writing the loop entirely in C++ and combine the results into a single object to return to R.

(It should be noted that this interface tax is less onerous for built-in Rcpp classes such as NumericVector or NumericMatrix, which do not require making copies of the data. Sparse data types are different, and in particular Armadillo’s sparse classes do not provide constructors that can directly use auxiliary memory.)

Iterators vs elementwise access

Rather than taking explicit slices of the data, let us try using good old-fashioned loops over the matrix elements. This is easily coded up in Armadillo, and it turns out to be quite efficient, relatively speaking. It is not as fast as using column slicing, but much better than row slicing.

// [[Rcpp::depends(RcppArmadillo)]]
#include <RcppArmadillo.h>

// [[Rcpp::export]]
double sum_by_element(const arma::sp_mat& x) {
    double result = 0;
    // loop over columns, then rows: see comments at the start of this article
    for (size_t j = 0; j < x.n_cols; j++) {
        for (size_t i = 0; i < x.n_rows; i++) {
            result += x(i, j) * (i + 1);
    return result;
[1] 1248361320
   user  system elapsed 
  0.176   0.000   0.176 

However, we can still do better. In Armadillo, the iterators for sparse matrix classes iterate only over the nonzero elements. Let us compare this to our naive double loop:

// [[Rcpp::depends(RcppArmadillo)]]
#include <RcppArmadillo.h>

// [[Rcpp::export]]
double sum_by_iterator(const arma::sp_mat& x) {
    double result = 0;
    for (arma::sp_mat::const_iterator i = x.begin(); i != x.end(); ++i) {
        result += *i * (i.row() + 1);
    return result;
[1] 1248361320
   user  system elapsed 
  0.002   0.000   0.002 

This is the best time achieved so far, to the extent that system.time might have difficulty capturing it. The timings are now so low that we should use the microbenchmark package to get accurate measurements:

Unit: milliseconds
 expr       min        lq      mean    median        uq       max neval
  col   4.78921   4.88444   5.05229   4.99184   5.18450   5.50579    20
 elem 172.84830 177.20431 179.87007 179.06447 182.08075 188.11256    20
 iter   1.02268   1.05447   1.12611   1.12627   1.16482   1.30800    20

Thus, using iterators represents a greater than three-order-of-magnitude speedup over the original row-slicing code.

April 18, 2018 12:00 AM

March 27, 2018

RCpp Gallery

Suppressing Call Stack Info in Rcpp-Generated Errors and Warnings


Rcpp has an elegant mechanism of exception handling whereby C++ exceptions are automatically translated to errors in R. For most projects, the Rcpp::stop wrapper (in conjunction with the BEGIN_RCPP and END_RCPP macros automatically inserted by RcppAttributes) is sufficient and easy to use, providing an Rcpp equivalent of base::stop.

By default, it captures the call stack and attaches it to the exception in R, giving informative error messages:

#include "Rcpp.h"
using namespace Rcpp; 

NumericVector add1(NumericVector x, NumericVector y){
    if(x.size() != y.size()){
        stop("x and y are not the same length!");
    return x + y; 
add1(1:5, 1:3)
Error in add1(1:5, 1:3): x and y are not the same length!

This matches the default behavior of base::stop() which captures the call info.

For complex calling patterns (e.g., creating an argument list and calling the Rcpp function with, the resulting error messages are less helpful:

#include "Rcpp.h"
using namespace Rcpp; 

// [[Rcpp::export]]
NumericVector internal_function_name(NumericVector x, NumericVector y){
    if(x.size() != y.size()){
        stop("x and y are not the same length!");
    return x + y; 
add2 <- function(x, y){
        x <- as.numeric(x)
    }, list(x, y))

add2(1:5, 1:3)
Error in (function (x, y) : x and y are not the same length!

If the internal error were being generated in R code, we might choose to use the call.=FALSE argument to base::stop to suppress the unhelpful (function (x, y) part of the error message, but we don’t (immediately) have a corresponding option in Rcpp. In this gallery post, we show how to suppress the call-stack capture of Rcpp::stop to give cleaner error messages.

Error Messages

The key functionality was added to Rcpp by Jim Hester in Rcpp Pull Request #663. To generate an R-level exception without a call stack, we pass an optional false flag to Rcpp::exception. For example,

#include "Rcpp.h"
using namespace Rcpp; 

// [[Rcpp::export]]
NumericVector internal_function_name2(NumericVector x, NumericVector y){
    if(x.size() != y.size()){
        throw Rcpp::exception("x and y are not the same length!", false);
    return x + y; 
add3 <- function(x, y){
        x <- as.numeric(x)
    }, list(x, y))

add3(1:5, 1:3)
Error: x and y are not the same length!

This can’t capture the R level call stack, but it is at least cleaner than the error message from the previous example.

Note that here, as elsewhere in C++, we need to handle exceptions using a try/catch structure, but we do not add it explicitly because RcppAttributes automatically handles this for us.


Similar to Rcpp::stop, Rcpp also provides a warning function to generate R level warnings. It has the same call-stack capture behavior as stop.

For the direct call case:

#include "Rcpp.h"
using namespace Rcpp; 

NumericVector add4(NumericVector x, NumericVector y){
    if(x.size() != y.size()){
        warning("x and y are not the same length!");
    return x + y; 
add4(1:5, 1:3)
Warning in add4(1:5, 1:3): x and y are not the same length!
[1] 2 4 6 4 5

For the indirect call case:

#include "Rcpp.h"
using namespace Rcpp; 

// [[Rcpp::export]]
NumericVector internal_function_name3(NumericVector x, NumericVector y){
    if(x.size() != y.size()){
        warning("x and y are not the same length!");
    return x + y; 
add5 <- function(x, y){
        x <- as.numeric(x)
    }, list(x, y))

add5(1:5, 1:3)
Warning in (function (x, y) : x and y are not the same length!
[1] 2 4 6 4 5

If we want to suppress the call stack info in this warning, we have to drop down to the C-level R API. In particular, we use the Rf_warningcall function, which takes the call as the first argument. By passing a NULL, we suppress the call:

#include "Rcpp.h"
using namespace Rcpp; 

// [[Rcpp::export]]
NumericVector internal_function_name5(NumericVector x, NumericVector y){
    if(x.size() != y.size()){
        Rf_warningcall(R_NilValue, "x and y are not the same length!");
    return x + y; 
add6 <- function(x, y){
        x <- as.numeric(x)
    }, list(x, y))

add6(1:5, 1)
Warning: x and y are not the same length!
[1] 2 2 3 4 5

A C++11 Implementation

The above methods work, but they are not as clean as their Rcpp::stop and Rcpp::warning counterparts. We can take advantage of C++11 to provide similar functionality for our call-free versions.

Basing our implementation on the C++11 implementation of Rcpp::stop and Rcpp::warning we can define our own stopNoCall and warningNoCall

#include "Rcpp.h"
using namespace Rcpp; 

// [[Rcpp::plugins(cpp11)]]
template <typename... Args>
inline void warningNoCall(const char* fmt, Args&&... args ) {
    Rf_warningcall(R_NilValue, tfm::format(fmt, std::forward<Args>(args)... ).c_str());

template <typename... Args>
inline void NORET stopNoCall(const char* fmt, Args&&... args) {
    throw Rcpp::exception(tfm::format(fmt, std::forward<Args>(args)... ).c_str(), false);

// [[Rcpp::export]]
NumericVector internal_function_name6(NumericVector x, NumericVector y, bool warn){
    if(x.size() != y.size()){
            warningNoCall("x and y are not the same length!");  
        } else {
            stopNoCall("x and y are not the same length!");
    return x + y; 
add7 <- function(x, y, warn=TRUE){
        x <- as.numeric(x)
    }, list(x, y, warn))
add7(1:5, 1:3, warn=TRUE)
Warning: x and y are not the same length!
[1] 2 4 6 4 5
add7(1:5, 1:3, warn=FALSE)
Error: x and y are not the same length!

Note that we used C++11 variadic templates here – if we wanted to do something similar in C++98, we could use essentially the same pattern, but would need to implement each case individually.

March 27, 2018 12:00 AM

March 07, 2018

RCpp Gallery

Introducing RcppArrayFire


The RcppArrayFire package provides an interface from R to and from the ArrayFire library, an open source library that can make use of GPUs and other hardware accelerators via CUDA or OpenCL.

The official R bindings expose ArrayFire data structures as S4 objects in R, which would require a large amount of code to support all the methods defined in ArrayFire’s C/C++ API. RcppArrayFire instead, which is derived from RcppFire by Kazuki Fukui, follows the lead of packages like RcppArmadillo or RcppEigen to provide seamless communication between R and ArrayFire at the C++ level.


Please note that RcppArrayFire is developed and tested on Linux systems. There is preliminary support for Mac OS X.

In order to use RcppArrayFire you will need the ArrayFire library and header files. While ArrayFire has been packaged for Debian, I currently prefer using upstream’s binary installer or building from source.

RcppArrayFire is not on CRAN, but you can install the current version via drat:


If you have installed ArrayFire in a non-standard directory, you have to use the configure argument --with-arrayfire, e.g.:

install.packages("RcppArrayFire", configure.args = "--with-arrayfire=/opt/arrayfire-3")

A first example

Let’s look at the classical example of calculating via simulation. The basic idea is to generate a large number of random points within the unit square. An approximation for can then be calculated from the ratio of points within the unit circle to the total number of points. A vectorized implementation in R might look like this:

piR <- function(N) {
    x <- runif(N)
    y <- runif(N)
    4 * sum(sqrt(x^2 + y^2) < 1.0) / N

system.time(cat("pi ~= ", piR(10^6), "\n"))
pi ~=  3.13999 
   user  system elapsed 
  0.102   0.009   0.111 

A simple way to use C++ code in R is to use the inline package or cppFunction() from Rcpp, which are both possible with RcppArrayFire. An implementation in C++ using ArrayFire might look like this:

src <- '
double piAF (const int N) {
    array x = randu(N, f32);
    array y = randu(N, f32);
    return 4.0 * sum<float>(sqrt(x*x + y*y) < 1.0) / N;
Rcpp::cppFunction(code = src, depends = "RcppArrayFire", includes = "using namespace af;")

cat("pi ~= ", piAF(10^6), "\n") # also used for warm-up 
pi ~=  3.14279 
   user  system elapsed 
  0.000   0.001   0.000 

Several things are worth noting:

  1. The syntax is almost identical. Besides the need for using types and a different function name when generating random numbers, the argument f32 to randu as well as the float type catches the eye. These instruct ArrayFire to use single precision floats, since not all devices support double precision floating point numbers. If you want and can to use double precision, you have to specify f64 and double.

  2. The results are not the same since ArrayFire uses a different random number generator.

  3. The speed-up can be quite impressive. However, the first invocation of a function is often not as fast as expected due to the just-in-time compilation used by ArrayFire. This can be circumvented by using a warm-up call with (normally) fewer computations.

Arrays as parameters

Up to now we have only considered simple types like double or int as function parameters and return values. However, we can also use arrays. Consider the case of an European put option that was recently handled with R, Rcpp and RcppArmadillo. The Armadillo based function from this post reads:

#include <RcppArmadillo.h>

// [[Rcpp::depends(RcppArmadillo)]]
// [[Rcpp::plugins(cpp11)]]

using arma::colvec;
using arma::log;
using arma::normcdf;
using std::sqrt;
using std::exp;

// [[Rcpp::export]]
colvec put_option_pricer_arma(colvec s, double k, double r, double y, double t, double sigma) {
  colvec d1 = (log(s / k) + (r - y + sigma * sigma / 2.0) * t) / (sigma * sqrt(t));
  colvec d2 = d1 - sigma * sqrt(t);
  // Notice the use of % to represent element wise multiplication
  colvec V = normcdf(-d2) * k * exp(-r * t) - s * exp(-y * t) % normcdf(-d1); 
  return V;

This function can be applied to a range of spot prices:

put_option_pricer_arma(s = 55:60, 60, .01, .02, 1, .05)
[1,] 5.52021
[2,] 4.58142
[3,] 3.68485
[4,] 2.85517
[5,] 2.11883
[6,] 1.49793

Porting this code to RcppArrayFire is straight forward:

#include <RcppArrayFire.h>

// [[Rcpp::depends(RcppArrayFire)]]

using af::array;
using af::log;
using af::erfc;
using std::sqrt;
using std::exp;

array normcdf(array x) {
  return erfc(-x / sqrt(2.0)) / 2.0;

// [[Rcpp::export]]
array put_option_pricer_af(RcppArrayFire::typed_array<f32> s, double k, double r,
                           double y, double t, double sigma) {
  array d1 = (log(s / k) + (r - y + sigma * sigma / 2.0) * t) / (sigma * sqrt(t));
  array d2 = d1 - sigma * sqrt(t);
  return normcdf(-d2) * k * exp(-r * t) - s * exp(-y * t) * normcdf(-d1); 

Compared with the implementations in R, Rcpp and RcppArmadillo the syntax is again almost the same. One exception is that ArrayFire does not contain a function for the cumulative normal distribution function. However, the closely related error function is available.

