Volume 8 Supplement 1
Testing for associations between systolic blood pressure and single-nucleotide polymorphism profiles obtained from sparse principal component analysis
© Bonner et al.; licensee BioMed Central Ltd. 2014
Published: 17 June 2014
Background: Hypertension is a prevalent condition linked to major cardiovascular conditions and multiple other comorbidities. Genetic information can offer a deeper understanding about susceptibility and the underlying disease mechanisms. The Genetic Analysis Workshop 18 (GAW18) provides abundant genotype data to determine genetic associations for being hypertensive and for the underlying trait of systolic blood pressure (SBP). The high-dimensional nature of this data promotes dimension reduction techniques to remove excess noise and also synthesize genetic information for complex, polygenic traits. Methods: For both measured and simulated phenotype data from GAW18, we use sparse principal component analysis to obtain sparse genetic profiles that represent the underlying data structures. We then detect associations between the obtained sparse principal components (PCs) and SBP, a major indicator of hypertension, following up by investigating the sparse PCs for genetic structure to gain insight into new patterns. Results: After adjusting for multiple testing, 27 of 122 PCs were significantly associated with measured SBP, offering a large number of components to investigate. Considering the top 3 PCs, linked genetic regions have been identified; these may act in unison while associated with SBP. Simulated data offered similar results. Conclusions: Sparse PCs can offer a new data-driven approach to structuring genotype data and understanding the genetic mechanics behind complex, polygenic traits such as hypertension.
Hypertension is a condition linked to major cardiovascular issues that result in heart failure and increased death rates [1–3]. Many risk factors, such as obesity, aging, and smoking, have been attributed to an individual's susceptibility to hypertension, but recent access to abundant genetic data has shifted investigation in a new and exciting direction. The Genetic Analysis Workshop 18 (GAW18) exemplifies not only this transition of focus but also the realization of new data-related challenges.
Offering genotype data for more than 24 million single-nucleotide polymorphisms (SNPs) on odd-numbered autosomal chromosomes from 959 individuals, the goal of GAW18 is to determine genetic markers that play a crucial role in blood pressure levels. A data environment of this size is termed high-dimensional, referring to the vast number of variables, and poses many statistical challenges relating to insufficient degrees of freedom when modeling (because n < p) and multiple testing; it creates an interesting platform to practice new statistical tools that confront these challenges. In particular, dimension-reduction methods that narrow our focus to the important data features could be extremely beneficial.
Principal component analysis (PCA) is a commonly used multivariate method for both dimension reduction and data visualization. It defines a new and convenient set of variables Z, called principal components (PCs), as linear combinations of original variables X. These PCs are uncorrelated and ordered by maximal variance, possibly giving the analyst an easier data set to work with. If most of the original variance is held by the first few PCs, one can discard the rest and work with a much lower dimensional problem without colinearity. However, making sense of what the PCs represent is often an issue because they are linear combinations of all original variables. To alleviate this limitation, sparse PCA methods [5–8] have been developed by incorporating methodology related to penalized regression  to achieve sparse coefficient, or loading, vectors. Tuning parameters control the level of sparseness induced, making the procedures very flexible. Setting most of the loadings to exactly 0, PCs can now be tied to tight groups of original variables that remain, resulting in an interpretable version of classical PCA.
In this paper, we use sparse PCA methodology to inform group structure in a portion of the GAW18 single-nucleotide polymorphism (SNP) data before moving on to model systolic blood pressure (SBP), a surrogate of hypertension, with representative sparse PCs. Through interpreting the PCs significantly associated with SBP, it is our goal to reveal unique data-driven groups of SNPs associated with our phenotype of interest. Because SBP is a polygenic trait, we expect the PCs to shed new light on structures of genetic regions that might act together. After describing our choice of data and methods of analysis, we will present our results and some discussion. We end by summarizing the limitations with using sparse PCA to handle genotype data and discussing future ideas.
The GAW18 data providers obtained real phenotype, covariate, and genotype data from 959 possibly related individuals. Fixing the genotype data, they prescribed a model-based relationship between functional genotypic regions, informed by the real data set and external sources, to simulate 200 phenotype-covariate data sets. We will use the real phenotype data to demonstrate an uninformed analysis that would occur in practice and use the simulated phenotype data to check the ability of our analysis to consistently detect similar group structure surrounding some truly associated SNPs.
Target sample. Of the 959 individuals from whom data is available, we chose to use only the 157 unrelated individuals.
Target variables (phenotype and covariates). Although the GAW18 group provided longitudinal phenotype and covariate data, we focus on just the baseline measures. We chose SBP as our target phenotype variable because its continuous structure allows detection of modest changes. We adjust for age, sex, smoking status, and use of blood pressure medication as covariates when attempting to detect associations between SBP and genotype information.
Target variables (genotype). The genotype data provided contained more than 24 million SNPs found on odd-numbered autosomes. Following the GAW18 group suggestions in the guide, we aim at chromosome 3. Furthermore, we consider only the 65,519 SNPs from the genome-wide association studies (GWAS) file of chromosome 3 because the sparse PCA method requires a sufficient level of variation.
