Figures
Abstract
Biological evidence suggests that multiple causal variants in a gene may cluster physically. Variants within the same protein functional domain or gene regulatory element would locate in close proximity on the DNA sequence. However, spatial information of variants is usually not used in current rare variant association analyses. We here propose a clustering method (abbreviated as “CLUSTER”), which is extended from the adaptive combination of P-values. Our method combines the association signals of variants that are more likely to be causal. Furthermore, the statistic incorporates the spatial information of variants. With extensive simulations, we show that our method outperforms several commonly-used methods in many scenarios. To demonstrate its use in real data analyses, we also apply this CLUSTER test to the Dallas Heart Study data. CLUSTER is among the best methods when the effects of causal variants are all in the same direction. As variants located in close proximity are more likely to have similar impact on disease risk, CLUSTER is recommended for association testing of clustered rare causal variants in case-control studies.
Citation: Lin W-Y (2014) Association Testing of Clustered Rare Causal Variants in Case-Control Studies. PLoS ONE 9(4): e94337. https://doi.org/10.1371/journal.pone.0094337
Editor: Zhaoxia Yu, University of California, Irvine, United States of America
Received: January 29, 2014; Accepted: March 12, 2014; Published: April 15, 2014
Copyright: © 2014 Wan-Yu Lin. This is an open-access article distributed under the terms of the Creative Commons Attribution License, which permits unrestricted use, distribution, and reproduction in any medium, provided the original author and source are credited.
Funding: This work was supported by grants 102-2628-B-002-039-MY3 and 102-2314-B-002-001-MY2 from the Ministry of Science and Technology of Taiwan, and NTU-CESRP-101R7622-8, NTU-CESRP-102R7622-8, NTU-CESRP-103R7622-8, and NTU-CDP-102R7769 from National Taiwan University. The funders had no role in study design, data collection and analysis, decision to publish, or preparation of the manuscript.
Competing interests: The author has declared that no competing interests exist.
Introduction
The development in next-generation sequencing technologies has allowed a comprehensive investigation of the role of rare variants (minor allele frequency (MAF) <1%) on complex diseases [1]. The low frequency of rare variants decreases the statistical power of detecting individual causal variants. Many statistical methods have been proposed to test for the collective association of multiple variants in a gene or region with diseases [2]–[13]. However, these methods do not incorporate the information of physical positions of the variants. Biological evidence suggests that multiple causal variants in a gene may cluster physically [14]. Variants within the same protein functional domain or gene regulatory element would locate in close proximity on the DNA sequence [15]–[18]. Furthermore, the spatial distribution of rare variants can be used to depict population structures [19]. These all constitute the importance of spatial approaches for rare variant association analyses.
Ionita-Laza et al. [14] has proposed a likelihood ratio scan statistic, and it successfully identifies clusters of rare deleterious variants with autism spectrum disorders. This method takes into account the underlying spatial distribution of variants, and we refer it to as “IL-K” because it is extended from the popular Kulldorff scan statistic [20]. It allows variable window sizes and calculates a likelihood ratio statistic for each window. The sliding window with the highest likelihood ratio statistic is the most likely region to harbor a cluster of rare deleterious variants. The statistical significance is assessed by permutation P-values [14].
Schaid et al. [16] has extended another popular spatial clustering method, Tango's statistic [21]–[23], to genomic sequence data. They incorporate the distance measures between variants into a kernel matrix, and therefore this method is referred to as “Kernel distance clustering” method (abbreviated as “KERNEL” hereafter). The statistic is , where
is the kernel matrix with spatial information, and
is the vector of case-control differences in variant frequencies. The statistical significance is also assessed by permutation P-values. Schaid et al. [16] have shown that IL-K outperforms KERNEL over a range of clustering scenarios, but KERNEL takes approximately half the computational time of IL-K.