Since an object of type af::array can contain different data types, the templated wrapper class RcppArrayFire::typed_array<> is used to indicate the desired data type when converting from R to C++. Again single precision floats are used with ArrayFire, which leads to differences of the order compared to the results from R, Rcpp and RcppArmadillo:

put_option_pricer_af(s = 55:60, 60, .01, .02, 1, .05)
[1] 5.52021 4.58143 3.68485 2.85516 2.11883 1.49793


The reason to use hardware accelerators is of course the quest for increased performance. How does ArrayFire fare in this respect? Using the same benchmark as in the R, Rcpp and RcppArmadillo comparison:

s <- matrix(seq(0, 100, by = .0001), ncol = 1)
rbenchmark::benchmark(Arma = put_option_pricer_arma(s, 60, .01, .02, 1, .05),
                      AF = put_option_pricer_af(s, 60, .01, .02, 1, .05),
                      order = "relative", 
                      replications = 100)[,1:4]
  test replications elapsed relative
2   AF          100   0.471    1.000
1 Arma          100   5.923   12.575

Here a Nvidia GeForce GT 1030 is used together with ArrayFire’s CUDA backend. With a build-in Intel HD Graphics 520 using the OpenCL backend the ArrayFire solution is about 6 times faster. Even without a high performance GPU the performance boost from using ArrayFire can be quite impressive. However, the results change dramatically, if fewer options are evaluated:

s <- matrix(seq(0, 100, by = 1), ncol = 1)
# use more replications to get run times of more than 10 ms
rbenchmark::benchmark(Arma = put_option_pricer_arma(s, 60, .01, .02, 1, .05),
                      AF = put_option_pricer_af(s, 60, .01, .02, 1, .05),
                      order = "relative", 
                      replications = 1000)[,1:4]
  test replications elapsed relative
1 Arma         1000   0.008    1.000
2   AF         1000   0.123   15.375

But is it realistic to process options at once? Probably not in the way used in the benchmark where only the spot price is allowed to vary. However, one can alter the function to process not only arrays of spot prices but also arrays of strikes, risk free rates etc.:

#include <RcppArrayFire.h>

// [[Rcpp::depends(RcppArrayFire)]]

using af::array;
using af::log;
using af::erfc;
using af::sqrt; // arrayfire function instead of standard function
using af::exp;  // arrayfire function instead of standard function

array normcdf(array x) {
  return erfc(-x / sqrt(2.0)) / 2.0;

// [[Rcpp::export]]
array put_option_pricer_af(RcppArrayFire::typed_array<f32> s,
                           RcppArrayFire::typed_array<f32> k, 
                           RcppArrayFire::typed_array<f32> r, 
                           RcppArrayFire::typed_array<f32> y, 
                           RcppArrayFire::typed_array<f32> t, 
                           RcppArrayFire::typed_array<f32> sigma) {
  array d1 = (log(s / k) + (r - y + sigma * sigma / 2.0) * t) / (sigma * sqrt(t));
  array d2 = d1 - sigma * sqrt(t);
  return normcdf(-d2) * k * exp(-r * t) - s * exp(-y * t) * normcdf(-d1); 

Note that ArrayFire does not recycle elements if arrays with non-matching dimensions are combined. In this particular case this means that all arrays must have the same length. One can ensure that by using a data frame for the values:

# 1000 * 21 * 3 * 3 * 3 * 3 = 1,701,000 different options
options <- expand.grid(
  s = rnorm(1000, mean = 60, sd = 20),
  k = 50:70,
  r = c(0.01, 0.005, 0.02),
  y = c(0.02, 0.01, 0.04),
  t = c(1, 0.5, 2),
  sigma = c(0.05, 0.025, 0.1)
            p <- put_option_pricer_af(s, k, r, y, t, sigma)))
        s  k    r    y t sigma           p
1 87.4192 50 0.01 0.02 1  0.05 7.44673e-29
2 48.7060 50 0.01 0.02 1  0.05 2.09401e+00
3 67.2626 50 0.01 0.02 1  0.05 2.34556e-09
4 72.6573 50 0.01 0.02 1  0.05 6.84457e-14
5 68.0854 50 0.01 0.02 1  0.05 5.26653e-10
6 57.8775 50 0.01 0.02 1  0.05 2.57750e-03


The ArrayFire library provides a convenient way to use hardware accelerators without the need to write low-level OpenCL or CUDA code. The C++ syntax is actually quite similar to properly vectorized R code. The RcppArrayFire package makes this available to useRs. However, one still has to be careful: using hardware accelerators is not a “silver bullet” due to the inherent memory transfer overhead.

March 07, 2018 12:00 AM

February 28, 2018

RCpp Gallery

Using RcppArmadillo to price European Put Options


In the quest for ever faster code, one generally begins exploring ways to integrate C++ with R using Rcpp. This post provides an example of multiple implementations of a European Put Option pricer. The implementations are done in pure R, pure Rcpp using some Rcpp sugar functions, and then in Rcpp using RcppArmadillo, which exposes the incredibly powerful linear algebra library, Armadillo.

Under the Black-Scholes model The value of a European put option has the closed form solution:



Armed with the formulas, we can create the pricer using just R.

put_option_pricer <- function(s, k, r, y, t, sigma) {

    d1 <- (log(s / k) + (r - y + sigma^2 / 2) * t) / (sigma * sqrt(t))
    d2 <- d1 - sigma * sqrt(t)

    V <- pnorm(-d2) * k * exp(-r * t) - s * exp(-y * t) * pnorm(-d1)


# Valuation with 1 stock price
put_option_pricer(s = 55, 60, .01, .02, 1, .05)
[1] 5.52021
# Valuation across multiple prices
put_option_pricer(s = 55:60, 60, .01, .02, 1, .05)
[1] 5.52021 4.58142 3.68485 2.85517 2.11883 1.49793

Let’s see what we can do with Rcpp. Besides explicitely stating the types of the variables, not much has to change. We can even use the sugar function, Rcpp::pnorm(), to keep the syntax as close to R as possible. Note how we are being explicit about the symbols we import from the Rcpp namespace: the basic vector type, and well the (vectorized) ‘Rcpp Sugar’ calls log() and pnorm() calls. Similarly, we use sqrt() and exp() for the calls on an atomic double variables from the C++ Standard Library. With these declarations the code itself is essentially identical to the R code (apart of course from requiring both static types and trailing semicolons).

#include <Rcpp.h>
using Rcpp::NumericVector;
using Rcpp::log;
using Rcpp::pnorm;
using std::sqrt;
using std::log;

// [[Rcpp::export]]
NumericVector put_option_pricer_rcpp(NumericVector s, double k, double r, double y, double t, double sigma) {

    NumericVector d1 = (log(s / k) + (r - y + sigma * sigma / 2.0) * t) / (sigma * sqrt(t));
    NumericVector d2 = d1 - sigma * sqrt(t);
    NumericVector V = pnorm(-d2) * k * exp(-r * t) - s * exp(-y * t) * pnorm(-d1);
    return V;

We can call this from R as well:

# Valuation with 1 stock price
put_option_pricer_rcpp(s = 55, 60, .01, .02, 1, .05)
[1] 5.52021
# Valuation across multiple prices
put_option_pricer_rcpp(s = 55:60, 60, .01, .02, 1, .05)
[1] 5.52021 4.58142 3.68485 2.85517 2.11883 1.49793

Finally, let’s look at RcppArmadillo. Armadillo has a number of object types, including mat, colvec, and rowvec. Here, we just use colvec to represent a column vector of prices. By default in Armadillo, * represents matrix multiplication, and % is used for element wise multiplication. We need to make this change to element wise multiplication in 1 place, but otherwise the changes are just switching out the types and the sugar functions for Armadillo specific functions.

Note that the arma::normcdf() function is in the upcoming release of RcppArmadillo, which is 0.8.400.0.0 at the time of writing and still in CRAN’s incoming. It also requires the C++11 plugin.

#include <RcppArmadillo.h>

// [[Rcpp::depends(RcppArmadillo)]]
// [[Rcpp::plugins(cpp11)]]

using arma::colvec;
using arma::log;
using arma::normcdf;
using std::sqrt;
using std::log;

// [[Rcpp::export]]
colvec put_option_pricer_arma(colvec s, double k, double r, double y, double t, double sigma) {
    colvec d1 = (log(s / k) + (r - y + sigma * sigma / 2.0) * t) / (sigma * sqrt(t));
    colvec d2 = d1 - sigma * sqrt(t);
    // Notice the use of % to represent element wise multiplication
    colvec V = normcdf(-d2) * k * exp(-r * t) - s * exp(-y * t) % normcdf(-d1); 

    return V;

Use from R:

# Valuation with 1 stock price
put_option_pricer_arma(s = 55, 60, .01, .02, 1, .05)
[1,] 5.52021
# Valuation across multiple prices
put_option_pricer_arma(s = 55:60, 60, .01, .02, 1, .05)
[1,] 5.52021
[2,] 4.58142
[3,] 3.68485
[4,] 2.85517
[5,] 2.11883
[6,] 1.49793

Finally, we can run a speed test to see which comes out on top.

s <- matrix(seq(0, 100, by = .0001), ncol = 1)

rbenchmark::benchmark(R = put_option_pricer(s, 60, .01, .02, 1, .05),
                      Arma = put_option_pricer_arma(s, 60, .01, .02, 1, .05),
                      Rcpp = put_option_pricer_rcpp(s, 60, .01, .02, 1, .05), 
                      order = "relative", 
                      replications = 100)[,1:4]
  test replications elapsed relative
2 Arma          100   6.409    1.000
3 Rcpp          100   7.917    1.235
1    R          100   9.091    1.418

Interestingly, Armadillo comes out on top here on this (multi-core) machine (as Armadillo uses OpenMP where available in newer versions). But the difference is slender, and there is certainly variation in repeated runs. And the nicest thing about all of this is that it shows off the “embarassment of riches” that we have in the R and C++ ecosystem for multiple ways of solving the same problem.

February 28, 2018 12:00 AM

November 07, 2017


Julia: Installation and Editors

If you have been following this blog, you may have noticed that I don't have any update for more than a year now. The reason is that I've been busy with my research, my work, and I promised not to share anything here until I finished my degree (Master of Science in Statistics). Anyways, at this point I think it's time to share with you what I've learned in the past year. So far, it's been a good year for Statistics especially in the Philippines, in fact, last November 15, 2016, the team of local data scientists made a huge step in Big data by organizing the first ever conference on this topic. Also months before that, the 13th National Convention on Statistics organized by the Philippine Statistics Authority, invited a keynote speaker from Paris21 to tackle Big data and its use in the government.

So without further ado, in this post, I would like to share a new programming language which I've used for several months now, and it's called Julia. This programming language is by far my favorite, it's a well-thought-out language as many would say, for many reasons. The first of course is the speed, second is the grammar, and many more. I can't list them down here, but I suggest you visit the official website, and try it for yourself.


The installation of this program is straightforward, simply go to the Julia's official download page and download the binaries for your operating system. Alternatively, you can install Julia by downloading the JuliaPro from the Julia Computing products. This will setup everything you need, which include the Github Atom Editor out of the box. After installation, the first time you load the command-line-version program, you'll have the following window:

Working with the command-line-version is actually fun, and personally I think Julia has the best command-line-version compared to R and Python in terms of features. For example, you can shift to shell mode by simply pressing ; in the Julia prompt, and using ? to activate the help mode. It also has autocompletion by pressing Tab after entering first few letters of the syntax, the LaTeX UTF autocompletion is also one of the best features, and almost any symbols/characters can be used as variables, like emoticon as shown below:


While Julia's command-line-version is loaded with good features, working with huge project needs a better front-end editors. Like RStudio for R, PyCharm for Python, Julia can run on Jupyter (also available for R and Python), Github Atom Editor, and Microsoft Visual Studio Code.

Julia in Jupyter Notebook

Julia in Github Atom Editor

Julia in Microsoft Visual Studio Code

To install the Jupyter notebook, simply run the following codes:
In the screenshot above, I tweaked the theme of the notebook using the script from this repository. As mentioned, to setup Julia in Github Atom Editor, I recommend downloading the JuliaPro or you can follow the instruction in the Juno Lab website. After installation, you can add Atom Extensions like Minimap, which is not available by default, and in case you are interested, the syntax highlighter I used in the screenshot is the Gruvbox Plus.

Further, to setup Julia in Microsoft Visual Studio Code, open the program, press Ctrl+P, paste ext install language-julia and hit Enter. This will install the Julia extension for Visual Studio Code. After installation, you can load the Julia REPL by pressing the following keys Ctrl+Shift+P (Windows) or Cmd+Shift+P (Mac) and enter julia start repl, and press Enter. If there is an error, the path may need to be specified properly. To do this, go to Preferences > Settings. Then in the .json user file settings, enter the following:
Of course, you need to check the path properly by replacing the Julia-0.6.0-rc3 (Windows) or (Mac) with the desired version of your Julia, and the C:/Users/MyName with your desired path. Further, I use the following setting in my .json file to adjust my Minimap similar to the screenshot above.
Lastly, to toggle the cursor's focus between the script pane and the integrated Julia terminal using Ctrl+`, I use the following Keybindings (go to Preferences > Keyboard Shortcuts > keybindings.json).
For more on this topic visit the official github page. The three editors above have advantages and disadvantages. However, my primary editor is the Visual Studio Code, because it is fast and loaded with features as well. The major limitation of this editor is the LaTeX UTF autocompletion, which is available for Atom Editor. But there are third party packages like Unicode LaTeX, that can do the job indirectly, or alternatively you can generate the LaTeX UTF using the console (the integrated Julia terminal in the Visual Studio Code), but I think this is not a big deal, and may be in the near future, this capability will be added. On the other hand, the Atom Editor has of course more features for Julia, for example the plot pane, the workspace, and many more. The only problem is that, it's kind of slow especially when working with several datasets in your workspace, plus plots, plus very long lines of codes, scrolling through it is not smooth. Nevertheless, let's be positive and hope that more improvements are coming to these editors. Finally, for those who want to start using Julia, visit the Official Documentation and Learning Materials; ask questions on Julia Discourse and join the Julia Gitter.

by Unknown ( at November 07, 2017 04:35 AM

April 15, 2017


R and Python: Gradient Descent

One of the problems often dealt in Statistics is minimization of the objective function. And contrary to the linear models, there is no analytical solution for models that are nonlinear on the parameters such as logistic regression, neural networks, and nonlinear regression models (like Michaelis-Menten model). In this situation, we have to use mathematical programming or optimization. And one popular optimization algorithm is the gradient descent, which we're going to illustrate here. To start with, let's consider a simple function with closed-form solution given by \begin{equation} f(\beta) \triangleq \beta^4 - 3\beta^3 + 2. \end{equation} We want to minimize this function with respect to $\beta$. The quick solution to this, as what calculus taught us, is to compute for the first derivative of the function, that is \begin{equation} \frac{\text{d}f(\beta)}{\text{d}\beta}=4\beta^3-9\beta^2. \end{equation} Setting this to 0 to obtain the stationary point gives us \begin{align} \frac{\text{d}f(\beta)}{\text{d}\beta}&\overset{\text{set}}{=}0\nonumber\\ 4\hat{\beta}^3-9\hat{\beta}^2&=0\nonumber\\ 4\hat{\beta}^3&=9\hat{\beta}^2\nonumber\\ 4\hat{\beta}&=9\nonumber\\ \hat{\beta}&=\frac{9}{4}. \end{align}
The following plot shows the minimum of the function at $\hat{\beta}=\frac{9}{4}$ (red line in the plot below).

