- Methodology Article
- Open Access
An Eigenvalue test for spatial principal component analysis
- V. Montano^{1}Email authorView ORCID ID profile and
- T. Jombart^{2}
https://doi.org/10.1186/s12859-017-1988-y
© The Author(s). 2017
Received: 1 July 2017
Accepted: 5 December 2017
Published: 16 December 2017
Abstract
Background
The spatial Principal Component Analysis (sPCA, Jombart (Heredity 101:92-103, 2008) is designed to investigate non-random spatial distributions of genetic variation. Unfortunately, the associated tests used for assessing the existence of spatial patterns (global and local test; (Heredity 101:92-103, 2008) lack statistical power and may fail to reveal existing spatial patterns. Here, we present a non-parametric test for the significance of specific patterns recovered by sPCA.
Results
We compared the performance of this new test to the original global and local tests using datasets simulated under classical population genetic models. Results show that our test outperforms the original global and local tests, exhibiting improved statistical power while retaining similar, and reliable type I errors. Moreover, by allowing to test various sets of axes, it can be used to guide the selection of retained sPCA components.
Conclusions
As such, our test represents a valuable complement to the original analysis, and should prove useful for the investigation of spatial genetic patterns.
Keywords
Background
The principal component analysis (PCA; [1, 2]) is one of the most common multivariate approaches in population genetics [3]. Although PCA is not explicitly accounting for spatial information, it has often been used for investigating spatial genetic patterns [4]. As a complement to PCA, the spatial principal component analysis [5] has been introduced to explicitly include spatial information in the analysis of genetic variation, and gain more power for investigating spatial genetic structures.
sPCA finds synthetic variables, the principal components (PCs), which maximise both the genetic variance and the spatial autocorrelation as measured by Moran’s I [6]. As such, PCs can reveal two types of patterns: ‘global’ structures, which correspond to positive autocorrelation typically observed in the presence of patches or clines, and ‘local’ structures, which correspond to negative autocorrelation, whereby neighboring individuals are more genetically distinct than expected at random (for a more detailed explanation on the meaning of global and local structures see [5]). The global and local tests have been developed for detecting the presence of global and local patterns, respectively [5]. Unfortunately, while these tests have robust type I error, they also typically lack power, and can therefore fail to identify existing spatial genetic patterns [5]. Moreover, they can only be used to diagnose the presence or absence of spatial patterns, and are unable to test the significance of specific structures revealed by sPCA axes.
In this paper, we introduce an alternative statistical test which addresses these issues. This approach relies on computing the cumulative sum of a defined set of sPCA eigenvalues as a test statistic, and uses a Monte-Carlo procedure to generate null distributions of the test statistics and approximate p-values. After describing our approach, we compare its performances to the global and local tests using simulated datasets, investigating several standard spatial population genetics models. Our approach is implemented as the function spca_randtest in the package adegenet [7, 8] for the R software [9].
Methods
Test statistic
f _{ i } ^{ + } and f _{ i } ^{ − } become larger in the presence of strong global or local structures in the first i ^{th} global/local PCs. Therefore, they can be used as test statistics against the null hypotheses of absence of global or local structures in these PCs. The expected distribution of f _{ i } ^{ + } and f _{ i } ^{ − } in the absence of spatial structure is not known analytically. Fortunately, it can be approximated using a Monte-Carlo procedure, in which at each permutation individual genotypes are shuffled to be assigned to a different pair of coordinates than in the observed original dataset and f _{ i } ^{ + } and f _{ i } ^{ − } are computed. Note that the original values of the test statistic are also included in these distributions, as the initial spatial configuration is by definition a possible random outcome. The p-values are then computed as the relative frequencies of permuted statistics equal to or greater than the initial value of f _{ i } ^{ + } or f _{ i } ^{ − }.
Simulation study
To assess the performance of our test, we simulated genetic data under three migration models: island (IS) and stepping stone (SS), using the software GenomePop 2.7 [11], and isolation by distance (IBD), using IBDSimV2.0 [12]. We simulated the IS and SS models with 4 populations, each with 25 individuals, and a single population under IBD with 100 individuals. 200 unlinked biallelic diploid loci (or single nucleotide polymorphisms; SNPs) were simulated. Populations evolved under constant effective population size θ = 20, and interchanged migrants at three different symmetric and homogeneous rates (0.005, 0.01, and 0.1). We performed 100 independent runs for each of the three migration rates, for a total of 300 simulated dataset per migration model. An example of input file for GenomePop 2.7 and IBDSimV2.0 are included as Additional files 1 and 2.
