Volume 5 Supplement 9
Capability of common SNPs to tag rare variants
© Sun et al; licensee BioMed Central Ltd. 2011
Published: 29 November 2011
Genome-wide association studies are based on the linkage disequilibrium pattern between common tagging single-nucleotide polymorphisms (SNPs) (i.e., SNPs having only common alleles) and true causal variants, and association studies with rare SNP alleles aim to detect rare causal variants. To better understand and explain the findings from both types of studies and to provide clues to improve the power of an association study with only common SNPs genotyped, we study the correlation between common SNPs and the presence of rare alleles within a region in the genome and look at the capability of common SNPs in strong linkage disequilibrium with each other to capture single rare alleles. Our results indicate that common SNPs can, to some extent, tag the presence of rare alleles and that including SNPs in strong linkage disequilibrium with each other among the tagging SNPs helps to detect rare alleles.
In recent years, genome-wide association studies have identified hundreds of genetic variants that may be associated with many common diseases [1–3]. It is believed that the associated single-nucleotide polymorphisms (SNPs) detected from current association studies may represent linkage disequilibrium (LD) between a common tagging SNP and true causal variants. Under the common disease/rare variants hypothesis, which suggests that many rare variants can contribute to the phenotypic variation [4, 5], association studies to detect rare alleles have become more and more important. In this study, we try to answer two questions: (1) Within a region in the genome, how well do common SNPs tag the presence of rare alleles? (2) When selecting common tagging SNPs for association studies to detect rare alleles, should we exclude SNPs in strong LD with each other (r2 > 0.95), or does it help to capture more information on the rare alleles if we include tagging SNPs in strong LD (r2 > 0.95) with each other? To answer the first question, we analyzed the correlation between common SNPs and the number of rare alleles in samples of rare SNPs (i.e., SNPs containing rare alleles) in each region of the chromosomes. Then, for the second question, we studied the change in correlation between a single rare SNP and common tagging SNPs that is achieved by including SNPs in strong LD with each other when selecting common tagging SNPs.
We use the Genetic Analysis Workshop 17 (GAW17) data set, which is composed of 697 individuals in this study. The data include 24,487 SNPs, 74% (18,131) of which are considered rare SNPs with a minor allele frequency (MAF) less than 0.01 and only 12.8% of which are common SNPs with MAF > 0.05. Because of the unbalanced number of rare and common SNPs in the data, in order to study the capability of the common SNPs to tag rare variants, we incorporate into this data set genotype data from the International HapMap Project, release 28 (http://hapmap.ncbi.nlm.nih.gov/). The final data set includes 627 individuals from 7 populations: European (88), Chinese (91), Chinese in Denver (90), Japanese (92), Luhya (98), Tuscan (61), and Yoruba (107). After removal of SNPs in perfect LD, we are left with 13,777 rare SNPs (MAF < 0.01) and 116,944 common SNPs (MAF > 0.05).
Correlation between common SNPs and the presence of rare alleles
We divide the genome into nonoverlapping 1-Mb bins. For each bin, we separate the rare SNPs from the common SNPs. The common SNP value for each individual is the number of minor alleles. The correlation between the set of common SNPs and the numbers of rare alleles is calculated in each bin as follows. For n s randomly selected rare SNPs (here we studied n s = 5) in a bin, we quantify the number of rare alleles as the total number of rare alleles, y i , that individual i (i = 1, 2, …,N) carries. The correlation between the variable y i and the common SNPs in the bin is calculated over the N individuals in two ways. In the first way we calculate the Pearson correlation r between y i and each of the common SNPs, taking the maximum r2. In the second way we calculate the multiple correlation R2  between y i and the common SNPs, using a multiple regression model. These two correlations are calculated for each consecutive region across the whole genome. We repeat the random sampling of the rare SNPs and the calculation of the correlation n r /n s times (i.e., the closest integer to n r /n s ) if n r >n s , where n r is defined as the total number of rare SNPs in a bin.
We calculate the correlations between the common SNPs and the number of rare alleles in rare SNPs separately in each of the seven subpopulations, to test whether the tagging capability is different in different populations. We also calculate the correlation between common SNPs and the number of each of two types of rare alleles (synonymous and nonsynonymous) to test whether common SNPs have a different capability to tag these two types of rare alleles.
To examine whether the correlations between common SNPs and rare alleles are due to statistical noise, we perform a permutation test. We permute each of the common SNPs within the bin across individuals and calculate the correlations between the variable yi and the permuted common SNPs. Then the observed and permutation correlation distributions are compared using a Kolmogorov-Smirnov test. We also compare the means of the two distributions using a t test.