R ScriptNow let's consider minimizing this problem using gradient descent with the following algorithm:
  1. Initialize $\mathbf{x}_{r},r=0$
  2. while $\lVert \mathbf{x}_{r}-\mathbf{x}_{r+1}\rVert > \nu$
  3.         $\mathbf{x}_{r+1}\leftarrow \mathbf{x}_{r} - \gamma\nabla f(\mathbf{x}_r)$
  4.         $r\leftarrow r + 1$
  5. end while
  6. return $\mathbf{x}_{r}$ and $r$
where $\nabla f(\mathbf{x}_r)$ is the gradient of the cost function, $\gamma$ is the learning-rate parameter of the algorithm, and $\nu$ is the precision parameter. For the function above, let the initial guess be $\hat{\beta}_0=4$ and $\gamma=.001$ with $\nu=.00001$. Then $\nabla f(\hat{\beta}_0)=112$, so that \[\hat{\beta}_1=\hat{\beta}_0-.001(112)=3.888.\] And $|\hat{\beta}_1 - \hat{\beta}_0| = 0.112> \nu$. Repeat the process until at some $r$, $|\hat{\beta}_{r}-\hat{\beta}_{r+1}| \ngtr \nu$. It will turn out that 350 iterations are needed to satisfy the desired inequality, the plot of which is in the following figure with estimated minimum $\hat{\beta}_{350}=2.250483\approx\frac{9}{4}$.

R Script with PlotPython ScriptObviously the convergence is slow, and we can adjust this by tuning the learning-rate parameter, for example if we try to increase it into $\gamma=.01$ (change gamma to .01 in the codes above) the algorithm will converge at 42nd iteration. To support that claim, see the steps of its gradient in the plot below.

If we try to change the starting value from 4 to .1 (change beta_new to .1) with $\gamma=.01$, the algorithm converges at 173rd iteration with estimate $\hat{\beta}_{173}=2.249962\approx\frac{9}{4}$ (see the plot below).

Now let's consider another function known as Rosenbrock defined as \begin{equation} f(\mathbf{w})\triangleq(1 - w_1) ^ 2 + 100 (w_2 - w_1^2)^2. \end{equation} The gradient is \begin{align} \nabla f(\mathbf{w})&=[-2(1 - w_1) - 400(w_2 - w_1^2) w_1]\mathbf{i}+200(w_2-w_1^2)\mathbf{j}\nonumber\\ &=\left[\begin{array}{c} -2(1 - w_1) - 400(w_2 - w_1^2) w_1\\ 200(w_2-w_1^2) \end{array}\right]. \end{align} Let the initial guess be $\hat{\mathbf{w}}_0=\left[\begin{array}{c}-1.8\\-.8\end{array}\right]$, $\gamma=.0002$, and $\nu=.00001$. Then $\nabla f(\hat{\mathbf{w}}_0)=\left[\begin{array}{c} -2914.4\\-808.0\end{array}\right]$. So that \begin{equation}\nonumber \hat{\mathbf{w}}_1=\hat{\mathbf{w}}_0-\gamma\nabla f(\hat{\mathbf{w}}_0)=\left[\begin{array}{c} -1.21712 \\-0.63840\end{array}\right]. \end{equation} And $\lVert\hat{\mathbf{w}}_0-\hat{\mathbf{w}}_1\rVert=0.6048666>\nu$. Repeat the process until at some $r$, $\lVert\hat{\mathbf{w}}_r-\hat{\mathbf{w}}_{r+1}\rVert\ngtr \nu$. It will turn out that 23,374 iterations are needed for the desired inequality with estimate $\hat{\mathbf{w}}_{23375}=\left[\begin{array}{c} 0.9464841 \\0.8956111\end{array}\right]$, the contour plot is depicted in the figure below.
R Script with Contour PlotPython ScriptNotice that I did not use ggplot for the contour plot, this is because the plot needs to be updated 23,374 times just to accommodate for the arrows for the trajectory of the gradient vectors, and ggplot is just slow. Finally, we can also visualize the gradient points on the surface as shown in the following figure.
R ScriptIn my future blog post, I hope to apply this algorithm on statistical models like linear/nonlinear regression models for simple illustration.

by Unknown ( at April 15, 2017 12:31 PM

September 29, 2016

Statistical Modelling

Time-dependent ROC methodology to evaluate the predictive accuracy of semiparametric multi-state models in the presence of competing risks: An application to peritoneal dialysis programme


The evaluation of peritoneal dialysis (PD) programmes requires the use of statistical methods that suit the complexity of such programmes. Multi-state regression models taking competing risks into account are a good example of suitable approaches. In this work, multi-state structured additive regression (STAR) models combined with penalized splines (P-splines) are proposed to evaluate peritoneal dialysis programmes. These models are very flexible since they may consider smooth estimates of baseline transition intensities and the inclusion of time-varying and smooth covariate effects at each transition. A key issue in survival analysis is the quantification of the time-dependent predictive accuracy of a given regression model, which is typically assessed using receiver operating characteristic (ROC)’based methodologies. The main objective of the present study is to adapt the concept of time-dependent ROC curve, and their corresponding area under the curve (AUC), to a multi-state competing risks framework. All statistical methodologies discussed in this work were applied to PD survival data. Using a multi-state competing risks framework, this study explored the effects of major clinical covariates on survival such as age, sex, diabetes and previous renal replacement therapy. Such multi-state model was composed of one transient state (peritonitis) and several absorbing states (death, transfer to haemodialysis and renal transplantation). The application of STAR models combined with time-dependent ROC curves revealed important conclusions not previously reported in the nephrology literature when using standard statistical methodologies. For practical application, all the statistical methods proposed in this article were implemented in R and we wrote and made available a script named as NestedCompRisks.

by Teixeira, L., Cadarso-Suarez, C., Rodrigues, A., Mendonca, D. at September 29, 2016 05:16 AM

A multivariate single-index model for longitudinal data


Index measures are commonly used in medical research and clinical practice, primarily for quantification of health risks in individual subjects or patients. The utility of an index measure is ultimately contingent on its ability to predict health outcomes. Construction of medical indices has largely been based on heuristic arguments, although the acceptance of a new index typically requires objective validation, preferably with multiple outcomes. In this article, we propose an analytical tool for index development and validation. We use a multivariate single-index model to ascertain the best functional form for risk index construction. Methodologically, the proposed model represents a multivariate extension of the traditional single-index models. Such an extension is important because it assures that the resultant index simultaneously works for multiple outcomes. The model is developed in the general framework of longitudinal data analysis. We use penalized cubic splines to characterize the index components while leaving the other subject characteristics as additive components. The splines are estimated directly by penalizing nonlinear least squares, and we show that the model can be implemented using existing software. To illustrate, we examine the formation of an adiposity index for prediction of systolic and diastolic blood pressure in children. We assess the performance of the method through a simulation study.

by Wu, J., Tu, W. at September 29, 2016 05:16 AM

Semi-parametric frailty model for clustered interval-censored data


The shared frailty model is a popular tool to analyze correlated right-censored time-to-event data. In the shared frailty model, the latent frailty is assumed to be shared by the members of a cluster and is assigned a parametric distribution, typically a gamma distribution due to its conjugacy. In the case of interval-censored time-to-event data, the inclusion of frailties results in complicated intractable likelihoods. Here, we propose a flexible frailty model for analyzing such data by assuming a smooth semi-parametric form for the conditional time-to-event distribution and a parametric or a flexible form for the frailty distribution. The results of a simulation study suggest that the estimation of regression parameters is robust to misspecification of the frailty distribution (even when the frailty distribution is multimodal or skewed). Given sufficiently large sample sizes and number of clusters, the flexible approach produces smooth and accurate posterior estimates for the baseline survival function and for the frailty density, and it can correctly detect and identify unusual frailty density forms. The methodology is illustrated using dental data from the Signal Tandmobiel® study.

by Yavuz, A. C., Lambert, P. at September 29, 2016 05:16 AM

Bayesian dynamic modelling to assess differential treatment effects on panic attack frequencies


To represent the complex structure of intensive longitudinal data of multiple individuals, we propose a hierarchical Bayesian Dynamic Model (BDM). This BDM is a generalized linear hierarchical model where the individual parameters do not necessarily follow a normal distribution. The model parameters can be estimated on the basis of relatively small sample sizes and in the presence of missing time points. We present the BDM and discuss the model identification, convergence and selection. The use of the BDM is illustrated using data from a randomized clinical trial to study the differential effects of three treatments for panic disorder. The data involves the number of panic attacks experienced weekly (73 individuals, 10–52 time points) during treatment. Presuming that the counts are Poisson distributed, the BDM considered involves a linear trend model with an exponential link function. The final model included a moving average parameter and an external variable (duration of symptoms pre-treatment). Our results show that cognitive behavioural therapy is less effective in reducing panic attacks than serotonin selective re-uptake inhibitors or a combination of both. Post hoc analyses revealed that males show a slightly higher number of panic attacks at the onset of treatment than females.

by Krone, T., Albers, C., Timmerman, M. at September 29, 2016 05:16 AM

July 18, 2016

R you ready?

Populating data frame cells with more than one value

Data frames are lists

Most R users will know that data frames are lists. You can easily verify that a data frame is a list by typing

d <- data.frame(id=1:2, name=c("Jon", "Mark"))
 id name
1 1 Jon
2 2 Mark
[1] TRUE

However, data frames are lists with some special properties. For example, all entries in the list must have the same length (here 2), etc. You can find a nice description of the differences between lists and data frames here. To access the first column of d, we find that it contains a vector (and a factor in case of column name). Note, that [[ ]] is an operator to select a list element. As data frames are lists, they will work here as well.

[1] TRUE

Data frame columns can contain lists

A long time, I was unaware of the fact, that data frames may also contain lists as columns instead of vectors. For example, let’s assume Jon’s children are Mary and James, and Mark’s children are called Greta and Sally. Their names are stored in a list with two elements. We can add them to the data frame like this:

d$children <-  list(c("Mary", "James"), c("Greta", "Sally"))
 id name children
1 1 Jon Mary, James
2 2 Mark Greta, Sally

A single data frame entry in column children now contains more than one value. Given that the column is a list, not a vector, we cannot go as usual when modifying an entry of the column. For example, to change Jon’s children, we cannot do

> d[1 , "children"] <- c("Mary", "James", "Thomas")

Error in `[<`(`*tmp*`, 1, "children", value = c("Mary", "James", :
replacement has 3 rows, data has 1

Taking into account the list structure of the column, we can type the following to change the values in a single cell.

d[1 , "children"][[1]] <- list(c("Mary", "James", "Thomas"))

# or also

d$children[1] <- list(c("Mary", "James", "Thomas"))
 id name children
1 1 Jon Mary, James, Thomas
2 2 Mark Greta, Sally

You can also create a data frame having a list as a column using the <tt>data.frame</tt> function, but with a little tweak. The list column has to be wrapped inside the function <tt>I</tt>. This will protect it from several conversions taking place in <tt>data.frame</tt> (see <tt>?I</tt> documentation).

d <- data.frame(id = 1:2,
                   name = c("Jon", "Mark"),
                   children = I(list(c("Mary", "James"),
                                     c("Greta", "Sally")))

This is an interesting feature, which gives me a deeper understanding of what a data frame is. But when exactly would I want to use it? I have not encountered the need to use it very often yet (though of course there may be plenty of situations where it makes sense). But today I had a case where this feature seemed particularly useful.

Converting lists and data frames to JSON

I had two separate types of information. One stored in a data frame and the other one in a list Referring to the example above, I had

d <- data.frame(id=1:2, name=c("Jon", "Mark"))
 id name
1 1 Jon
2 2 Mark


ch <- list(c("Mary", "James"), c("Greta", "Sally"))
[1] "Mary" "James"

[1] "Greta" "Sally"

I needed to return an array of JSON objects which look like this.

    "id": 1,
    "name": "Jon",
    "children": ["Mary", "James"]
    "id": 2,
    "name": "Mark",
    "children": ["Greta", "Sally"]

Working with the superb jsonlite package to convert R to JSON, I could do the following to get the result above.


l <- split(d, seq(nrow(d))) # convert data frame rows to list
l <- unname(l)              # remove list names
for (i in seq_along(l))     # add element from ch to list
    l[[i]] <- c(l[[i]], children=ch[i])

toJSON(l, pretty=T, auto_unbox = T) # convert to JSON

The results are correct, but getting there involved quite a number of tedious steps. These can be avoided by directly placing the list into a column of the data frame. Then jsonlite::toJSON takes care of the rest.

d$children <- list(c("Mary", "James"), c("Greta", "Sally"))
toJSON(d, pretty=T, auto_unbox = T)
    "id": 1,
    "name": "Jon",
    "children": ["Mary", "James"]
    "id": 2,
    "name": "Mark",
    "children": ["Greta", "Sally"]

Nice :) What we do here, is basically creating the same nested list structure as above, only now it is disguised as a data frame. However, this approach is much more convenient.

by markheckmann at July 18, 2016 05:01 PM

December 27, 2015


R: Principal Component Analysis on Imaging

Ever wonder what's the mathematics behind face recognition on most gadgets like digital camera and smartphones? Well for most part it has something to do with statistics. One statistical tool that is capable of doing such feature is the Principal Component Analysis (PCA). In this post, however, we will not do (sorry to disappoint you) face recognition as we reserve this for future post while I'm still doing research on it. Instead, we go through its basic concept and use it for data reduction on spectral bands of the image using R.

