Volume 10 Supplement 7

## Genetic Analysis Workshop 19: Sequence, Blood Pressure and Expression Data. Proceedings.

- Proceedings
- Open Access

# Identification of low frequency and rare variants for hypertension using sparse-data methods

- Ji-Hyung Shin
^{1}Email author, - Ruiyang Yi
^{1}and - Shelley B. Bull
^{1}Email author

**Published:**11 October 2016

## Abstract

Availability of genomic sequence data provides opportunities to study the role of low-frequency and rare variants in the etiology of complex disease. In this study, we conduct association analyses of hypertension status in the cohort of 1943 unrelated Mexican Americans provided by Genetic Analysis Workshop 19, focusing on exonic variants in *MAP4* on chromosome 3. Our primary interest is to compare the performance of standard and sparse-data approaches for single-variant tests and variant-collapsing tests for sets of rare and low-frequency variants. We analyze both the real and the simulated phenotypes.

## Keywords

- Minor Allele Frequency
- Rare Variant
- Standard Score Test
- Sequence Kernel Association Test
- Simulated Phenotype

## Background

Despite the success of genome-wide association studies, much of the genetic contribution to complex diseases and traits remains unexplained. Therefore, an increasing number of studies have turned to low-frequency and rare variant association analysis for additional explanation of disease risk or trait variability. For binary phenotypes, single-variant analyses of low-frequency and rare variants are challenging because the conventional logistic regression approaches often violate the large-sample-size assumption for test statistics, resulting in poor type 1 error control or low statistical power [1, 2]. The standard score test, in particular, can be extremely anticonservative under the null [3]. Variant-collapsing methods across multiple variants or sparse-data methods for single-variant analysis offer an alternative [1–5]. Furthermore, depending on the linkage disequilibrium (LD) structure, it is possible that even nonfunctional low-frequency or common variants can capture functional rare variant signals [4]. On the other hand, because power is higher for a variant with a higher minor allele frequency (MAF), a common functional variant will usually be better detected by a single-variant test rather than as part of a collapsing test that incorporates nonfunctional variants.

In this report, we analyze the exome-sequence data and both the real and simulated phenotype data of the unrelated Mexican American sample to evaluate and compare the performance of single-variant and variant-collapsing methods for association analysis.

## Methods

*i*= 1, …, 1943 indexes the individuals,

*HTN*

_{ i }indicates hypertension status of the

*i*

^{ th }individual (1 if the individual is hypertensive and 0, otherwise);

*AGE*

_{ i }is the age at the time of examination,

*SEX*

_{ i }is the gender of the individual, and \( {\boldsymbol{G}}_i=\left({G}_{i_1},{G}_{i_2}, \dots,\ {G}_{i_m}\right) \) indicates the vector containing the numbers of copies of the nonreference alleles at

*m*variants (ie, additively coded genotype), and \( {\boldsymbol{\beta}}_g\hbox{'} = \left({\beta}_1,{\beta}_2,\dots,\ {\beta}_m\right) \) is the vector of the associated parameters.

*m*= 1, we apply 2 types of nonstandard approaches: Firth-type penalized logistic regression likelihood ratio (LR) tests [2, 6–8], and small-sample adjusted score tests [9], and compare them to standard LR and score tests. The LR and score tests are asymptotically equivalent but may be discrepant in finite samples. The penalized LR test is based on the penalized log-likelihood function

*i*(β) is the Fisher information matrix. This is a generalization of Haldane’s statistic for sparse 2 × 2 table analysis, where \( \frac{1}{2} \) is added to each cell. For the small-sample-adjusted single-variant score tests, we apply an approach to adjust the null distribution of the test statistic by incorporating small-sample variance and/or kurtosis (see Lee et al. [9], pp. 226–227); this approach was originally recommended for variant-collapsing tests.

For variant-collapsing analysis, we consider a MAF-based weighted burden test [1], a nonburden sequence kernel association test (SKAT) and a unified approach (SKAT-O) that optimally combines a burden test and a SKAT (eg, Lee et al. [9]). For these tests, we first define *K* subregions, then pool the variants within each subregion, and test *K* null hypotheses \( {H}_{0_K}:\left({\beta}_1,{\beta}_2,\dots,\ {\beta}_{m_k}\right)\hbox{'}=\left(0,\ 0,\dots,\ 0\right)\hbox{'} \), where *m*
_{
k
} indicates the number of variants within the *k*-th subregion (*k* = 1,…, *K*). For convenience, we determine the subregions on the basis of physical proximities among the variants.

*MAP4*gene on chromosome 3 in the real and the simulated phenotype data sets. For the imputed variants, we analyzed the predicted dosages rather than their best-guess genotypes. In addition, we examined all polymorphic variants, including the singletons to assess the extremes at which the tests break down. For the standard and penalized logistic regression tests, we used the R

*glm*function and

*pmlr*(Penalized Multinomial Logistic Regression) package [10], respectively. For the small-sample-adjusted score test and the variant-collapsing tests, we used the R package

*SKAT*[11], with analytical variance estimates and empirical kurtosis estimates based on 10,000 bootstrap replicates. For the variant-collapsing methods, we let

*K*= 6 based on a visual inspection of the physical positions of the variants (Fig. 1a).