We tested 100 simulations each for all the 30 sets of geographic coordinates (random, positive and negative), for each of the three migration rates (0.005, 0.01 and 0.1), for each of the three migration models (IS, SS, IBD; total of 9000 tests per migration model). We repeated all tests using a subset of 40 SNPs per individual, for a total of 18,000 tests in the absence of spatial structures, and and 36,000 tests in the presence of global or local structures.
Results
Statistical power of the spca_randtest
Significant results for global test (g test), local tests (l test), and spca_randtest (r test +/−) for random, global and local patterns using 200 loci per individual. IS, SS, IBD indicate the migration models (see Methods); different migration rates are coded by number: 1 = 0.005, 2 = 0.01 and 3 = 0.1
200 SNPs | Random Patterns | Global Patterns | Local Patterns | ||||||||||
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Models | Significance level | g test | r test (+) | l test | r test (−) | g test | r test (+) | l test | rt est. (−) | g test | r test (+) | l test | r test (−) |
IS-1 | .05 | 0.054 | 0.059 | 0.041 | 0.047 | 0.947 | 0.985 | 0.029 | 0.001 | 0.047 | 0.071 | 0.061 | 0.284 |
.01 | 0.011 | 0.007 | 0.009 | 0.010 | 0.822 | 0.948 | 0.005 | 0.001 | 0.008 | 0.010 | 0.015 | 0.113 | |
IS-2 | .05 | 0.040 | 0.041 | 0.058 | 0.056 | 0.227 | 0.564 | 0.044 | 0.018 | 0.056 | 0.059 | 0.050 | 0.123 |
.01 | 0.007 | 0.009 | 0.009 | 0.013 | 0.067 | 0.302 | 0.005 | 0.002 | 0.011 | 0.007 | 0.012 | 0.026 | |
IS-3 | .05 | 0.051 | 0.040 | 0.053 | 0.041 | 0.055 | 0.049 | 0.045 | 0.047 | 0.049 | 0.047 | 0.044 | 0.059 |
.01 | 0.010 | 0.014 | 0.013 | 0.008 | 0.010 | 0.013 | 0.007 | 0.013 | 0.002 | 0.014 | 0.008 | 0.019 | |
SS-1 | .05 | 0.053 | 0.058 | 0.053 | 0.050 | 0.986 | 0.996 | 0.022 | 0.000 | 0.063 | 0.064 | 0.124 | 0.582 |
.01 | 0.007 | 0.011 | 0.010 | 0.010 | 0.960 | 0.988 | 0.002 | 0.000 | 0.017 | 0.010 | 0.041 | 0.398 | |
SS-2 | .05 | 0.044 | 0.058 | 0.058 | 0.063 | 0.798 | 0.909 | 0.047 | 0.004 | 0.034 | 0.044 | 0.059 | 0.316 |
.01 | 0.011 | 0.011 | 0.013 | 0.016 | 0.676 | 0.771 | 0.010 | 0.000 | 0.004 | 0.005 | 0.014 | 0.147 | |
SS-3 | .05 | 0.047 | 0.046 | 0.057 | 0.049 | 0.054 | 0.128 | 0.040 | 0.042 | 0.044 | 0.054 | 0.049 | 0.071 |
.01 | 0.014 | 0.007 | 0.011 | 0.013 | 0.014 | 0.036 | 0.006 | 0.010 | 0.003 | 0.009 | 0.006 | 0.009 | |
IBD-1 | .05 | 0.044 | 0.050 | 0.053 | 0.048 | 0.962 | 0.999 | 0.021 | 0.000 | 0.025 | 0.087 | 0.438 | 0.809 |
.01 | 0.008 | 0.012 | 0.009 | 0.010 | 0.926 | 0.997 | 0.003 | 0.000 | 0.009 | 0.023 | 0.192 | 0.694 | |
IBD-2 | .05 | 0.052 | 0.045 | 0.061 | 0.038 | 0.967 | 0.998 | 0.023 | 0.000 | 0.046 | 0.076 | 0.451 | 0.794 |
.01 | 0.009 | 0.008 | 0.011 | 0.009 | 0.932 | 0.997 | 0.004 | 0.000 | 0.009 | 0.018 | 0.208 | 0.672 | |