Let's view it mathematically

Consider a line $L$ in a parametric form described as a set of all vectors $k\cdot\mathbf{u}+\mathbf{v}$ parameterized by $k\in \mathbb{R}$, where $\mathbf{v}$ is a vector orthogonal to a normalized vector $\mathbf{u}$. Below is the graphical equivalent of the statement:
So if given a point $\mathbf{x}=[x_1,x_2]^T$, the orthogonal projection of this point on the line $L$ is given by $(\mathbf{u}^T\mathbf{x})\mathbf{u}+\mathbf{v}$. Graphically, we mean

$Proj$ is the projection of the point $\mathbf{x}$ on the line, where the position of it is defined by the scalar $\mathbf{u}^{T}\mathbf{x}$. Therefore, if we consider $\mathbf{X}=[X_1, X_2]^T$ be a random vector, then the random variable $Y=\mathbf{u}^T\mathbf{X}$ describes the variability of the data on the direction of the normalized vector $\mathbf{u}$. So that $Y$ is a linear combination of $X_i, i=1,2$. The principal component analysis identifies a linear combinations of the original variables $\mathbf{X}$ that contain most of the information, in the sense of variability, contained in the data. The general assumption is that useful information is proportional to the variability. PCA is used for data dimensionality reduction and for interpretation of data. (Ref 1. Bajorski, 2012)

To better understand this, consider two dimensional data set, below is the plot of it along with two lines ($L_1$ and $L_2$) that are orthogonal to each other:
If we project the points orthogonally to both lines we have,

So that if normalized vector $\mathbf{u}_1$ defines the direction of $L_1$, then the variability of the points on $L_1$ is described by the random variable $Y_1=\mathbf{u}_1^T\mathbf{X}$. Also if $\mathbf{u}_2$ is a normalized vector that defines the direction of $L_2$, then the variability of the points on this line is described by the random variable $Y_2=\mathbf{u}_2^T\mathbf{X}$. The first principal component is one with maximum variability. So in this case, we can see that $Y_2$ is more variable than $Y_1$, since the points projected on $L_2$ are more dispersed than in $L_1$. In practice, however, the linear combinations $Y_i = \mathbf{u}_i^T\mathbf{X}, i=1,2,\cdots,p$ is maximized sequentially so that $Y_1$ is the linear combination of the first principal component, $Y_2$ is the linear combination of the second principal component, and so on. Further, the estimate of the direction vector $\mathbf{u}$ is simply the normalized eigenvector $\mathbf{e}$ of the variance-covariance matrix $\mathbf{\Sigma}$ of the original variable $\mathbf{X}$. And the variability explained by the principal component is the corresponding eigenvalue $\lambda$. For more details on theory of PCA refer to (Bajorski, 2012) at Reference 1 below.

As promised we will do dimensionality reduction using PCA. We will use the Airborne Visible/Infrared Imaging Spectrometer (AVIRIS) data from (Barjorski, 2012), you can use other locations of AVIRIS data that can be downloaded here. However, since for most cases the AVIRIS data contains thousands of bands so for simplicity we will stick with the data given in (Bajorski, 2012) as it was cleaned reducing to 152 bands only.

What is spectral bands?

In imaging, spectral bands refer to the third dimension of the image usually denoted as $\lambda$. For example, RGB image contains red, green and blue bands as shown below along with the first two dimensions $x$ and $y$ that define the resolution of the image.

These are few of the bands that are visible to our eyes, there are other bands that are not visible to us like infrared, and many other in electromagnetic spectrum. That is why in most cases AVIRIS data contains huge number of bands each captures different characteristics of the image. Below is the proper description of the data.


The Airborne Visible/Infrared Imaging Spectrometer (AVIRIS), is a sensor collecting spectral radiance in the range of wavelengths from 400 to 2500 nm. It has been flown on various aircraft platforms, and many images of the Earth’s surface are available. A 100 by 100 pixel AVIRIS image of an urban area in Rochester, NY, near the Lake Ontario shoreline is shown below. The scene has a wide range of natural and man-made material including a mixture of commercial/warehouse and residential neighborhoods, which adds a wide range of spectral diversity. Prior to processing, invalid bands (due to atmospheric water absorption) were removed, reducing the overall dimensionality to 152 bands. This image has been used in Bajorski et al. (2004) and Bajorski (2011a, 2011b). The first 152 values in the AVIRIS Data represent the spectral radiance values (a spectral curve) for the top left pixel. This is followed by spectral curves of the pixels in the first row, followed by the next row, and so on. (Ref. 1 Bajorski, 2012)

To load the data, run the following code:

Above code uses EBImage package, and can be installed from my previous post.

Why do we need to reduce the dimension of the data?

Before we jump in to our analysis, in case you may ask why? Well sometimes it's just difficult to do analysis on high dimensional data, especially on interpreting it. This is because there are dimensions that aren't significant (like redundancy) which adds to our problem on the analysis. So in order to deal with this, we remove those nuisance dimension and deal with the significant one.

To perform PCA in R, we use the function princomp as seen below:

The structure of princomp consist of a list shown above, we will give description to selected outputs. Others can be found in the documentation of the function by executing ?princomp.
  • sdev - standard deviation, the square root of the eigenvalues $\lambda$ of the variance-covariance matrix $\mathbf{\Sigma}$ of the data, dat.mat;
  • loadings - eigenvectors $\mathbf{e}$ of the variance-covariance matrix $\mathbf{\Sigma}$ of the data, dat.mat;
  • scores - the principal component scores.
Recall that the objective of PCA is to find for a linear combination $Y=\mathbf{u}^T\mathbf{X}$ that will maximize the variance $Var(Y)$. So that from the output, the estimate of the components of $\mathbf{u}$ is the entries of the loadings which is a matrix of eigenvectors, where the columns corresponds to the eigenvectors of the sequence of principal components, that is if the first principal component is given by $Y_1=\mathbf{u}_1^T\mathbf{X}$, then the estimate of $\mathbf{u}_1$ which is $\mathbf{e}_1$ (eigenvector) is the set of coefficients obtained from the first column of the loadings. The explained variability of the first principal component is the square of the first standard deviation sdev, the explained variability of the second principal component is the square of the second standard deviation sdev, and so on. Now let's interpret the loadings (coefficients) of the first three principal components. Below is the plot of this,
Base above, the coefficients of the first principal component (PC1) are almost all negative. A closer look, the variability in this principal component is mainly explained by the weighted average of radiance of the spectral bands 35 to 100. Analogously, PC2 mainly represents the variability of the weighted average of radiance of spectral bands 1 to 34. And further, the fluctuation of the coefficients of PC3 makes it difficult to tell on which bands greatly contribute on its variability. Aside from examining the loadings, another way to see the impact of the PCs is through the impact plot where the impact curve $\sqrt{\lambda_j}\mathbf{e}_j$ are plotted, I want you to explore that.

Moving on, let's investigate the percent of variability in $X_i$ explained by the $j$th principal component, below is the formula of this, \begin{equation}\nonumber \frac{\lambda_j\cdot e_{ij}^2}{s_{ii}}, \end{equation} where $s_{ii}$ is the estimated variance of $X_i$. So that below is the percent of explained variability in $X_i$ of the first three principal components including the cumulative percent variability (sum of PC1, PC2, and PC3),
For the variability of the first 33 bands, PC2 takes on about 90 percent of the explained variability as seen in the above plot. And still have great contribution further to 102 to 152 bands. On the other hand, from bands 37 to 100, PC1 explains almost all the variability with PC2 and PC3 explain 0 to 1 percent only. The sum of the percentage of explained variability of these principal components is indicated as orange line in the above plot, which is the cumulative percent variability.

To wrap up this section, here is the percentage of the explained variability of the first 10 PCs.

Table 1: Variability Explained by the First Ten Principal Components for the AVIRIS data.

Above variability were obtained by noting that the variability explained by the principal component is simply the eigenvalue (square of the sdev) of the variance-covariance matrix $\mathbf{\Sigma}$ of the original variable $\mathbf{X}$, hence the percentage of variability explained by the $j$th PC is equal to its corresponding eigenvalue $\lambda_j$ divided by the overall variability which is the sum of the eigenvalues, $\sum_{j=1}^{p}\lambda_j$, as we see in the following code,

Stopping Rules

Given the list of percentage of variability explained by the PCs in Table 1, how many principal components should we take into account that would best represent the variability of the original data? To answer that, we introduce the following stopping rules that will guide us on deciding the number of PCs:
  1. Scree plot;
  2. Simple fare-share;
  3. Broken-stick; and,
  4. Relative broken-stick.
The scree plot is the plot of the variability of the PCs, that is the plot of the eigenvalues. Where we look for an elbow or sudden drop of the eigenvalues on the plot, hence for our example we have
Therefore, we need return the first two principal components based on the elbow shape. However, if the eigenvalues differ by order of magnitude, it is recommended to use the logarithmic scale which is illustrated below,
Unfortunately, sometimes it won't work as we can see here, it's just difficult to determine where the elbow is. The succeeding discussions on the last three stopping rules are based on (Bajorski, 2012). The simple fair-share stopping rule identifies the largest $k$ such that $\lambda_k$ is larger than its fair share, that is larger than $(\lambda_1+\lambda_2+\cdots+\lambda_p)/p$. To illustrate this, consider the following:

Thus, we need to stop at second principal component.

If one was concerned that the above method produces too many principal components, a broken-stick rule could be used. The rule is that it identifies the principal components with largest $k$ such that $\lambda_j/(\lambda_1+\lambda_2+\cdots +\lambda_p)>a_j$, for all $j\leq k$, where \begin{equation}\nonumber a_j = \frac{1}{p}\sum_{i=j}^{p}\frac{1}{i},\quad j =1,\cdots, p. \end{equation} Let's try it,

Above result coincides with the first two stopping rule. The draw back of simple fair-share and broken-stick rules is that it do not work well when the eigenvalues differ by orders of magnitude. In such case, we then use the relative broken-stick rule, where we analyze $\lambda_j$ as the first eigenvalue in the set $\lambda_j\geq \lambda_{j+1}\geq\cdots\geq\lambda_{p}$, where $j < p$. The dimensionality $k$ is chosen as the largest value such that $\lambda_j/(\lambda_j+\cdots +\lambda_p)>b_j$, for all $j\leq k$, where \begin{equation}\nonumber b_j = \frac{1}{p-j+1}\sum_{i=1}^{p-j+1}\frac{1}{i}. \end{equation} Applying this to the data we have,
According to the numerical output, the first 34 principal components are enough to represent the variability of the original data.

Principal Component Scores

The principal component scores is the resulting new data set obtained from the linear combinations $Y_j=\mathbf{e}_j(\mathbf{x}-\bar{\mathbf{x}}), j = 1,\cdots, p$. So that if we use the first three stopping rules, then below is the scores (in image) of PC1 and PC2,
If we base on the relative broken-stick rule then we return the first 34 PCs, and below is the corresponding scores (in image).
Click on the image to zoom in.

Residual Analysis

Of course when doing PCA there are errors to be considered unless one would return all the PCs, but that would not make any sense because why would someone apply PCA when you still take into account all the dimensions? An overview of the errors in PCA without going through the theory is that, the overall error is simply the excluded variability explained by the $k$th to $p$th principal components, $k>j$.


by Unknown ( at December 27, 2015 01:52 AM

R: k-Means Clustering on Imaging

Enough with the theory we recently published, let's take a break and have fun on the application of Statistics used in Data Mining and Machine Learning, the k-Means Clustering.
k-means clustering is a method of vector quantization, originally from signal processing, that is popular for cluster analysis in data mining. k-means clustering aims to partition n observations into k clusters in which each observation belongs to the cluster with the nearest mean, serving as a prototype of the cluster. (Wikipedia, Ref 1.)
We will apply this method to an image, wherein we group the pixels into k different clusters. Below is the image that we are going to use,
Colorful Bird From Wall321
We will utilize the following packages for input and output:
  1. jpeg - Read and write JPEG images; and,
  2. ggplot2 - An implementation of the Grammar of Graphics.

Download and Read the Image

Let's get started by downloading the image to our workspace, and tell R that our data is a JPEG file.

Cleaning the Data

Extract the necessary information from the image and organize this for our computation:

The image is represented by large array of pixels with dimension rows by columns by channels -- red, green, and blue or RGB.


Plot the original image using the following codes:


Apply k-Means clustering on the image:

Plot the clustered colours:

Possible clusters of pixels on different k-Means:

Originalk = 6
Table 1: Different k-Means Clustering.
k = 5k = 4
k = 3k = 2

I suggest you try it!


  1. K-means clustering. Wikipedia. Retrieved September 11, 2014.

by Unknown ( at December 27, 2015 01:52 AM

May 12, 2015

Chris Lawrence

That'll leave a mark

Here’s a phrase you never want to see in print (in a legal decision, no less) pertaining to your academic research: “The IRB process, however, was improperly engaged by the Dartmouth researcher and ignored completely by the Stanford researchers.”

Whole thing here; it’s a doozy.

by Chris Lawrence at May 12, 2015 12:00 AM

April 14, 2015

R you ready?

Beautiful plots while simulating loss in two-part procrustes problem

loss2Today I was working on a two-part procrustes problem and wanted to find out why my minimization algorithm sometimes does not converge properly or renders unexpected results. The loss function to be minimized is

\displaystyle  L(\mathbf{Q},c) = \| c \mathbf{A_1Q} - \mathbf{B_1} \|^2 + \| \mathbf{A_2Q} - \mathbf{B_2} \|^2 \rightarrow min

with \| \cdot \| denoting the Frobenius norm, c is an unknown scalar and \mathbf{Q} an unknown rotation matrix, i.e. \mathbf{Q}^T\mathbf{Q}=\mathbf{I}. \;\mathbf{A_1}, \mathbf{A_2}, \mathbf{B_1}, and \mathbf{B_1} are four real valued matrices. The minimum for c is easily found by setting the partial derivation of L(\mathbf{Q},c) w.r.t c equal to zero.

\displaystyle  c = \frac {tr \; \mathbf{Q}^T \mathbf{A_1}^T \mathbf{B_1}}  { \| \mathbf{A_1} \|^2 }

By plugging c into the loss function L(\mathbf{Q},c) we get a new loss function L(\mathbf{Q}) that only depends on \mathbf{Q}. This is the starting situation.

When trying to find out why the algorithm to minimize L(\mathbf{Q}) did not work as expected, I got stuck. So I decided to conduct a small simulation and generate random rotation matrices to study the relation between the parameter c and the value of the loss function L(\mathbf{Q}). Before looking at the results for the entire two-part procrustes problem from above, let’s visualize the results for the first part of the loss function only, i.e.

\displaystyle  L(\mathbf{Q},c) = \| c \mathbf{A_1Q} - \mathbf{B_1} \|^2 \rightarrow min

Here, c has the same minimum as for the whole formula above. For the simulation I used

\mathbf{A_1}= \begin{pmatrix}  0.0 & 0.4 & -0.5 \\  -0.4 & -0.8 & -0.5 \\  -0.1 & -0.5 & 0.2 \\  \end{pmatrix} \mkern18mu \qquad \text{and} \qquad \mkern36mu \mathbf{B_1}= \begin{pmatrix}  -0.1 & -0.8 & -0.1 \\  0.3 & 0.2 & -0.9 \\  0.1 & -0.3 & -0.5 \\  \end{pmatrix}

as input matrices. Generating many random rotation matrices \mathbf{Q} and plotting c against the value of the loss function yields the following plot.