Capability of common SNPs in strong LD to capture rare alleles
We hypothesize that incorporating common SNPs in strong LD will capture significantly more variation resulting from rare alleles than using only the common SNPs in less strong LD with each other. We select the common SNPs within a 1-Mb region of each rare SNP and divide them into two sets. The first set is composed of the common tagging SNPs with LD of r2 ≤ 0.80 between each pair; we call this set A. The second set is composed of the common SNPs with LD of r2 ≤ 0.95 between each pair, which we call set B. So set B has two parts: all the SNPs in set A (r2 ≤ 0.80) and those SNPs in set (B − A) that are in higher LD with the SNPs in set A or between themselves (0.80 <r2 ≤ 0.95). Any SNP in perfect LD (r2 = 1) with another is excluded from the data. Then we calculate the multiple correlations R2 between each rare SNP and the set of common SNPs (set A and set B, respectively). Because R2 always increases when the number of independent variables in the model increases, is always greater than or equal to , where the subscripts A and B represent set A and set B, respectively.
where n is n A or n B .
In order to test whether the increase in R2 is due to the stronger LD among the SNPs in set B, which comes from the SNPs in set (B − A), or due to the larger number of SNPs from set (B − A), we evaluate the significance of the F statistic by comparison to a sample of 1,000 replicates of its permutation distribution, obtained by permuting across individuals the set of SNPs in set B but not in set A (i.e., the SNPs in set (B − A)), which breaks any LD structure between sets A and (B − A) but keeps the structure within the set (B − A).
For each rare SNP, we also compare its multiple correlation with the common SNP set A having LD given by r2 ≤ 0.95 and with set B having LD given by r2 ≤ 0.99.
Correlation between the number of rare alleles and common SNPs within a region
Mean multiple correlation between (1) the set of common SNPs and the number of rare alleles, (2) permuted common SNPs and the number of rare alleles, (3) the set of common SNPs and the number of synonymous rare alleles, and (4) the set of common SNPs and the number of nonsynonymous rare alleles
(1) Common vs. rare SNPs
(2) Random correlation
t test P
Kolmogorov-Smirnov test P
(3) Common vs. synonymous rare SNPs
(4) Common vs. nonsynonymous rare SNPs
t test P
2.84 × 10−9
9.66 × 10−15
6.80 × 10−6
1.28 × 10−5
2.30 × 10−6
3.052 × 10−10
1.50 × 10−8
6.17 × 10−12
<2.2 × 10−16
<2.2 × 10−16
4.60 × 10−6
<2.2 × 10−16
<2.2 × 10−16
7.74 × 10-4
In the total sample, the set of common SNPs has a correlation with the number of rare synonymous alleles and with the number of rare nonsynonymous alleles ; the difference, although small, is significant (P = 7.74 × 10−4). In the subpopulations, the set of common SNPs also showed higher correlations with the number of rare synonymous alleles than with the number of rare nonsynonymous alleles, and the difference was most significant in Yoruba (P = 0.008). Note that in Yoruba, although the average correlation between common SNPs and the number of rare alleles is not high , it is significantly different from a random correlation, which suggests that common SNPs are able to capture some information on the number of rare alleles. In Yoruba, the set of common SNPs has a significantly smaller correlation with the number of rare synonymous alleles than with the number of rare nonsynonymous alleles (P = 0.008), which may indicate that the common SNPs are more prone to detecting nonfunctional SNPs than functional SNPs in this population. The correlation between common SNPs and the number of rare alleles is highest in Luhya , but common SNPs show no significant difference in capturing synonymous and nonsynonymous SNPs.
Capability of common SNPs in strong LD to capture rare variants within a region
In this study, we found that within a region in the genome, overall the common SNPs are not highly correlated with the number of rare alleles, so they are not powerful for tagging the presence of rare alleles. But in subpopulations, the common SNPs can capture some information on the presence of rare variants, and their increased correlations are statistically significant but are often small (Table 1). We also found that including tagging SNPs in strong LD with each other is helpful in detecting rare alleles.
Common SNPs have higher correlations with the presence of rare SNPs in the subpopulations, which indicates that population structure influences the tagging power. The common SNPs have lower correlations with the presence of nonsynonymous SNPs, especially in the Yoruba population, which may indicate difficulty in capturing rare functional variants in that population. In addition to the presence of rare alleles, we also analyzed the correlation between common SNPs and another variable, a collapsing statistic for rare SNPs [7–9], which has the value 1 if a rare allele is present and the value 0 if no rare alleles are present among several randomly selected SNPs within a genome region. We obtained similar results with the collapsing variable (data not shown).