We here propose a clustering method that is extended from the adaptive combination of P-values [24], [25]. This method truncates the variants with larger P-values which are more likely to be neutral variants. With extensive simulations, we have shown that our method outperforms KERNEL [16], the weighted-sum approach (referred to as “WS”) [4], and the variable threshold approach (referred to as “VT”) [6], in the majority of scenarios. It also outperforms IL-K [14] and the sequence kernel association test (SKAT) [8], [9] when all the causal variants are protective. We also apply this test to the Dallas Heart Study data [26], [27], to demonstrate its use in real data analyses.
Materials and Methods
Suppose that there are K variant sites in a region of interest. We name the sites with larger variant frequencies in cases than in controls “deleterious-inclined variant sites”, and those with larger variant frequencies in controls than in cases “protective-inclined variant sites”. For a case-control study, the association of each variant with the disease status can be tested by the Fisher's exact test [13], [28] or by the logistic regression (if covariate adjustment is required). Let the per-site P-values of the K variants be , respectively. To test for the significance of the region, we combine the per-site P-values that are smaller than some truncation threshold. Suppose we consider J candidate truncation thresholds,
.
Multiple causal variants may cluster spatially in a functional region [14]. The proposed method is extended from the adaptive combination of P-values [24], [25]. Furthermore, the spatial distribution of variants is taken into consideration. Under the jth truncation threshold (), the significance signal accumulated by the deleterious-inclined variant sites is
, where
is a
-length vector with the ith element of
. The indicator variable
is 1 if the ith site is deleterious-inclined and 0 otherwise,
is the weight given to the ith site (detailed in the next paragraph), and
is 1 if the P-value of the ith site is smaller than the jth truncation threshold (
) and 0 otherwise. Similarly, under the jth truncation threshold, the significance signal accumulated by the protective-inclined variant sites is
, where
is a
-length vector with the ith element of
. The indicator variable
is 1 if the ith site is protective-inclined and 0 otherwise.
We follow Madsen and Browning [4] to determine the weights given to variant sites ('s). Let
be the number of mutant alleles observed for variant i in the unaffected subjects, and let
be the number of unaffected subjects genotyped for variant i. The frequency of variant i in the unaffected subjects is
. The weight given to the ith site is
, where
is the total number of subjects genotyped for variant i.
The matrix
incorporates the spatial information of the variants. The (i, j)th element of
is
, where
,
is the physical distance between the ith and the jth variants, and
is a user-specified maximum distance of variants. Although the distance measure
(named “tri-weight”) is used throughout this work, it can be replaced by other measures (see [16]).
Under the jth truncation threshold, a test statistic regardless of the directions of effects (deleterious or protective) is . With B permutations by randomly shuffling the case/control status, we obtain the permuted statistics
. The P-value of the observed statistic
is estimated by
, and the P-value of the
th permuted statistic
is estimated by
. Across the J candidate truncation thresholds, the minimum P-value of the observed sample is
, and the minimum P-value of the
th permuted sample is
. Because we have B permutations, we compare
with
, and the “adjusted P-value” is estimated by
. This method is referred to as “CLUSTER”, as it is proposed for detecting clusters of rare variants.
If we ignore the spatial information and let be an identity matrix (all the diagonal elements are 1 and all the off-diagonal elements are 0), the statistic
will be reduced to
This is equivalent to the statistic of the “adaptive combination of P-values for rare variant association testing” (abbreviated as “ADA”) [24].
Simulation Study
To simulate real human genomic structure, we used the Cosi program [29] that was based on a coalescent process [30]. We generated 100 data sets, each containing 10,000 chromosomes of 1 Mb regions. The chromosomes were generated according to the linkage disequilibrium patterns of the HapMap CEU (Utah residents with ancestry from northern and western Europe) samples [31]. For each data set, we randomly selected a ∼20 kb region. We considered two situations: (I) clustered causal variants: 20 rare causal variants were clustered within a ∼6 kb region; (II) non-clustered causal variants: 20 rare causal variants were approximately equally spaced across the whole ∼20 kb. The 20 causal variants were assumed to be (I) all protective; (II) 15 protective and 5 deleterious; (III) 10 protective and 10 deleterious; (IV) 5 protective and 15 deleterious; (V) all deleterious. The population attributable risk (PAR) of each causal variant was assumed to be 0%, 0.2%, 0.4%, 0.6%, 0.8%, and 1%, respectively.