This is a well behaved relation, for each scaling parameter c the loss is identical. Now let’s look at the full two-part loss function. As input matrices I used

\displaystyle  A1= \begin{pmatrix}  0.0 & 0.4 & -0.5 \\  -0.4 & -0.8 & -0.5 \\  -0.1 & -0.5 & 0.2 \\  \end{pmatrix} \mkern18mu , \mkern36mu B1= \begin{pmatrix}  -0.1 & -0.8 & -0.1 \\  0.3 & 0.2 & -0.9 \\  0.1 & -0.3 & -0.5 \\  \end{pmatrix}
A2= \begin{pmatrix}  0 & 0 & 1 \\  1 & 0 & 0 \\  0 & 1 & 0 \\  \end{pmatrix} \mkern18mu , \mkern36mu B2= \begin{pmatrix}  0 & 0 & 1 \\  1 & 0 & 0 \\  0 & 1 & 0 \\  \end{pmatrix}

and the following R-code.

# trace function
tr <- function(X) sum(diag(X))

# random matrix type 1
rmat_1 <- function(n=3, p=3, min=-1, max=1){
  matrix(runif(n*p, min, max), ncol=p)

# random matrix type 2, sparse
rmat_2 <- function(p=3) {
  diag(p)[, sample(1:p, p)]

# generate random rotation matrix Q. Based on Q find 
# optimal scaling factor c and calculate loss function value
one_sample <- function(n=2, p=2)
  Q <- mixAK::rRotationMatrix(n=1, dim=p) %*%         # random rotation matrix det(Q) = 1
    diag(sample(c(-1,1), p, rep=T))                   # additional reflections, so det(Q) in {-1,1}
  s <- tr( t(Q) %*% t(A1) %*% B1 ) / norm(A1, "F")^2  # scaling factor c
  rss <- norm(s*A1 %*% Q - B1, "F")^2 +               # get residual sum of squares
         norm(A2 %*% Q - B2, "F")^2 
  c(s=s, rss=rss)

# find c and rss or many random rotation matrices
set.seed(10)  # nice case for 3 x 3
n <- 3
p <- 3
A1 <- round(rmat_1(n, p), 1)
B1 <- round(rmat_1(n, p), 1)
A2 <- rmat_2(p)
B2 <- rmat_2(p)

x <- plyr::rdply(40000, one_sample(3,3)) 
plot(x$s, x$rss, pch=16, cex=.4, xlab="c", ylab="L(Q)", col="#00000010")

This time the result turns out to be very different and … beautiful :)

Here, we do not have a one to one relation between the scaling parameter and the loss function any more. I do not quite know what to make of this yet. But for now I am happy that it has aestethic value. Below you find some more beautiful graphics with different matrices as inputs.


by markheckmann at April 14, 2015 04:53 PM

February 24, 2015

Douglas Bates

RCall: Running an embedded R in Julia

I have used R (and S before it) for a couple of decades. In the last few years most of my coding has been in Julia, a language for technical computing that can provide remarkable performance for a dynamically typed language via Just-In-Time (JIT) compilation of functions and via multiple dispatch.

Nonetheless there are facilities in R that I would like to have access to from Julia. I created the RCall package for Julia to do exactly that. This IJulia notebook provides an introduction to RCall.

This is not a novel idea by any means. Julia already has PyCall and JavaCall packages that provide access to Python and to Java. These packages are used extensively and are much more sophisticated than RCall, at present. Many other languages have facilities to run an embedded instance of R. In fact, Python has several such interfaces.

The things I plan to do using RCall is to access datasets from R and R packages, to fit models that are not currently implemented in Julia and to use R graphics, especially the ggplot2 and lattice packages. Unfortunately I am not currently able to start a graphics device from the embedded R but I expect that to be fixed soon.

I can tell you the most remarkable aspect of RCall although it may not mean much if you haven't tried to do this kind of thing. It is written entirely in Julia. There is absolutely no "glue" code written in a compiled language like C or C++. As I said, this may not mean much to you unless you have tried to do something like this, in which case it is astonishing.

by Douglas Bates ( at February 24, 2015 11:05 PM

February 03, 2015

Romain Francois

January 16, 2015

Modern Toolmaking


My package caretEnsemble, for making ensembles of caret models, is now on CRAN.

Check it out, and let me know what you think! (Submit bug reports and feature requests to the issue tracker)

by Unknown ( at January 16, 2015 10:22 PM

January 15, 2015

Gregor Gorjanc

cpumemlog: Monitor CPU and RAM usage of a process (and its children)

Long time no see ...

Today I pushed the cpumemlog script to GitHub Read more about this useful utility at the GitHub site.

by Unknown ( at January 15, 2015 10:16 PM

December 15, 2014

R you ready?

QQ-plots in R vs. SPSS – A look at the differences


We teach two software packages, R and SPSS, in Quantitative Methods 101 for psychology freshman at Bremen University (Germany). Sometimes confusion arises, when the software packages produce different results. This may be due to specifics in the implemention of a method or, as in most cases, to different default settings. One of these situations occurs when the QQ-plot is introduced. Below we see two QQ-plots, produced by SPSS and R, respectively. The data used in the plots were generated by:

x <- sample(0:9, 100, rep=T)    


QQ-plot in SPSS using Blom's method


qqnorm(x, datax=T)      # uses Blom's method by default
qqline(x, datax=T)

There are some obvious differences:

  1. The most obvious one is that the R plot seems to contain more data points than the SPSS plot. Actually, this is not the case. Some data points are plotted on top of each in SPSS while they are spread out vertically in the R plot. The reason for this difference is that SPSS uses a different approach assigning probabilities to the values. We will expore the two approaches below.
  2. The scaling of the y-axis differs. R uses quantiles from the standard normal distribution. SPSS by default rescales these values using the mean and standard deviation from the original data. This allows to directly compare the original and theoretical values. This is a simple linear transformation and will not be explained any further here.
  3. The QQ-lines are not identical. R uses the 1st and 3rd quartile from both distributions to draw the line. This is different in SPSS where of a line is drawn for identical values on both axes. We will expore the differences below.

QQ-plots from scratch

To get a better understanding of the difference we will build the R and SPSS-flavored QQ-plot from scratch.

R type

In order to calculate theoretical quantiles corresponding to the observed values, we first need to find a way to assign a probability to each value of the original data. A lot of different approaches exist for this purpose (for an overview see e.g. Castillo-Gutiérrez, Lozano-Aguilera, & Estudillo-Martínez, 2012b). They usually build on the ranks of the observed data points to calculate corresponding p-values, i.e. the plotting positions for each point. The qqnorm function uses two formulae for this purpose, depending on the number of observations n (Blom’s mfethod, see ?qqnorm; Blom, 1958). With r being the rank, for n > 10 it will use the formula p = (r - 1/2) / n, for n \leq 10 the formula p = (r - 3/8) / (n + 1/4) to determine the probability value p for each observation (see the help files for the functions qqnorm and ppoint). For simplicity reasons, we will only implement the n > 10 case here.

n <- length(x)          # number of observations
r <- order(order(x))    # order of values, i.e. ranks without averaged ties
p <- (r - 1/2) / n      # assign to ranks using Blom's method
y <- qnorm(p)           # theoretical standard normal quantiles for p values
plot(x, y)              # plot empirical against theoretical values

Before we take at look at the code, note that our plot is identical to the plot generated by qqnorm above, except that the QQ-line is missing. The main point that makes the difference between R and SPSS is found in the command order(order(x)). The command calculates ranks for the observations using ordinal ranking. This means that all observations get different ranks and no average ranks are calculated for ties, i.e. for observations with equal values. Another approach would be to apply fractional ranking and calculate average values for ties. This is what the function rank does. The following codes shows the difference between the two approaches to assign ranks.

v <- c(1,1,2,3,3)
order(order(v))     # ordinal ranking used by R
## [1] 1 2 3 4 5
rank(v)             # fractional ranking used by SPSS
## [1] 1.5 1.5 3.0 4.5 4.5

R uses ordinal ranking and SPSS uses fractional ranking by default to assign ranks to values. Thus, the positions do not overlap in R as each ordered observation is assigned a different rank and therefore a different p-value. We will pick up the second approach again later, when we reproduce the SPSS-flavored plot in R.1

The second difference between the plots concerned the scaling of the y-axis and was already clarified above.

The last point to understand is how the QQ-line is drawn in R. Looking at the probs argument of qqline reveals that it uses the 1st and 3rd quartile of the original data and theoretical distribution to determine the reference points for the line. We will draw the line between the quartiles in red and overlay it with the line produced by qqline to see if our code is correct.

plot(x, y)                      # plot empirical against theoretical values
ps <- c(.25, .75)               # reference probabilities
a <- quantile(x, ps)            # empirical quantiles
b <- qnorm(ps)                  # theoretical quantiles
lines(a, b, lwd=4, col="red")   # our QQ line in red
qqline(x, datax=T)              # R QQ line

The reason for different lines in R and SPSS is that several approaches to fitting a straight line exist (for an overview see e.g. Castillo-Gutiérrez, Lozano-Aguilera, & Estudillo-Martínez, 2012a). Each approach has different advantages. The method used by R is more robust when we expect values to diverge from normality in the tails, and we are primarily interested in the normality of the middle range of our data. In other words, the method of fitting an adequate QQ-line depends on the purpose of the plot. An explanation of the rationale of the R approach can e.g. be found here.

SPSS type

The default SPSS approach also uses Blom’s method to assign probabilities to ranks (you may choose other methods is SPSS) and differs from the one above in the following aspects:

  • a) As already mentioned, SPSS uses ranks with averaged ties (fractional rankings) not the plain order ranks (ordinal ranking) as in R to derive the corresponding probabilities for each data point. The rest of the code is identical to the one above, though I am not sure if SPSS distinguishes between the n  10 case.
  • b) The theoretical quantiles are scaled to match the estimated mean and standard deviation of the original data.
  • c) The QQ-line goes through all quantiles with identical values on the x and y axis.
n <- length(x)                # number of observations
r <- rank(x)                  # a) ranks using fractional ranking (averaging ties)
p <- (r - 1/2) / n            # assign to ranks using Blom's method
y <- qnorm(p)                 # theoretical standard normal quantiles for p values
y <- y * sd(x) + mean(x)      # b) transform SND quantiles to mean and sd from original data
plot(x, y)                    # plot empirical against theoretical values

Lastly, let us add the line. As the scaling of both axes is the same, the line goes through the origin with a slope of 1.

abline(0,1)                   # c) slope 0 through origin

The comparison to the SPSS output shows that they are (visually) identical.

Function for SPSS-type QQ-plot

The whole point of this demonstration was to pinpoint and explain the differences between a QQ-plot generated in R and SPSS, so it will no longer be a reason for confusion. Note, however, that SPSS offers a whole range of options to generate the plot. For example, you can select the method to assign probabilities to ranks and decide how to treat ties. The plots above used the default setting (Blom’s method and averaging across ties). Personally I like the SPSS version. That is why I implemented the function qqnorm_spss in the ryouready package, that accompanies the course. The formulae for the different methods to assign probabilities to ranks can be found in Castillo-Gutiérrez et al. (2012b). The implentation is a preliminary version that has not yet been thoroughly tested. You can find the code here. Please report any bugs or suggestions for improvements (which are very welcome) in the github issues section.

install_github("markheckmann/ryouready")                # install from github repo
library(ryouready)                                      # load package
qq <- qqnorm_spss(x, method=1, ties.method="average")   # Blom's method with averaged ties
plot(qq)                                                # generate QQ-plot
ggplot(qq)                                              # use ggplot2 to generate QQ-plot


  1. Technical sidenote: Internally, qqnorm uses the function ppoints to generate the p-values. Type in stats:::qqnorm.default to the console to have a look at the code. 

by markheckmann at December 15, 2014 08:55 AM

October 20, 2014

Modern Toolmaking

For faster R on a mac, use veclib

Update: The links to all my github gists on blogger are broken, and I can't figure out how to fix them.  If you know how to insert gitub gists on a dynamic blogger template, please let me known.

In the meantime, here are instructions with links to the code:
First of all, use homebrew to compile openblas.  It's easy!  Second of all, you can also use homebrew to install R! (But maybe stick with the CRAN version unless you really want to compile your own R binary)

To use openblas with R, follow these instructions:

To use veclib with R, follow these intructions:


Inspired by this post, I decided to try using OpenBLAS for R on my mac.  However, it turns out there's a simpler option, using the vecLib BLAS library, which is provided by Apple as part of the accelerate framework.

If you are using R 2.15, follow these instructions to change your BLAS from the default to vecLib:

However, as noted in r-sig-mac, these instructions do not work for R 3.0.  You have to directly link to the accelerate framework's version of vecLib:

Finally, test your new blas using this script:

On my system (a retina macbook pro), the default BLAS takes 141 seconds and vecLib takes 43 seconds, which is a significant speedup.  If you plan to use vecLib, note the following warning from the R development team "Although fast, it is not under our control and may possibly deliver inaccurate results."

So far, I have not encountered any issues using vecLib, but it's only been a few hours :-).

UPDATE: you can also install OpenBLAS on a mac:

If you do this, make sure to change the directories to point to the correct location on your system  (e.g. change /users/zach/source to whatever directory you clone the git repo into).  On my system, the benchmark script takes ~41 seconds when using openBLAS, which is a small but significant speedup.

by Unknown ( at October 20, 2014 04:24 PM

September 19, 2014

Chris Lawrence

What could a federal UK look like?

Assuming that the “no” vote prevails in the Scottish independence referendum, the next question for the United Kingdom is to consider constitutional reform to implement a quasi-federal system and resolve the West Lothian question once and for all. In some ways, it may also provide an opportunity to resolve the stalled reform of the upper house as well. Here’s the rough outline of a proposal that might work.

  • Devolve identical powers to England, Northern Ireland, Scotland, and Wales, with the proviso that local self-rule can be suspended if necessary by the federal legislature (by a supermajority).

  • The existing House of Commons becomes the House of Commons for England, which (along with the Sovereign) shall comprise the English Parliament. This parliament would function much as the existing devolved legislatures in Scotland and Wales; the consociational structure of the Northern Ireland Assembly (requiring double majorities) would not be replicated.

  • The House of Lords is abolished, and replaced with a directly-elected Senate of the United Kingdom. The Senate will have authority to legislate on the non-devolved powers (in American parlance, “delegated” powers) such as foreign and European Union affairs, trade and commerce, national defense, and on matters involving Crown dependencies and territories, the authority to legislate on devolved matters in the event self-government is suspended in a constituent country, and dilatory powers including a qualified veto (requiring a supermajority) over the legislation proposed by a constituent country’s parliament. The latter power would effectively replace the review powers of the existing House of Lords; it would function much as the Council of Revision in Madison’s original plan for the U.S. Constitution.