IBD-3 | .05 | 0.052 | 0.046 | 0.053 | 0.050 | 0.977 | 0.999 | 0.015 | 0.000 | 0.050 | 0.083 | 0.441 | 0.824 |
.01 | 0.013 | 0.009 | 0.011 | 0.012 | 0.939 | 0.999 | 0.005 | 0.000 | 0.009 | 0.023 | 0.225 | 0.684 |
Results for the same simulations reported in Table 1 using a subset of 40 loci per individual
40 SNPs | Random Patterns | Global Patterns | Local Patterns | ||||||||||
---|---|---|---|---|---|---|---|---|---|---|---|---|---|
Models | Significance level | g test | r test (+) | l test | r test (−) | g test | r test (+) | l test | r test (−) | g test | r test (+) | l test | r test (−) |
IS-1 | .05 | 0.052 | 0.061 | 0.046 | 0.050 | 0.591 | 0.807 | 0.033 | 0.004 | 0.036 | 0.000 | 0.055 | 0.077 |
.01 | 0.016 | 0.013 | 0.010 | 0.007 | 0.393 | 0.592 | 0.005 | 0.000 | 0.004 | 0.000 | 0.015 | 0.022 | |
IS-2 | .05 | 0.053 | 0.047 | 0.038 | 0.042 | 0.103 | 0.226 | 0.046 | 0.020 | 0.073 | 0.000 | 0.057 | 0.038 |
.01 | 0.011 | 0.009 | 0.006 | 0.006 | 0.022 | 0.072 | 0.011 | 0.005 | 0.012 | 0.000 | 0.010 | 0.006 | |
IS-3 | .05 | 0.047 | 0.050 | 0.050 | 0.045 | 0.048 | 0.060 | 0.044 | 0.042 | 0.036 | 0.000 | 0.053 | 0.026 |
.01 | 0.009 | 0.011 | 0.008 | 0.007 | 0.009 | 0.011 | 0.011 | 0.011 | 0.002 | 0.000 | 0.013 | 0.001 | |
SS-1 | .05 | 0.052 | 0.054 | 0.039 | 0.049 | 0.898 | 0.949 | 0.017 | 0.000 | 0.050 | 0.001 | 0.067 | 0.169 |
.01 | 0.009 | 0.012 | 0.005 | 0.011 | 0.826 | 0.865 | 0.006 | 0.000 | 0.007 | 0.000 | 0.021 | 0.052 | |
SS-2 | .05 | 0.046 | 0.045 | 0.050 | 0.046 | 0.528 | 0.588 | 0.044 | 0.009 | 0.052 | 0.000 | 0.048 | 0.081 |
.01 | 0.013 | 0.010 | 0.010 | 0.015 | 0.377 | 0.370 | 0.016 | 0.000 | 0.005 | 0.000 | 0.011 | 0.014 | |
SS-3 | .05 | 0.068 | 0.040 | 0.050 | 0.048 | 0.066 | 0.055 | 0.053 | 0.033 | 0.026 | 0.000 | 0.047 | 0.023 |
.01 | 0.014 | 0.005 | 0.013 | 0.012 | 0.012 | 0.009 | 0.005 | 0.006 | 0.006 | 0.000 | 0.008 | 0.000 | |
IBD-1 | .05 | 0.049 | 0.053 | 0.052 | 0.057 | 0.822 | 0.883 | 0.027 | 0.002 | 0.034 | 0.055 | 0.124 | 0.480 |
.01 | 0.005 | 0.008 | 0.013 | 0.013 | 0.755 | 0.742 | 0.004 | 0.000 | 0.005 | 0.008 | 0.032 | 0.278 | |
IBD-2 | .05 | 0.043 | 0.054 | 0.060 | 0.049 | 0.835 | 0.880 | 0.028 | 0.001 | 0.043 | 0.051 | 0.111 | 0.458 |
.01 | 0.011 | 0.007 | 0.015 | 0.009 | 0.755 | 0.732 | 0.005 | 0.000 | 0.008 | 0.015 | 0.026 | 0.259 | |
IBD-3 | .05 | 0.043 | 0.042 | 0.051 | 0.050 | 0.844 | 0.899 | 0.026 | 0.002 | 0.048 | 0.058 | 0.115 | 0.465 |
.01 | 0.012 | 0.013 | 0.012 | 0.010 | 0.763 | 0.756 | 0.007 | 0.000 | 0.009 | 0.010 | 0.023 | 0.263 |
Significant eigenvalues are assessed using a hierarchical Bonferroni correction which accounts for non-independence of eigenvalues and multiple testing (Fig. 2). Strong patterns (e.g. IBD) tend to produce a higher number of significant components than weak patterns (e.g. island models with high migration rates), which are otherwise captured by fewer to no components.