Given PAR () and MAF (
) of the jth causal variant, its genotype relative risk (GRR) is:
[4], [32]–[34]. The indicator function
is 1 if the jth causal variant is protective, and is 0 otherwise. The genotypes of a subject were formed by two chromosomes randomly drawn from the pool of 10,000 chromosomes. For a subject with chromosomes
, his/her disease status was generated by
[32]–[34], where
was the baseline penetrance (set at 1%), and
was the minor allele at the jth site. Chromosome pairs were randomly drawn from the chromosome pool with replacement until 500 cases and 500 controls were recruited.
Tests under Comparison
We compared CLUSTER with IL-K [14], KERNEL [16], SKAT [8], [9], WS [4], and VT [6]. Single-nucleotide polymorphisms with MAF >5% in the combined sample of cases and controls were first removed from the analyses. The per-site P-values of individual variants were obtained by the mid P-values from the Fisher's exact test [28]. The user-specified maximum distance was fixed at 20 kb throughout this work. IL-K and KERNEL were implemented with the R package “vclust” [16]. The maximum window size considered by IL-K was set at 50% of the total region length, ∼10 kb, as suggested by Ionita-Laza et al. [14]. When performing “KERNEL”, tri-weight (
) was used as the distance measure between any two variants, because this was the default setting in the R package “vclust” [16]. To have a fair comparison, CLUSTER was implemented with the same tri-weight distance measure. The candidate truncation thresholds considered in CLUSTER were 0.10, 0.11, 0.12, …, 0.20. These are suitable P-value truncation thresholds for rare variant association testing [24].
Two burden tests including WS and VT were implemented with the R script by Price et al. [6] (http://genetics.bwh.harvard.edu/rare_variants/). As a representative method of non-burden tests, SKAT was also included into comparisons. SKAT was implemented with the R package “SKAT” [35]. The weight given to the jth variant site (with MAF of ) was set at
, because this was the default weight function in the package “SKAT”. Note that the SKAT [9] compared here is the test that optimally combines the burden tests and the original SKAT proposed by Wu et al. [8].
The P-values of CLUSTER, IL-K, KERNEL, WS, and VT were obtained with 10,000 permutations when evaluating type-I error rates and 1,000 permutations when evaluating power, respectively. For SKAT, we used the default Davies method [36] in the package “SKAT” to compute P-values.
Results
Type-I Error Rates
The type-I error rates were measured when PAR was set at 0%. We performed 1,000 replications for each of the 100 simulated data sets. Therefore, there were totally 100,000 ( = ) replications. Table 1 summarizes the type-I error rates given various nominal significance levels. The type-I error rates of all the six methods match the corresponding nominal significance levels.
Power Comparisons
To evaluate power, a total of 100 replications were performed under each scenario for each of the 100 simulated data sets. Figure 1 presents the power averaged over the replications. When all the 20 causal variants were protective, CLUSTER was much more powerful than other methods. Under a mixture of deleterious and protective variants, IL-K, SKAT, and CLUSTER were powerful methods. However, CLUSTER had decreased power when the causal variants were non-clustered (see the bottom row). When all the 20 causal variants were deleterious, IL-K, SKAT, and CLUSTER were again the more powerful methods. Note that the effect size (measured by the magnitude of odds ratio) of a deleterious variant was larger than that of a protective variant with the same PAR and MAF (as shown by Lin et al. [24]). Therefore, all the methods performed better under 20 deleterious variants (the right column of Fig. 1) than under 20 protective variants (the left column of Fig. 1).
The figure shows the empirical power at . Top panel: clustered causal variants; bottom panel: non-clustered causal variants. The letters “p” and “r” denote the numbers of protective variants and deleterious (or, risky) variants, respectively.