    As the Senate will have relatively limited powers, it need not be as large as the existing Lords or Commons. To ensure the countries other than England have a meaningful voice, given that nearly 85% of the UK’s population is in England, two-thirds of the seats would be allocated proportionally based on population and one-third allocated equally to the four constituent countries. This would still result in a chamber with a large English majority (around 64.4%) but nonetheless would ensure the other three countries would have meaningful representation as well.

by Chris Lawrence at September 19, 2014 12:00 AM

June 18, 2014

Chris Lawrence

Soccer queries answered

Kevin Drum asks a bunch of questions about soccer:

  1. Outside the penalty area there’s a hemisphere about 20 yards wide. I can’t recall ever seeing it used for anything. What’s it for?
  2. On several occasions, I’ve noticed that if the ball goes out of bounds at the end of stoppage time, the referee doesn’t whistle the match over. Instead, he waits for the throw-in, and then immediately whistles the match over. What’s the point of this?
  3. Speaking of stoppage time, how has it managed to last through the years? I know, I know: tradition. But seriously. Having a timekeeper who stops the clock for goals, free kicks, etc. has lots of upside and no downside. Right? It wouldn’t change the game in any way, it would just make timekeeping more accurate, more consistent, and more transparent for the fans and players. Why keep up the current pretense?
  4. What’s the best way to get a better sense of what’s a foul and what’s a legal tackle? Obviously you can’t tell from the players’ reactions, since they all writhe around like landed fish if they so much as trip over their own shoelaces. Reading the rules provides the basics, but doesn’t really help a newbie very much. Maybe a video that shows a lot of different tackles and explains why each one is legal, not legal, bookable, etc.?

The first one’s easy: there’s a general rule that no defensive player can be within 10 yards of the spot of a direct free kick. A penalty kick (which is a type of direct free kick) takes place in the 18-yard box, and no players other than the player taking the kick and the goalkeeper are allowed in the box. However, owing to geometry, the 18 yard box and the 10 yard exclusion zone don’t fully coincide, hence the penalty arc. (That’s also why there are two tiny hash-marks on the goal line and side line 10 yards from the corner flag. And why now referees have a can of shaving cream to mark the 10 yards for other free kicks, one of the few MLS innovations that has been a good idea.)

Second one’s also easy: the half and the game cannot end while the ball is out of play.

Third one’s harder. First, keeping time inexactly forestalls the silly premature celebrations that are common in most US sports. You’d never see the Stanford-Cal play happen in a soccer game. Second, it allows some slippage for short delays and doesn’t require exact timekeeping; granted, this was more valuable before instant replays and fourth officials, but most US sports require a lot of administrative record-keeping by ancillary officials. A soccer game can be played with one official (and often is, particularly at the amateur level) without having to change timing rules;* in developing countries in particular this lowers the barriers to entry for the sport (along with the low equipment requirements) without changing the nature of the game appreciably. Perhaps most importantly, if the clock was allowed to stop regularly it would create an excuse for commercial timeouts and advertising breaks, which would interrupt the flow of the game and potentially reduce the advantages of better-conditioned and more skilled athletes. (MLS tried this, along with other exciting American ideas like “no tied games,” and it was as appealing to actual soccer fans as ketchup on filet mignon would be to a foodie, and perhaps more importantly didn’t make any non-soccer fans watch.)

Fourth, the key distinction is usually whether there was an obvious attempt to play the ball; in addition, in the modern game, even some attempts to play the ball are considered inherently dangerous (tackling from behind, many sliding tackles, etc.) and therefore are fouls even if they are successful in getting more ball than human.

* To call offside, you’d also probably need what in my day we called a “linesman.”

by Chris Lawrence at June 18, 2014 12:00 AM

May 07, 2014

Chris Lawrence

The mission and vision thing

Probably the worst-kept non-secret is that the next stage of the institutional evolution of my current employer is to some ill-defined concept of “university status,” which mostly involves the establishment of some to-be-determined master’s degree programs. In the context of the University System of Georgia, it means a small jump from the “state college” prestige tier (a motley collection of schools that largely started out as two-year community colleges and transfer institutions) to the “state university” tier (which is where most of the ex-normal schools hang out these days). What is yet to be determined is how that transition will affect the broader institution that will be the University of Middle Georgia.* People on high are said to be working on these things; in any event, here are my assorted random thoughts on what might be reasonable things to pursue:

  • Marketing and positioning: Unlike the situation facing many of the other USG institutions, the population of the two anchor counties of our core service area (Bibb and Houston) is growing, and Houston County in particular has a statewide reputation for the quality of its public school system. Rather than conceding that the most prepared students from these schools will go to Athens or Atlanta or Valdosta, we should strongly market our institutional advantages over these more “prestigious” institutions, particularly in terms of the student experience in the first two years and the core curriculum: we have no large lecture courses, no teaching assistants, no lengthy bus rides to and from class every day, and the vast majority of the core is taught by full-time faculty with terminal degrees. Not to mention costs to students are much lower, particularly in the case of students who do not qualify for need-based aid. Even if we were to “lose” these students as transfers to the top-tier institutions after 1–4 semesters, we’d still benefit from the tuition and fees they bring in and we would not be penalized in the upcoming state performance funding formula. Dual enrollment in Warner Robins in particular is an opportunity to showcase our institution as a real alternative for better prepared students rather than a safety school.
  • Comprehensive offerings at the bachelor’s level: As a state university, we will need to offer a comprehensive range of options for bachelor’s students to attract and retain students, both traditional and nontraditional. In particular, B.S. degrees in political science and sociology with emphasis in applied empirical skills would meet public and private employer demand for workers who have research skills and the ability to collect, manage, understand, and use data appropriately. There are other gaps in the liberal arts and sciences as well that need to be addressed to become a truly comprehensive state university.
  • Create incentives to boost the residential population: The college currently has a heavy debt burden inherited from the overbuilding of dorms at the Cochran campus. We need to identify ways to encourage students to live in Cochran, which may require public-private partnerships to try to build a “college town” atmosphere in the community near campus. We also need to work with wireless providers like Sprint and T-Mobile to ensure that students from the “big city” can fully use their cell phones and tablets in Cochran and Eastman without roaming fees or changing wireless providers.
  • Tie the institution more closely to the communities we serve: This includes both physical ties and psychological ties. The Macon campus in particular has poor physical links to the city itself for students who might walk or ride bicycles; extending the existing bike/walking trail from Wesleyan to the Macon campus should be a priority, as should pedestrian access and bike facilities along Columbus Road. Access to the Warner Robins campus is somewhat better but still could be improved. More generally, the institution is perceived as an afterthought or alternative of last resort in the community. Improving this situation and perception among community leaders and political figures may require a physical presence in or near downtown Macon, perhaps in partnership with the GCSU Graduate Center.

* There is no official name-in-waiting, but given that our former interim president seemed to believe he could will this name into existence by repeating it enough I’ll stick with it. The straw poll of faculty trivia night suggests that it’s the least bad option available, which inevitably means the regents will choose something else instead (if the last name change is anything to go by).

by Chris Lawrence at May 07, 2014 12:00 AM

February 17, 2014

Seth Falcon

Have Your SHA and Bcrypt Too


I've been putting off sharing this idea because I've heard the rumors about what happens to folks who aren't security experts when they post about security on the internet. If this blog is replaced with cat photos and rainbows, you'll know what happened.

The Sad Truth

It's 2014 and chances are you have accounts on websites that are not properly handling user passwords. I did no research to produce the following list of ways passwords are mishandled in decreasing order of frequency:

  1. Site uses a fast hashing algorithm, typically SHA1(salt + plain-password).
  2. Site doesn't salt password hashes
  3. Site stores raw passwords

We know that sites should be generating secure random salts and using an established slow hashing algorithm (bcrypt, scrypt, or PBKDF2). Why are sites not doing this?

While security issues deserve a top spot on any site's priority list, new features often trump addressing legacy security concerns. The immediacy of the risk is hard to quantify and it's easy to fall prey to a "nothing bad has happened yet, why should we change now" attitude. It's easy for other bugs, features, or performance issues to win out when measured by immediate impact. Fixing security or other "legacy" issues is the Right Thing To Do and often you will see no measurable benefit from the investment. It's like having insurance. You don't need it until you do.

Specific to the improper storage of user password data is the issue of the impact to a site imposed by upgrading. There are two common approaches to upgrading password storage. You can switch cold turkey to the improved algorithms and force password resets on all of your users. Alternatively, you can migrate incrementally such that new users and any user who changes their password gets the increased security.

The cold turkey approach is not a great user experience and sites might choose to delay an upgrade to avoid admitting to a weak security implementation and disrupting their site by forcing password resets.

The incremental approach is more appealing, but the security benefit is drastically diminished for any site with a substantial set of existing users.

Given the above migration choices, perhaps it's (slightly) less surprising that businesses choose to prioritize other work ahead of fixing poorly stored user password data.

The Idea

What if you could upgrade a site so that both new and existing users immediately benefited from the increased security, but without the disruption of password resets? It turns out that you can and it isn't very hard.

Consider a user table with columns:


Where the hashed_pass column is computed using a weak fast algorithm, for example SHA1(salt + plain_pass).

The core of the idea is to apply a proper algorithm on top of the data we already have. I'll use bcrypt to make the discussion concrete. Add columns to the user table as follows:


Process the existing user table by computing bcrypt(salt2 + hashed_pass) and storing the result in the hashed_pass column (overwriting the less secure value); save the new salt value to salt2 and set hash_type to bycrpt+sha1.

To verify a user where hash_type is bcrypt+sha1, compute bcrypt(salt2 + SHA1(salt + plain_pass)) and compare to the hashed_pass value. Note that bcrypt implementations encode the salt as a prefix of the hashed value so you could avoid the salt2 column, but it makes the idea easier to explain to have it there.

You can take this approach further and have any user that logs in (as well as new users) upgrade to a "clean" bcrypt only algorithm since you can now support different verification algorithms using hash_type. With the proper application code changes in place, the upgrade can be done live.

This scheme will also work for sites storing non-salted password hashes as well as those storing plain text passwords (THE HORROR).

Less Sadness, Maybe

Perhaps this approach makes implementing a password storage security upgrade more palatable and more likely to be prioritized. And if there's a horrible flaw in this approach, maybe you'll let me know without turning this blog into a tangle of cat photos and rainbows.

February 17, 2014 07:08 PM

December 26, 2013

Seth Falcon

A Rebar Plugin for Locking Deps: Reproducible Erlang Project Builds For Fun and Profit

What's this lock-deps of which you speak?

If you use rebar to generate an OTP release project and want to have reproducible builds, you need the rebar_lock_deps_plugin plugin. The plugin provides a lock-deps command that will generate a rebar.config.lock file containing the complete flattened set of project dependencies each pegged to a git SHA. The lock file acts similarly to Bundler's Gemfile.lock file and allows for reproducible builds (*).

Without lock-deps you might rely on the discipline of using a tag for all of your application's deps. This is insufficient if any dep depends on something not specified as a tag. It can also be a problem if a third party dep doesn't provide a tag. Generating a rebar.config.lock file solves these issues. Moreover, using lock-deps can simplify the work of putting together a release consisting of many of your own repos. If you treat the master branch as shippable, then rather than tagging each subproject and updating rebar.config throughout your project's dependency chain, you can run get-deps (without the lock file), compile, and re-lock at the latest versions throughout your project repositories.

The reproducibility of builds when using lock-deps depends on the SHAs captured in rebar.config.lock. The plugin works by scanning the cloned repos in your project's deps directory and extracting the current commit SHA. This works great until a repository's history is rewritten with a force push. If you really want reproducible builds, you need to not nuke your SHAs and you'll need to fork all third party repos to ensure that someone else doesn't screw you over in this fashion either. If you make a habit of only depending on third party repos using a tag, assume that upstream maintainers are not completely bat shit crazy, and don't force push your master branch, then you'll probably be fine.

Getting Started

Install the plugin in your project by adding the following to your rebar.config file:

%% Plugin dependency
{deps, [
    {rebar_lock_deps_plugin, ".*",
     {git, "git://", {branch, "master"}}}

%% Plugin usage
{plugins, [rebar_lock_deps_plugin]}.

To test it out do:

rebar get-deps
# the plugin has to be compiled so you can use it
rebar compile
rebar lock-deps

If you'd like to take a look at a project that uses the plugin, take a look at CHEF's erchef project.

Bonus features

If you are building an OTP release project using rebar generate then you can use rebar_lock_deps_plugin to enhance your build experience in three easy steps.

  1. Use rebar bump-rel-version version=$BUMP to automate the process of editing rel/reltool.config to update the release version. The argument $BUMP can be major, minor, or patch (default) to increment the specified part of a semver X.Y.Z version. If $BUMP is any other value, it is used as the new version verbatim. Note that this function rewrites rel/reltool.config using ~p. I check-in the reformatted version and maintain the formatting when editing. This way, the general case of a version bump via bump-rel-version results in a minimal diff.

  2. Autogenerate a change summary commit message for all project deps. Assuming you've generated a new lock file and bumped the release version, use rebar commit-release to commit the changes to rebar.config.lock and rel/reltool.config with a commit message that summarizes the changes made to each dependency between the previously locked version and the newly locked version. You can get a preview of the commit message via rebar log-changed-deps.

  3. Finally, create an annotated tag for your new release with rebar tag-release which will read the current version from rel/reltool.config and create an annotated tag named with the version.

The dependencies, they are ordered

Up to version 2.0.1 of rebar_lock_deps_plugin, the dependencies in the generated lock file were ordered alphabetically. This was a side-effect of using filelib:wildcard/1 to list the dependencies in the top-level deps directory. In most cases, the order of the full dependency set does not matter. However, if some of the code in your project uses parse transforms, then it will be important for the parse transform to be compiled and on the code path before attempting to compile code that uses the parse transform.

This issue was recently discovered by a colleague who ran into build issues using the lock file for a project that had recently integrated lager for logging. He came up with the idea of maintaining the order of deps as they appear in the various rebar.config files along with a prototype patch proving out the idea. As of rebar_lock_deps_plugin 3.0.0, the lock-deps command will (mostly) maintain the relative order of dependencies as found in the rebar.config files.