Application to real data
Results of the spca_randtest with 10,000 permutations on the human mtDNA dataset (Montano et al., [14])
Spatial patterns | Observed p-value | Decreasing Positive Eigenvalues | Observed p-value | Bonferroni corrected significant level |
---|---|---|---|---|
Global pattern | 0.0058 | 3.4e-2 | 0.0105 | 0.05 |
Local pattern | 0.8826 | 8.5e-3 | 0.0137 | 0.025 |
4.1e3 | 0.0136 | 0.016 | ||
1.6e-3 | 0.506 | 0.0125 |
Discussion
We introduced a new statistical test associated to the sPCA to evaluate the statistical significance of global and local spatial patterns. Using simulated data, we show that this new approach outperforms previously implemented tests, having greater statistical power (lower type II errors) whilst retaining consistent type I errors. Our simulations also suggest that demographic settings and migratory models can substantially impact the ability to detect spatial patterns. Indeed, high migration rates, non-hierarchical migration models, such as island model, and low amount of loci can hamper or worsen the performance of the test, preventing the detection of actual spatial patterns. In lack of previous information on the demographic history and/or the movement ecology of the population under study, it is certainly useful to exploit all the available genetic information. In this regards, our simulations show how an increased number of loci does improve the ability of the test to provide meaningful results.
The impact of specific factors such as the effective population size or the number of individuals sampled per population remain to be investigated. A more extensive simulation study, possibly comparing different non-model based methods such as sPCA, would clarify the extent of the spatial information that can be obtained with such methods without comparing explicit evolutionary hypotheses. In fact, the sPCA and the associated spca_randtest cannot distinguish between explicit migration models. However, the possibility to detect which eigenvalues contain the spatial information provides the user with further information to interpret the biological meaning of the spatial structure, by focusing on few meaningful dimensions.
Our data application seems to confirm that the spca_randtest is more effective than global or local tests. We chose indeed a previously published dataset of human populations which span a subcontinental area of Africa and had been originally detected to be a highly structured dataset with a geographic cline of population differentiation (Montano et al. [14]). On the basis of the original results, we would have expected a spatial global structure to be present in the data and thus detected with an sPCA. While the global test failed to provide statistical significance, the spca_randtest did obtain significant results and pointed to the three first most positive components to be also significant after Bonferroni correction. In agreement with the original interpretation of the genetic structure within the samples, spatial component 1 (SP1) shows a clear differentiation of populations in the Gabon-Congo region, while SP2 detects differentiation of Central Nigerian and North Cameroonian populations, on one hand, and extreme Western populations of Senegal, on the other hand (Fig. 3). The colored combination of the first and second most positive component (Fig. 3) also correctly detects a more fragmented differentiation across Central forested areas (Cameroon, Gabon and Congo) compared to more homogeneous Central-Western populations, which was the main result of the original publication based on very different approaches [14]. We limited the analysis to these two component as the third did not add much information to the previous.
Conclusions
Our simulation approach coupled with a real data application well illustrates the informativeness of our new test to retrieve significant spatial patterns, being these global or local structures and highlights the usefulness of selecting a specific number of significant components to interpret the biological meaning of the results.
Declarations
Acknowledgements
We thank two anonymous reviewers for insightful comments and feedback which greatly improved the original version of the manuscript.
Funding
No funds were used for this study.
Availability of data and materials
https://github.com/thibautjombart/adegenet/blob/master/R/spca_randtest.R
Author contributions
Test development: VM and TJ. Data analysis: VM. Wrote the manuscript: VM and TJ.
Ethics approval and consent to participate
Not applicable
Consent for publication
Not applicable
Competing interests
The authors declare no conflict of interest.
Open AccessThis article is distributed under the terms of the Creative Commons Attribution 4.0 International License (http://creativecommons.org/licenses/by/4.0/), which permits unrestricted use, distribution, and reproduction in any medium, provided you give appropriate credit to the original author(s) and the source, provide a link to the Creative Commons license, and indicate if changes were made. The Creative Commons Public Domain Dedication waiver (http://creativecommons.org/publicdomain/zero/1.0/) applies to the data made available in this article, unless otherwise stated.
Authors’ Affiliations
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