Final data. There were instances of missing data in the 157 unrelated subjects and 65,519 SNPs. After removing individuals with missing phenotype or covariate data, we used PLINK software to remove individuals with genotypic calling error rates greater than 5% and remove SNPs that had missing data, minor allele frequency (MAF) less than 5%, or that failed the Hardy-Weinberg equilibrium (HWE) test at 0.001 level of significance. The final real phenotype data set we work with has 122 unrelated individuals with complete data for SBP, age, sex, smoking status, hypertension medication, and 46,574 SNPs. The final 200 simulated phenotype data sets each have complete data on 133 individuals because there was no missing data in phenotypes or covariates.
We used a 3-step process to ultimately determine groups of SNPs jointly related to SBP for the real phenotype data and each of the 200 simulated phenotype data sets. An additive model for SNPs was assumed, meaning SNPs (coded 0, 1, and 2 for copies of the minor allele) were taken as continuous.
Step 1: SNP-by-SNP filtering. To reduce the computational burden for our sparse PCA method, we first applied a linear regression model for each SNP individually, retaining those that were statistically associated with SBP at a 5% level of significance after adjusting for age, sex, smoking status, and blood pressure medication covariates. This also ensures our sparse PCA method will not accept marginally insignificant SNPs that could draw attention away from those that are most likely to be of effect. We did not adjust for multiple testing here because this step is merely used as a filter.
Step 2: Sparse PCA to obtain groups. Taking SNPs retained from step 1, we performed the sparse PCA method published in 2009 by Witten et al  to obtain a less dimensional yet representative set of PCs. The remaining nonzero loadings of these sparse PCs correspond to the SNPs contributing to their linear combinations. Prior work suggests this sparse PCA method could be the best choice among competing sparse PCA methodology when facing such a high-dimensional (n < p) data situation . Tuning parameter selection: From the real phenotype data set, we selected a tuning parameter that maintained a balance between adjusted-percentage-explained variance of PCs as calculated by Witten et al  and sparseness of loading vectors among the sparse PCs. This tuning parameter was then used for each of the 200 simulated data sets to keep dimension reduction consistent.
Step 3: Relating sparse PCs to SBP. Finally, we applied a linear regression model for each sparse PC individually, retaining those that were topmost statistically associated with SBP. We then cross-referenced the SNPs with nonzero loadings in these significant sparse PCs with gene information to attribute genetic structure to the groupings and see if new structures emerged. We report the most prevalent genetic regions.
Alongside these steps, we also tracked progress of two of the topmost contributing SNPs in the underlying simulation model. They were rs6442089 from the MAP4 gene (β = −2.3810) and rs1131356 from the FLNB gene (β = 1.0007). We were restricted to following these because they were the only notable contributing SNPs still remaining in our GWAS chromosome 3 data; rare variants (i.e., SNPs with MAF <5%) were given heavier weights in the simulation model.
All steps were performed within the statistical programming language R (version 2.15.2). To apply the sparse PCA method, we used the authors' published R-package called PMA .
Real phenotype data analysis
Step 1. Of the 46,574 SNPs in our real data, 2256 were deemed to be statistically associated with SBP at a 5% level of significance. Minimum p-value was 1.72 × 10-5. Therefore, we retained these SNPs into the sparse PCA phase with a data set of 122 individuals and 2256 SNPs.
Step 2. Tuning parameter selection must be appropriate because it decides how sparse the obtained PCs are at the expense of adjusted-percentage-explained variance. Attempting tuning parameters λ = 3, 4, 5, 6, 7, 8, 9, 10, 12, 14, 16, 18, 20, 25, 30, we gauged that choosing tuning parameter λ = 10 resulted in a balance between adjusted-percentage-explained variance and sparseness. This was graphically determined based on diminishing returns in both criteria across tuning parameters. Performing the sparse PCA, a mean (SD) of 246.2 (44.1) nonzero loadings per PC existed across the 122 PCs, reflecting that a decent level of sparseness was introduced to the PCA procedure. These PCs retained 66.1% of the total variance across p = 2256 SNPs that entered the sparse PCA phase. This is a relatively large adjusted-percentage-explained variance because roughly 90% of the loadings were forced to 0.
Notable genetic regions from top 3 sparse principal components associated with systolic blood pressure
# SNPs in PC
% Load contrib.
# SNPs in PC
% Load contrib.
# SNPs in PC
% Load contrib.
ZPLD1 to MIR548A3
NPHP3-AS1 to TMEM108
FGF12 to MB21D2
CDCP1 to TMEM158
Simulated phenotype data analysis
Step 1. Of the 46,574 SNPs in each simulated data set, a mean (SD) of 2385.4 (232.0) across the 200 data sets was deemed statistically associated with SBP at a 5% significance. Minimum p-values had a mean (SD) of 3.65 × 10-5 (3.79 × 10-5); rs6442089 from the MAP4 gene was deemed significant in 38 of 200 simulated data sets, and rs1131356 from the FLNB gene was deemed significant in only 8 of the 200 simulated data sets. Because we would expect 10 out of 200 samples to result in a false positive if there were no underlying association (i.e., if β = 0), rs6442089 (β = −2.3810) has been detected an appropriately increased number of times, but rs1131356 (β = 1.0007) seems unrelated. For this reason, we now look exclusively at rs6442089.