The "mostly" is that when a dep is shared across two subprojects, it will appear in the expected order for the first subproject (based on the ordering of the two subprojects). The deps for the second subproject will not be in strict rebar.config order, but the resulting order should address any compile-time dependencies and be relatively stable (only changing when project deps alter their deps with larger impact when shared deps are introduced or removed).

Digression: fun with dependencies

There are times, as a programmer, when a real-world problem looks like a text book exercise (or an interview whiteboard question). Just the other day at work we had to design some manhole covers, but I digress.

Fixing the order of the dependencies in the generated lock file is (nearly) the same as finding an install order for a set of projects with inter-dependencies. I had some fun coding up the text book solution even though the approach doesn't handle the constraint of respecting the order provided by the rebar.config files. Onward with the digression.

We have a set of "packages" where some packages depend on others and we want to determine an install order such that a package's dependencies are always installed before the package. The set of packages and the relation "depends on" form a directed acyclic graph or DAG. The topological sort of a DAG produces an install order for such a graph. The ordering is not unique. For example, with a single package C depending on A and B, valid install orders are [A, B, C] and [B, A, C].

To setup the problem, we load all of the project dependency information into a proplist mapping each package to a list of its dependencies extracted from the package's rebar.config file.

read_all_deps(Config, Dir) ->
    TopDeps = rebar_config:get(Config, deps, []),
    Acc = [{top, dep_names(TopDeps)}],
    DepDirs = filelib:wildcard(filename:join(Dir, "*")),
    Acc ++ [
     {filename:basename(D), dep_names(extract_deps(D))}
     || D <- DepDirs ].

Erlang's standard library provides the digraph and digraph_utils modules for constructing and operating on directed graphs. The digraph_utils module includes a topsort/1 function which we can make use of for our "exercise". The docs say:

Returns a topological ordering of the vertices of the digraph Digraph if such an ordering exists, false otherwise. For each vertex in the returned list, there are no out-neighbours that occur earlier in the list.

To figure out which way to point the edges when building our graph, consider two packages A and B with A depending on B. We know we want to end up with an install order of [B, A]. Rereading the topsort/1 docs, we must want an edge B => A. With that, we can build our DAG and obtain an install order with the topological sort:

load_digraph(Config, Dir) ->
    AllDeps = read_all_deps(Config, Dir),
    G = digraph:new(),
    Nodes = all_nodes(AllDeps),
    [ digraph:add_vertex(G, N) || N <- Nodes ],
    %% If A depends on B, then we add an edge A <= B
      [ digraph:add_edge(G, Dep, Item)
        || Dep <- DepList ]
      || {Item, DepList} <- AllDeps, Item =/= top ],

%% extract a sorted unique list of all deps
all_nodes(AllDeps) ->
    lists:usort(lists:foldl(fun({top, L}, Acc) ->
                                    L ++ Acc;
                               ({K, L}, Acc) ->
                                    [K|L] ++ Acc
                            end, [], AllDeps)).

The digraph module manages graphs using ETS giving it a convenient API, though one that feels un-erlang-y in its reliance on side-effects.

The above gives an install order, but doesn't take into account the relative order of deps as specified in the rebar.config files. The solution implemented in the plugin is a bit less fancy, recursing over the deps and maintaining the desired ordering. The only tricky bit being that shared deps are ignored until the end and the entire linearized list is de-duped which required a . Here's the code:

order_deps(AllDeps) ->
    Top = proplists:get_value(top, AllDeps),
    order_deps(lists:reverse(Top), AllDeps, []).

order_deps([], _AllDeps, Acc) ->
order_deps([Item|Rest], AllDeps, Acc) ->
    ItemDeps = proplists:get_value(Item, AllDeps),
    order_deps(lists:reverse(ItemDeps) ++ Rest, AllDeps, [Item | Acc]).

de_dup(AccIn) ->
    WithIndex = lists:zip(AccIn, lists:seq(1, length(AccIn))),
    UWithIndex = lists:usort(fun({A, _}, {B, _}) ->
                                     A =< B
                             end, WithIndex),
    Ans0 = lists:sort(fun({_, I1}, {_, I2}) ->
                              I1 =< I2
                      end, UWithIndex),
    [ V || {V, _} <- Ans0 ].

Conclusion and the end of this post

The great thing about posting to your blog is, you don't have to have a proper conclusion if you don't want to.

December 26, 2013 04:20 PM

December 09, 2013

Leandro Penz

Probabilistic bug hunting

Probabilistic bug hunting

Have you ever run into a bug that, no matter how careful you are trying to reproduce it, it only happens sometimes? And then, you think you've got it, and finally solved it - and tested a couple of times without any manifestation. How do you know that you have tested enough? Are you sure you were not "lucky" in your tests?

In this article we will see how to answer those questions and the math behind it without going into too much detail. This is a pragmatic guide.

The Bug

The following program is supposed to generate two random 8-bit integer and print them on stdout:

  #include <stdio.h>
  #include <fcntl.h>
  #include <unistd.h>
  /* Returns -1 if error, other number if ok. */
  int get_random_chars(char *r1, char*r2)
  	int f = open("/dev/urandom", O_RDONLY);
  	if (f < 0)
  		return -1;
  	if (read(f, r1, sizeof(*r1)) < 0)
  		return -1;
  	if (read(f, r2, sizeof(*r2)) < 0)
  		return -1;
  	return *r1 & *r2;
  int main(void)
  	char r1;
  	char r2;
  	int ret;
  	ret = get_random_chars(&r1, &r2);
  	if (ret < 0)
  		fprintf(stderr, "error");
  		printf("%d %d\n", r1, r2);
  	return ret < 0;

On my architecture (Linux on IA-32) it has a bug that makes it print "error" instead of the numbers sometimes.

The Model

Every time we run the program, the bug can either show up or not. It has a non-deterministic behaviour that requires statistical analysis.

We will model a single program run as a Bernoulli trial, with success defined as "seeing the bug", as that is the event we are interested in. We have the following parameters when using this model:

  • \(n\): the number of tests made;
  • \(k\): the number of times the bug was observed in the \(n\) tests;
  • \(p\): the unknown (and, most of the time, unknowable) probability of seeing the bug.

As a Bernoulli trial, the number of errors \(k\) of running the program \(n\) times follows a binomial distribution \(k \sim B(n,p)\). We will use this model to estimate \(p\) and to confirm the hypotheses that the bug no longer exists, after fixing the bug in whichever way we can.

By using this model we are implicitly assuming that all our tests are performed independently and identically. In order words: if the bug happens more ofter in one environment, we either test always in that environment or never; if the bug gets more and more frequent the longer the computer is running, we reset the computer after each trial. If we don't do that, we are effectively estimating the value of \(p\) with trials from different experiments, while in truth each experiment has its own \(p\). We will find a single value anyway, but it has no meaning and can lead us to wrong conclusions.

Physical analogy

Another way of thinking about the model and the strategy is by creating a physical analogy with a box that has an unknown number of green and red balls:

  • Bernoulli trial: taking a single ball out of the box and looking at its color - if it is red, we have observed the bug, otherwise we haven't. We then put the ball back in the box.
  • \(n\): the total number of trials we have performed.
  • \(k\): the total number of red balls seen.
  • \(p\): the total number of red balls in the box divided by the total number of green balls in the box.

Some things become clearer when we think about this analogy:

  • If we open the box and count the balls, we can know \(p\), in contrast with our original problem.
  • Without opening the box, we can estimate \(p\) by repeating the trial. As \(n\) increases, our estimate for \(p\) improves. Mathematically: \[p = \lim_{n\to\infty}\frac{k}{n}\]
  • Performing the trials in different conditions is like taking balls out of several different boxes. The results tell us nothing about any single box.

Estimating \(p\)

Before we try fixing anything, we have to know more about the bug, starting by the probability \(p\) of reproducing it. We can estimate this probability by dividing the number of times we see the bug \(k\) by the number of times we tested for it \(n\). Let's try that with our sample bug:

  $ ./hasbug
  67 -68
  $ ./hasbug
  79 -101
  $ ./hasbug

We know from the source code that \(p=25%\), but let's pretend that we don't, as will be the case with practically every non-deterministic bug. We tested 3 times, so \(k=1, n=3 \Rightarrow p \sim 33%\), right? It would be better if we tested more, but how much more, and exactly what would be better?

\(p\) precision

Let's go back to our box analogy: imagine that there are 4 balls in the box, one red and three green. That means that \(p = 1/4\). What are the possible results when we test three times?

Red balls Green balls \(p\) estimate
0 3 0%
1 2 33%
2 1 66%
3 0 100%

The less we test, the smaller our precision is. Roughly, \(p\) precision will be at most \(1/n\) - in this case, 33%. That's the step of values we can find for \(p\), and the minimal value for it.

Testing more improves the precision of our estimate.

\(p\) likelihood

Let's now approach the problem from another angle: if \(p = 1/4\), what are the odds of seeing one error in four tests? Let's name the 4 balls as 0-red, 1-green, 2-green and 3-green:

The table above has all the possible results for getting 4 balls out of the box. That's \(4^4=256\) rows, generated by this python script. The same script counts the number of red balls in each row, and outputs the following table:

k rows %
0 81 31.64%
1 108 42.19%
2 54 21.09%
3 12 4.69%
4 1 0.39%

That means that, for \(p=1/4\), we see 1 red ball and 3 green balls only 42% of the time when getting out 4 balls.

What if \(p = 1/3\) - one red ball and two green balls? We would get the following table:

k rows %
0 16 19.75%
1 32 39.51%
2 24 29.63%
3 8 9.88%
4 1 1.23%

What about \(p = 1/2\)?

k rows %
0 1 6.25%
1 4 25.00%
2 6 37.50%
3 4 25.00%
4 1 6.25%

So, let's assume that you've seen the bug once in 4 trials. What is the value of \(p\)? You know that can happen 42% of the time if \(p=1/4\), but you also know it can happen 39% of the time if \(p=1/3\), and 25% of the time if \(p=1/2\). Which one is it?

The graph bellow shows the discrete likelihood for all \(p\) percentual values for getting 1 red and 3 green balls:

The fact is that, given the data, the estimate for \(p\) follows a beta distribution \(Beta(k+1, n-k+1) = Beta(2, 4)\) (1) The graph below shows the probability distribution density of \(p\):

The R script used to generate the first plot is here, the one used for the second plot is here.

Increasing \(n\), narrowing down the interval

What happens when we test more? We obviously increase our precision, as it is at most \(1/n\), as we said before - there is no way to estimate that \(p=1/3\) when we only test twice. But there is also another effect: the distribution for \(p\) gets taller and narrower around the observed ratio \(k/n\):

Investigation framework

So, which value will we use for \(p\)?

  • The smaller the value of \(p\), the more we have to test to reach a given confidence in the bug solution.
  • We must, then, choose the probability of error that we want to tolerate, and take the smallest value of \(p\) that we can.

    A usual value for the probability of error is 5% (2.5% on each side).
  • That means that we take the value of \(p\) that leaves 2.5% of the area of the density curve out on the left side. Let's call this value \(p_{min}\).
  • That way, if the observed \(k/n\) remains somewhat constant, \(p_{min}\) will raise, converging to the "real" \(p\) value.
  • As \(p_{min}\) raises, the amount of testing we have to do after fixing the bug decreases.

By using this framework we have direct, visual and tangible incentives to test more. We can objectively measure the potential contribution of each test.

In order to calculate \(p_{min}\) with the mentioned properties, we have to solve the following equation:

\[\sum_{k=0}^{k}{n\choose{k}}p_{min} ^k(1-p_{min})^{n-k}=\frac{\alpha}{2} \]

\(alpha\) here is twice the error we want to tolerate: 5% for an error of 2.5%.

That's not a trivial equation to solve for \(p_{min}\). Fortunately, that's the formula for the confidence interval of the binomial distribution, and there are a lot of sites that can calculate it:

Is the bug fixed?

So, you have tested a lot and calculated \(p_{min}\). The next step is fixing the bug.

After fixing the bug, you will want to test again, in order to confirm that the bug is fixed. How much testing is enough testing?

Let's say that \(t\) is the number of times we test the bug after it is fixed. Then, if our fix is not effective and the bug still presents itself with a probability greater than the \(p_{min}\) that we calculated, the probability of not seeing the bug after \(t\) tests is:

\[\alpha = (1-p_{min})^t \]

Here, \(\alpha\) is also the probability of making a type I error, while \(1 - \alpha\) is the statistical significance of our tests.

We now have two options:

  • arbitrarily determining a standard statistical significance and testing enough times to assert it.
  • test as much as we can and report the achieved statistical significance.

Both options are valid. The first one is not always feasible, as the cost of each trial can be high in time and/or other kind of resources.

The standard statistical significance in the industry is 5%, we recommend either that or less.

Formally, this is very similar to a statistical hypothesis testing.

Back to the Bug

Testing 20 times

This file has the results found after running our program 5000 times. We must never throw out data, but let's pretend that we have tested our program only 20 times. The observed \(k/n\) ration and the calculated \(p_{min}\) evolved as shown in the following graph:

After those 20 tests, our \(p_{min}\) is about 12%.

Suppose that we fix the bug and test it again. The following graph shows the statistical significance corresponding to the number of tests we do:

In words: we have to test 24 times after fixing the bug to reach 95% statistical significance, and 35 to reach 99%.

Now, what happens if we test more before fixing the bug?

Testing 5000 times

Let's now use all the results and assume that we tested 5000 times before fixing the bug. The graph bellow shows \(k/n\) and \(p_{min}\):

After those 5000 tests, our \(p_{min}\) is about 23% - much closer to the real \(p\).

The following graph shows the statistical significance corresponding to the number of tests we do after fixing the bug:

We can see in that graph that after about 11 tests we reach 95%, and after about 16 we get to 99%. As we have tested more before fixing the bug, we found a higher \(p_{min}\), and that allowed us to test less after fixing the bug.

Optimal testing

We have seen that we decrease \(t\) as we increase \(n\), as that can potentially increases our lower estimate for \(p\). Of course, that value can decrease as we test, but that means that we "got lucky" in the first trials and we are getting to know the bug better - the estimate is approaching the real value in a non-deterministic way, after all.

But, how much should we test before fixing the bug? Which value is an ideal value for \(n\)?

To define an optimal value for \(n\), we will minimize the sum \(n+t\). This objective gives us the benefit of minimizing the total amount of testing without compromising our guarantees. Minimizing the testing can be fundamental if each test costs significant time and/or resources.