We also evaluated the power performance of these tests when the number of causal variants was 10. Figure 2 shows the results of two situations considered: (I) clustered causal variants: 10 rare causal variants were clustered within a ∼3 kb region; (II) non-clustered causal variants: 10 rare causal variants were approximately equally spaced across the whole ∼20 kb. The 10 causal variants were assumed to be (I) all protective; (II) 8 protective and 2 deleterious; (III) 5 protective and 5 deleterious; (IV) 2 protective and 8 deleterious; (V) all deleterious. The result was similar to that shown by Fig. 1. CLUSTER was among the best methods when the effects of causal variants were all in the same direction, but it had decreased power under a mixture of deleterious and protective variants (see columns 2–4 of Figs. 1 & 2). This is because the test statistic facilitates the detection of variants with effects in a consistent direction. We will further discuss this in the Discussion section.
The figure shows the empirical power at . Top panel: clustered causal variants; bottom panel: non-clustered causal variants. The letters “p” and “r” denote the numbers of protective variants and deleterious (or, risky) variants, respectively.
In Figs. 1 and 2, the power from the top panel (clustered situation) is generally lower than that from the bottom panel (non-clustered situation). This is because, when the causal variants are clustered in a small region (∼6 kb or ∼3 kb, in the simulations), the variants far from this region will have almost no correlation (or, no linkage disequilibrium) with the causal variants. Therefore, they can hardly provide any association signal when testing for the whole region (∼20 kb here). When the causal variants are equally spaced across the whole region, the variants surrounding each causal variant can provide some signal because of their correlation with the causal ones. Although the correlation between rare variants is usually low [37], [38], it can still boost the power to some extent. This is a general trend for all the methods. What we can compare is the performance of the methods with spatial information (CLUSTER, IL-K, and KERNEL) relative to that of the methods without spatial information (SKAT, WS, and VT), in clustered situation or in non-clustered situation.
Not surprisingly, the clustered situation favors the methods considering spatial information (CLUSTER, IL-K, and KERNEL). They were relatively (relative to SKAT, WS, and VT) more powerful when the causal variants were clustered (top panels of Figs. 1 and 2). CLUSTER had good performance and was more powerful than KERNEL. IL-K also had good power performance, except when all the causal variants were protective (see the left columns of Figs. 1 and 2). With a mixture of protective and deleterious variants, IL-K was generally more powerful than CLUSTER, especially when the PAR was larger (see columns 2–4 of Figs. 1 and 2).
It was worth noting that CLUSTER outperformed SKAT, even when the causal variants were non-clustered (see the bottom-left plots of Figs. 1 and 2). This may be attributed to the “noise truncation” property of CLUSTER. The effect size (measured by the magnitude of odds ratio) of a protective variant was smaller than that of a deleterious variant with the same PAR and MAF (as shown by Lin et al. [24]). The effects of the protective variants were rather mild, and most methods were underpowered. CLUSTER takes the advantage of truncating neutral variants with larger P-values. CLUSTER is an extension of ADA, and this outcome is consistent with that observed in the ADA paper (see the left column of Fig. 2 of [24]).
Application to Dallas Heart Study Data
These six tests were then applied to the Dallas Heart Study [26], [27], [39]. This study was to uncover the role of ANGIOPOIETIN–LIKE 4 (ANGPTL4) in plasma triglyceride levels. The genotypes of 1,045 European Americans were analyzed. We first used a linear regression to adjust the log-transformed triglyceride levels for age, sex, and BMI. Subjects with residuals smaller than the 30th percentile and larger than the 70th percentile were treated as controls and cases, respectively. Then, the subjects with missing genotypes were excluded from the analysis. Finally, 179 cases and 213 controls were left.
The six tests were applied to this data set. The variants with MAF >5% were removed. To have an exhaustive search for the most likely region to harbor causal variants, the maximum window size considered by IL-K was set as the total region length (∼10 kb). As a result, only CLUSTER and SKAT had P-values smaller than 0.05 (see Table 2).