Step 2. Because our focus is to track a specific SNP, we will follow only those data sets that contain rs6442089. Tuning parameters were fixed at λ = 10 to keep sparseness and adjusted-percentage-explained variance consistent with the real phenotype data analysis. For each of the 38 data sets that retained rs6442089, we ran sparse PCA to obtain the 133 sparse PCs.
Step 3. Of the 133 sparse PCs obtained for each of the 38 data sets that retained rs6442089, a mean (SD) of 28.1 (8.5) PCs was deemed statistically associated with SBP at a Bonferroni-corrected 5/133 = 0.00038% level of significance. From each of the 38 lists of significant PCs, we then identified the PC for which rs6442089 had the largest contribution (absolute loading value) and detected genetic structure from the SNPs (loadings) in this PC. Among the 38 PCs chosen in this way, the MAP4 gene had a large set of SNPs with substantial loading contribution; this is as expected because rs6442089 is from MAP4. With few exceptions, the SMARCC1 gene was equivalent in both SNP frequency and loading contribution, suggesting it may be linked with MAP4. This consistency shows the robustness of sparse PCA to noise generated in the phenotype; likewise, but less consistent and impactful, were the DHX30 and CSPG5 genes. Intergenic regions between CSPG5 and SMARCC1, SMARCC1 and MAP4, and MAP4 and CDC25A were also notable.
The sparse PCs constructed from a list of marginally associated SNPs gives insight into a new grouping structure. With a genetic component that is complex and polygenic, understanding the genetics behind SBP from this data-driven angle may be rewarding. Perhaps genes and intergenic regions that are highly weighted within the same PC have some functional similarities, or act in unison.
The choice of tuning parameter heavily influences our conclusions. We could have, for example, chosen a tuning parameter such that there were 10 to 20 remaining nonzero loadings for each loading vector. This would allow us to focus on the last groups of SNPs remaining, but with drastically increased sparseness comes loss of information, namely, severe reduction in adjusted-percentage-explained variance and loss of the SNPs of interest for the simulated data. Prior biological understanding, including specifying candidate genetic regions, could help to guide decisions regarding the tuning parameter.
The strategy we followed in this paper has some limitations. For example, concentrating only on unrelated individuals reduced our sample size, leading to low power when working with the simulated data, and limited our ability to detect the two SNPs of interest. Similarly, because we chose to focus on the GWAS file, containing only common SNPs (MAF >5%), we were not able to search for the rare-variant SNPs with higher coefficient weights in the underlying simulation model. Step 1 of our analysis strategy informs, or supervises, our sparse PCA. We could have discarded step 1 in favor of unsupervised sparse PCA to search for SNPs jointly associated with SBP, although not marginally; any finding here could be very interesting. Our assumptions regarding the genotype data structure may have influenced the results from our analysis. Considering each SNP as continuous is usually a necessity when applying sparse PCA; however, this assumes an additive model from which only linear effects can be measured.
It would be interesting to investigate performance of sparse PCA using the variance-covariance matrix with the similarity measure developed and explained by Niitsuma and Okada (2005) that is meant to handle categorical data such as SNPs [9, 10]. Also, investigating differences in findings between our supervised approach and an unsupervised approach to sparse PCA could be an excellent simulation study for future work.
As we have demonstrated, sparse PCA methodology is able to reduce the dimension of SNPs and reveal groups potentially related to a phenotype of interest. It can also be applied to many other, perhaps more suitable, data types and could be of significant benefit to researchers attempting to handle high-dimensional data, especially when considering complex, polygenic traits.
JB acknowledges grant funding from the Natural Sciences and Engineering Research Council of Canada (NSERC) and the Canadian Institutes of Health Research (CIHR, grant 84392). The GAW18 whole genome sequence data were provided by the T2D-GENES (Type 2 Diabetes Genetic Exploration by Next-generation sequencing in Ethnic Samples) Consortium, which is supported by NIH grants U01 DK085524, U01 DK085584, U01 DK085501, U01 DK085526, and U01 DK085545. The other genetic and phenotypic data for GAW18 were provided by the San Antonio Family Heart Study and San Antonio Family Diabetes/Gallbladder Study, which are supported by NIH grants P01 HL045222, R01 DK047482, and R01 DK053889. The GAW is supported by NIH grant R01 GM031575.
This article has been published as part of BMC Proceedings Volume 8 Supplement 1, 2014: Genetic Analysis Workshop 18. The full contents of the supplement are available online at http://www.biomedcentral.com/bmcproc/supplements/8/S1. Publication charges for this supplement were funded by the Texas Biomedical Research Institute.
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