The graph bellow shows us the evolution of the value of \(t\) and \(t+n\) using the data we generated for our bug:

We can see clearly that there are some low values of \(n\) and \(t\) that give us the guarantees we need. Those values are \(n = 15\) and \(t = 24\), which gives us \(t+n = 39\).

While you can use this technique to minimize the total number of tests performed (even more so when testing is expensive), testing more is always a good thing, as it always improves our guarantee, be it in \(n\) by providing us with a better \(p\) or in \(t\) by increasing the statistical significance of the conclusion that the bug is fixed. So, before fixing the bug, test until you see the bug at least once, and then at least the amount specified by this technique - but also test more if you can, there is no upper bound, specially after fixing the bug. You can then report a higher confidence in the solution.


When a programmer finds a bug that behaves in a non-deterministic way, he knows he should test enough to know more about the bug, and then even more after fixing it. In this article we have presented a framework that provides criteria to define numerically how much testing is "enough" and "even more." The same technique also provides a method to objectively measure the guarantee that the amount of testing performed provides, when it is not possible to test "enough."

We have also provided a real example (even though the bug itself is artificial) where the framework is applied.

As usual, the source code of this page (R scripts, etc) can be found and downloaded in

December 09, 2013 12:00 AM

December 01, 2013

Gregor Gorjanc

Read line by line of a file in R

Are you using R for data manipulation for later use with other programs, i.e., a workflow something like this:
  1. read data sets from a disk,
  2. modify the data, and
  3. write it back to a disk.
All fine, but of data set is really big, then you will soon stumble on memory issues. If data processing is simple and you can read only chunks, say only line by line, then the following might be useful:

## File
file <- "myfile.txt"
## Create connection
con <- file(description=file, open="r")
## Hopefully you know the number of lines from some other source or
com <- paste("wc -l ", file, " | awk '{ print $1 }'", sep="")
n <- system(command=com, intern=TRUE)
## Loop over a file connection
for(i in 1:n) {
tmp <- scan(file=con, nlines=1, quiet=TRUE)
## do something on a line of data
Created by Pretty R at

by Unknown ( at December 01, 2013 10:55 PM

August 13, 2013

Gregor Gorjanc

Setup up the inverse of additive relationship matrix in R

Additive genetic covariance between individuals is one of the key concepts in (quantitative) genetics. When doing the prediction of additive genetic values for pedigree members, we need the inverse of the so called numerator relationship matrix (NRM) or simply A. Matrix A has off-diagonal entries equal to numerator of Wright's relationship coefficient and diagonal elements equal to 1 + inbreeding coefficient. I have blogged before about setting up such inverse in R using routine from the ASReml-R program or importing the inverse from the CFC program. However, this is not the only way to "skin this cat" in R. I am aware of the following attempts to provide this feature in R for various things (the list is probably incomplete and I would grateful if you point me to other implementations):
  • pedigree R package has function makeA() and makeAinv() with obvious meanings; there is also calcG() if you have a lot of marker data instead of pedigree information; there are also some other very handy functions calcInbreeding(), orderPed(), trimPed(), etc.
  • pedigreemm R package does not have direct implementation to get A inverse, but has all the needed ingredients, which makes the package even more interesting
  • MCMCglmm R package has function inverseA() which works with pedigree or phlyo objects; there are also handy functions such as prunePed(), rbv()sm2asreml(), etc.
  • kinship and kinship2 R packages have function kinship() to setup kinship matrix, which is equal to the half of A; there are also nice functions for plotting pedigrees etc. (see also here)
  • see also a series of R scripts for relationship matrices 
As I described before, the interesting thing is that setting up inverse of A is easier and cheaper than setting up A and inverting it. This is very important for large applications. This is an old result using the following matrix theory. We can decompose symmetric positive definite matrix as A = LU = LL' (Cholesky decomposition) or as A = LDU = LDL' (Generalized Cholesky decomposition), where L (U) is lower (upper) triangular, and D is diagonal matrix. Note that L and U in previous two equations are not the same thing (L from Cholesky is not equal to L from Generalized Cholesky decomposition)! Sorry for sloppy notation. In order to confuse you even more note that Henderson usually wrote A = TDT'. We can even do A = LSSU, where S diagonal is equal to the square root of D diagonal. This can get us back to A = LU = LL' as LSSU = LSSL' = LSS'L' = LS(LS)' = L'L (be ware of sloppy notation)! The inverse rule says that inv(A) = inv(LDU) = inv(U) inv(D) inv(L) = inv(L)' inv(D) inv(L) = inv(L)' inv(S) inv(S) inv(L). I thank to Martin Maechler for pointing out to the last (obviously) bit to me. In Henderson's notation this would be inv(A) = inv(T)' inv(D) inv(T) = inv(T)' inv(S) inv(S) inv(T) Uf ... The important bit is that with NRM (aka A) inv(L) has nice simple structure - it shows the directed graph of additive genetic values in pedigree, while inv(D) tells us about the precision (inverse variance) of additive genetic values given the additive genetic values of parents and therefore depends on knowledge of parents and their inbreeding (the more they are inbred less variation can we expect in their progeny). Both inv(L) and inv(D) are easier to setup.

Packages MCMCglmm and pedigree give us inv(A) directly (we can also get inv(D) in MCMCglmm), but pedigreemm enables us to play around with the above matrix algebra and graph theory. First we need a small example pedigree. Bellow is an example with 10 members and there is also some inbreeding and some individuals have both, one, or no parents known. It is hard to see inbreeding directly from the table, but we will improve that later (see also here).

ped <- data.frame( id=c(  1,   2,   3,   4,   5,   6,   7,   8,   9,  10),
fid=c( NA, NA, 2, 2, 4, 2, 5, 5, NA, 8),
mid=c( NA, NA, 1, NA, 3, 3, 6, 6, NA, 9))

Now we will create an object of a pedigree class and show the A = U'U stuff:

## install.packages(pkgs="pedigreemm")
ped2 <- with(ped, pedigree(sire=fid, dam=mid, label=id))
U <-
A &lt
;- crossprod(U)
round(U, digits=2)
## 10 x 10 sparse Matrix of class "dtCMatrix"
## [1,] 1 . 0.50 . 0.25 0.25 0.25 0.25 . 0.12
## [2,] . 1 0.50 0.50 0.50 0.75 0.62 0.62 . 0.31
## [3,] . . 0.71 . 0.35 0.35 0.35 0.35 . 0.18
## [4,] . . . 0.87 0.43 . 0.22 0.22 . 0.11
## [5,] . . . . 0.71 . 0.35 0.35 . 0.18
## [6,] . . . . . 0.71 0.35 0.35 . 0.18
## [7,] . . . . . . 0.64 . . .
## [8,] . . . . . . . 0.64 . 0.32
## [9,] . . . . . . . . 1 0.50
## [10,] . . . . . . . . . 0.66

## To check
U - chol(A)

round(A, digits=2)
## 10 x 10 sparse Matrix of class "dsCMatrix"
## [1,] 1.00 . 0.50 . 0.25 0.25 0.25 0.25 . 0.12
## [2,] . 1.00 0.50 0.50 0.50 0.75 0.62 0.62 . 0.31
## [3,] 0.50 0.50 1.00 0.25 0.62 0.75 0.69 0.69 . 0.34
## [4,] . 0.50 0.25 1.00 0.62 0.38 0.50 0.50 . 0.25
## [5,] 0.25 0.50 0.62 0.62 1.12 0.56 0.84 0.84 . 0.42
## [6,] 0.25 0.75 0.75 0.38 0.56 1.25 0.91 0.91 . 0.45
## [7,] 0.25 0.62 0.69 0.50 0.84 0.91 1.28 0.88 . 0.44
## [8,] 0.25 0.62 0.69 0.50 0.84 0.91 0.88 1.28 . 0.64
## [9,] . . . . . . . . 1.0 0.50
## [10,] 0.12 0.31 0.34 0.25 0.42 0.45 0.44 0.64 0.5

ote tha
m package uses Matrix classes in order to store only what we need to store, e.g., matrix U is triangular (t in "dtCMatrix") and matrix A is symmetric (s in "dsCMatrix"). To show the generalized Cholesky A = LDU (or using Henderson notation A = TDT') we use gchol() from the bdsmatrix R package. Matrix T shows the "flow" of genes in pedigree.

## install.packages(pkgs="bdsmatrix")
&lt;- gchol(as.matrix(A))
D &lt;- diag(tmp)
(T <- as(as.matrix(tmp), "dtCMatrix"))
## 10 x 10 sparse Matrix of class "dtCMatrix"
## [1,] 1.000 . . . . . . . . .
## [2,] . 1.0000 . . . . . . . .
## [3,] 0.500 0.5000 1.00 . . . . . . .
## [4,] . 0.5000 . 1.000 . . . . . .
## [5,] 0.250 0.5000 0.50 0.500 1.00 . . . . .
## [6,] 0.250 0.7500 0.50 . . 1.00 . . . .
## [7,] 0.250 0.6250 0.50 0.250 0.50 0.50 1 . . .
## [8,] 0.250 0.6250 0.50 0.250 0.50 0.50 . 1.0 . .
## [9,] . . . . . . . . 1.0 .
## [10,] 0.125 0.3125 0.25 0.125 0.25 0.25 . 0.5 0.5 1

## To chec
- T %*% diag(sqrt(D))
L - t(U)
Now the A inverse part (inv(A) = inv(T)' inv(D) inv(T) = inv(T)' inv(S) inv(S) inv(T) using Henderson's notation, note that ). The nice thing is that pedigreemm authors provided functions to get inv(T) and D.

(TInv <- as(ped2, "sparseMatrix"))
## 10 x 10 sparse Matrix of class "dtCMatrix" (unitriangular)
## 1 1.0 . . . . . . . . .
## 2 . 1.0 . . . . . . . .
## 3 -0.5 -0.5 1.0 . . . . . . .
## 4 . -0.5 . 1.0 . . . . . .
## 5 . . -0.5 -0.5 1.0 . . . . .
## 6 . -0.5 -0.5 . . 1.0 . . . .
## 7 . . . . -0.5 -0.5 1 . . .
## 8 . . . . -0.5 -0.5 . 1.0 . .
## 9 . . . . . . . . 1.0 .
## 10 . . . . . . . -0.5 -0.5 1
round(DInv <- Diagonal(x=1/Dmat(ped2)), digits=2)
## 10 x 10 diagonal matrix of class "ddiMatrix"
## [,1] [,2] [,3] [,4] [,5] [,6] [,7] [,8] [,9] [,10]
## [1,] 1 . . . . . . . . .
## [2,] . 1 . . . . . . . .
## [3,] . . 2 . . . . . . .
## [4,] . . . 1.33 . . . . . .
## [5,] . . . . 2 . . . . .
## [6,] . . . . . 2 . . . .
## [7,] . . . . . . 2.46 . . .
## [8,] . . . . . . . 2.46 . .
## [9,] . . . . . . . . 1 .
## [10,] . . . . . . . . . 2.33
round(t(TInv) %*% DInv %*% TInv, digits=2)
## 10 x 10 sparse Matrix of class "dgCMatrix"
## .
und(crossprod(sqrt(DInv) %*% TInv), digits=2)
## 10 x 10 sparse Matrix of class "dsCMatrix"
##  [1,]  1.5  0.50 -1.0  .     .     .     .     .     .     .   
## [2,] 0.5 2.33 -0.5 -0.67 . -1.00 . . . .
## [3,] -1.0 -0.50 3.0 0.50 -1.00 -1.00 . . . .
## [4,] . -0.67 0.5 1.83 -1.00 . . . . .
## [5,] . . -1.0 -1.00 3.23 1.23 -1.23 -1.23 . .
## [6,] . -1.00 -1.0 . 1.23 3.23 -1.23 -1.23 . .
## [7,] . . . . -1.23 -1.23 2.46 . . .
## [8,] . . . . -1.23 -1.23 . 3.04 0.58 -1.16
## [9,] . . . . . . . 0.58 1.58 -1.16
## [10,] . . . . . . . -1.16 -1.16

# T
o c
) - crossprod(sqrt(DInv) %*% TInv)

The second method (using crossprod) is preferred as it leads directly to symmetric matrix (dsCMatrix), which stores only upper or lower triangle. And make sure you do not do crossprod(TInv %*% sqrt(DInv)) as it is the wrong order of matrices.

As promised we will display (plot) pedigree by use of conversion functions of matrix objects to graph objects using the following code. Two examples are provided using the graph and igraph packages. The former does a very good job on this example, but otherwise igraph seems to have much nicer support for editing etc.

## source("")
## biocLite(pkgs=c("graph", "Rgraphviz"))
g <- as(t(TInv), "graph")

## install.packages(pkgs="igraph")
i &l
t;- igraph.from.graphNEL(graphNEL=g)
i)$label <- 1:10
(i, layout=layout.kamada.kawai)
## tkplot(i)

by Unknown ( at August 13, 2013 02:28 PM

July 02, 2013

Gregor Gorjanc

Parse arguments of an R script

R can be used also as a scripting tool. We just need to add shebang in the first line of a file (script):


and then the R code should follow.

Often we want to pass arguments to such a script, which can be collected in the script by the commandArgs() function. Then we need to parse the arguments and conditional on them do something. I came with a rather general way of parsing these arguments using simply these few lines:

## Collect arguments
args <- commandArgs(TRUE)
## Default setting when no arguments passed
if(length(args) < 1) {
args <- c("--help")
## Help section
if("--help" %in% args) {
The R Script
--arg1=someValue - numeric, blah blah
--arg2=someValue - character, blah blah
--arg3=someValue - logical, blah blah
--help - print this text
./test.R --arg1=1 --arg2="
output.txt" --arg3=TRUE \n\n")
## Parse arguments (we expect the form --arg=value)
parseArgs <- function(x) strsplit(sub("^--", "", x), "=")
argsDF <-"rbind", parseArgs(args)))
argsL <- as.list(as.character(argsDF$V2))
names(argsL) <- argsDF$V1
## Arg1 default
if(is.null(args$arg1)) {
## do something
## Arg2 default
if(is.null(args$arg2)) {
## do something
## Arg3 default
if(is.null(args$arg3)) {
## do something
## ... your code here ...
Created by Pretty R at

It is some work, but I find it pretty neat and use it for quite a while now. I do wonder what others have come up for this task. I hope I did not miss some very general solution.

by Unknown ( at July 02, 2013 04:55 PM

March 24, 2013

Romain Francois



This blog is moving to The new one is powered by wordpress and gets a subdomain of

See you there

by romain francois at March 24, 2013 03:52 PM