Our study suggests that we should not exclude SNPs in strong LD (e.g., r2 > 0.95) from tagging SNPs in an association study, because they can help to detect rare SNPs. They are less helpful for predicting disease risk, however, because their attributable risk is so small; but the significant associations detected by them could be important for detecting new metabolic pathways.
The multiple correlation R2 could be overadjusted because the adjusting assumes independence of the common SNPs, which is not the case for our study. But we nevertheless get increased to tag rare SNPs by including SNPs in strong LD with each other among the tagging SNPs, which indicates their importance in an association study to detect causal variants.
In this study, we found that, overall, common SNPs are not good at capturing the presence of rare alleles within a region of the genome, but they can capture some information on their presence in subpopulations. The common SNPs are more prone to capturing nonfunctional rare SNPs, especially in some populations. We also found that including tagging SNPs in strong LD with each other can be helpful in detecting rare variants.
We appreciate the two reviewers’ and editor’s helpful comments. The Genetic Analysis Workshops are supported by National Institutes of Health (NIH) grant R01 GM031575 from the National Institute of General Medical Sciences. This work was supported by NIH grants HL086718 from the National Heart, Lung, Blood Institute, HG003054 from the National Human Genome Research Institute, RR03655 from the National Center for Research Resources, GM28356 from the National Institute of General Medical Sciences, and P30CAD43703 from the National Cancer Institute.
This article has been published as part of BMC Proceedings Volume 5 Supplement 9, 2011: Genetic Analysis Workshop 17. The full contents of the supplement are available online at http://www.biomedcentral.com/1753-6561/5?issue=S9.
- Wellcome Trust Case Control Consortium: Genome-wide association study of 14,000 cases of seven common diseases and 3,000 shared controls. Nature. 2007, 447: 661-678. 10.1038/nature05911.View ArticleGoogle Scholar
- Scott LJ, Mohlke KL, Bonnycastle LL, Willer CJ, Li Y, Duren WL, Erdos MR, Stringham HM, Chines PS, Jackson AU, et al: A genome-wide association study of type 2 diabetes in Finns detects multiple susceptibility variants. Science. 2007, 316: 1341-1345. 10.1126/science.1142382.PubMed CentralView ArticlePubMedGoogle Scholar
- Duerr RH, Taylor KD, Brant SR, Rioux JD, Silverberg MS, Daly MJ, Steinhart AH, Abraham C, Regueiro M, Griffiths A, et al: A genome-wide association study identifies IL23R as an inflammatory bowel disease gene. Science. 2006, 314: 1461-1463. 10.1126/science.1135245.PubMed CentralView ArticlePubMedGoogle Scholar
- Bodmer W, Bonilla C: Common and rare variants in multifactorial susceptibility to common diseases. Nat Genet. 2008, 40: 695-701. 10.1038/ng.f.136.PubMed CentralView ArticlePubMedGoogle Scholar
- Schork NJ, Murray SS, Frazer KA, Topol EJ: Common vs. rare allele hypotheses for complex diseases. Curr Opin Genet Dev. 2009, 19: 212-219. 10.1016/j.gde.2009.04.010.PubMed CentralView ArticlePubMedGoogle Scholar
- Cohen J, Cohen P: Applied multiple regression/correlation analysis for the behavioral sciences. 1983, Hillsdale, NJ, Lawrence Erlbaum AssociatesGoogle Scholar
- Li B, Leal SM: Methods for detecting associations with rare variants for common diseases: application to analysis of sequence data. Am J Hum Genet. 2008, 83: 311-321. 10.1016/j.ajhg.2008.06.024.PubMed CentralView ArticlePubMedGoogle Scholar
- Madsen BE, Browning SR: A group-wise association test for rare mutations using a weighted sum statistic. PLoS Genet. 2009, 5: e1000384-10.1371/journal.pgen.1000384.PubMed CentralView ArticlePubMedGoogle Scholar
- Price AL, Kryukov GV, de Bakker PI, Purcell SM, Staples J, Wei LJ, Sunyaev SR: Pooled association tests for rare variants in exon-resequencing studies. Am J Hum Genet. 2010, 86: 832-838. 10.1016/j.ajhg.2010.04.005.PubMed CentralView ArticlePubMedGoogle Scholar
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