The significant association of ANGPTL4 with triglyceride was previously reported. Results in over 30,000 subjects from non-diabetic and population-based studies have confirmed that variants in ANGPTL4 reduce triglyceride and exert protective effects against hyperlipidemia [26], [40], [41]. With the significance level of 0.05, only CLUSTER and SKAT confirmed this association. The other two spatial approaches, IL-K and KERNEL, were shown (by simulations) to have low power when all the causal variants were protective. No wonder they failed to detect the association here. This result is consistent with the finding from our simulation study.
Discussion
Multiple rare variants may cluster in a functional region [14]–[18]. Variants within the same protein functional domain may locate in close proximity and have similar impact on disease risk [15], [17]. Consistent with the finding from Schaid et al. [16], KERNEL usually has lower power than IL-K. However, when all the causal variants are protective, IL-K has very low power (see the left columns of Figs. 1 & 2). This is because IL-K can only identify deleterious variants [14]. When all the causal variants are protective, CLUSTER and SKAT are more powerful than other methods. No wonder only these two methods could detect the protective effect of the variants in ANGPTL4 against hyperlipidemia [26], [40], [41], in the Dallas Heart Study data analysis.
As mentioned in the Methods section, a test statistic regardless of the directions of effects (deleterious or protective) is under the jth truncation threshold. Another reasonable statistic is
. This is more powerful than CLUSTER when ∼50% of the causal variants are deleterious, but is less powerful when the effects of variants are all in the same direction. Because clustered variants are more likely to have effects in the same direction, we still suggest using
, instead of
. Note that even the statistic,
, is started from aggregating the information of “deleterious-inclined variants” and “protective-inclined variants”, separately. Under the assumption that deleterious variants and protective variants may have their own clusters, we do not mix all the variants together in the very beginning (i.e.,
, this will incorporate the distance between “deleterious-inclined variants” and “protective-inclined variants” into the statistic).
All the methods evaluated here require permutations to obtain accurate P-values, except SKAT that uses the Davies method [36] to compute P-values. For simulated data sets each containing 500 cases and 500 controls in ∼20 kb regions (including ∼330 nonsynonymous variant sites), the computation time lengths were ordered as CLUSTER (∼151.7 sec) > SKAT (∼30.2 sec) > IL-K (∼20.4 sec) > KERNEL (∼6.7 sec) > VT or WS (∼3.4 sec), where 1000 permutations were used for all the methods except SKAT. This was timed by a Linux workstation with an Intel Xeon E5-2690 2.9 GHz processor and 6 GB memory. CLUSTER takes a longer time to compute because it incorporates the spatial kernel matrix into the search of the optimal P-value truncation threshold.
Schaid et al. [16] showed that IL-K and KERNEL could have higher power than SKAT, when the variants were correlated. Without correlation, SKAT tended to have the highest power among the tests they compared [16]. In fact, the correlation between rare variants is usually low [37], [38]. Our simulated data sets were generated from the coalescent process [30] and they reflected realistic DNA sequences. Therefore, in our simulations, the correlation between rare variants is low and SKAT is better than KERNEL (and sometimes better than IL-K).
KERNEL and CLUSTER have similar forms in test statistics (), and they are both implemented with the tri-weight distance measure in our simulations. However, the results showed that CLUSTER outperformed KERNEL. This is because CLUSTER combines the association signals (P-values) of variants that are more likely to be causal, i.e., truncates variants with larger P-values. CLUSTER is among the best methods when the effects of causal variants are in one direction. As variants located in close proximity are more likely to have similar impact on disease risk [15], [17], CLUSTER is recommended for association testing of clustered rare causal variants in case-control studies.
Acknowledgments
The author would like to thank the anonymous reviewers for their insightful and constructive comments, and Drs. Jonathan C. Cohen and Helen H. Hobbs for kindly providing the Dallas Heart Study data.
Author Contributions
Conceived and designed the experiments: WYL. Performed the experiments: WYL. Analyzed the data: WYL. Contributed reagents/materials/analysis tools: WYL. Wrote the paper: WYL.
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