### Data preparation

In the real data set, we defined the hypertension phenotype using the conventional diagnostic criteria: a systolic blood pressure (SBP) greater than 140 mm Hg or a diastolic blood pressure (DBP) greater than 90 mm Hg. We also defined individuals on antihypertensive medication to be hypertensive regardless of their SBP and DBP levels.

For the simulated phenotypes, 2 data sets were available, “SIMQ1” and “SIMPHEN,” each with 200 replicates. SIMQ1, designed for evaluating type 1 error rates, contained normally distributed *Q*
_{1} generated under no genetic effects. Because SIMQ1 did not have binary phenotypes, we dichotomized *Q*
_{1} to create hypothetical disease status *Q*
_{2}, letting *Q*
_{2} correlate with AGE and SEX through *Q*
_{1}. We let *Q*
_{2} = 1 if *Q*
_{1} was greater than 51.2 and 0 otherwise, such that the disease prevalence for *Q*
_{2} was 17.8 %, the same as the prevalence of hypertension in SIMPHEN, which we used for evaluating power. The hypertension phenotype was derived from blood pressure phenotypes generated under a model with more than 1000 variants in more than 200 genes [12].

## Results

###
*MAP4* variants in the unrelated sample

*MAP4*variants, only 90 were polymorphic in the sample of 1943 unrelated individuals. These variants had MAFs ranging from 0.00027 to 0.34. As expected, rare variants (MAF <1 %) were most prevalent in the sample; except for 4 common variants, all variants had MAF less than 5 % (Fig. 2, Table 1). As expected for rare variants (eg, Pritchard [13]), the pairwise LD in the 90 variants was generally weak, with the exception of a few variants in strong LD in an upstream region (see Fig. 1). However, the strong LD seems to arise because of their physical proximities (all the markers in the LD block are located within 39 bases).

Frequencies of rare (MAF **<**1 %), low-frequency (1 % **≤** MAF <5 %) and common (MAF ≥5 %) variants in *K* = 6 subregions within *MAP4* region on chromosome 3

Subregion | Variant IDs | Rare | Low-frequency | Common | Total |
---|---|---|---|---|---|

1 | 1–16 | 14 (4) | – | 2 (0) | 16 (4) |

2 | 17–38 | 20 (7) | 2 (0) | – | 22 (7) |

3 | 39–53 | 15 (0) | – | – | 15 (0) |

4 | 54–77 | 20 (10) | 2 (1) | 2 (2) | 24 (13) |

5 | 78–86 | 9 (0) | – | – | 9 (0) |

6 | 87–90 | 3 (1) | 1 (1) | – | 4 (2) |

Total | – | 81 (22) | 5 (2) | 4 (2) | 90 (26) |

### Analysis of the real phenotype data

We found that the standard score test rejects the null hypothesis far more often than the other single-variant tests (results not shown), suggesting that it may be anti-conservative. This agrees with published simulations under a case-control design [3] and is confirmed by our own unpublished simulation studies under a cohort design at the observed hypertension prevalence of 26 %. After correcting for multiple testing, no single-variant tests identified any association (minimum unadjusted *p* value = 0.006). The burden, SKAT and SKAT-O (optimal sequence kernel association test) tests, each of which pooled all polymorphic variants within the *K* = 6 subregions defined in Table 1 and Fig. 1a, did not find the *MAP4* gene to be significant either (minimum unadjusted *p* values = 0.12, 0.24, and 0.20, respectively).

### Analysis of the simulated phenotype data

It has been demonstrated that for a genome-wide study with a large sample size, minor allele count (MAC) is the key parameter determining test calibration [3]. Because we analyzed predicted dosages, we do not have a MAC for all the variants. Hence, for the presentation of simulation results, we use the count of individuals with *G* > 0 dosage, denoted by \( \tilde{MAC} \), which is close to the MAC for a low MAF. For type 1 error rates of the single-variant tests, we pooled the results across all variants with the same values of \( \tilde{MAC} \). Power for the single-variant tests was evaluated separately for each of the 26 functional variants. For the variant-collapsing tests, power was examined for each subregion containing at least one functional variant.

#### Test size and type I error

*p*values for rare variants revealed departures from the expected distribution under the null hypothesis of no genetic effects with some discrepancies among tests. For example, for var_3_47660325, with \( \tilde{MAC}=1, \) all the single-variant tests showed unusual departures from the expected (Fig. 3a). For low-frequency variants, the

*p*value distributions were close to the expected, except in the upper tail where all tests seemed to be anticonservative (eg, Fig. 3b). As expected, the common variant test

*p*values were close to the null distribution with no discrepancy among the tests (eg, Fig. 3c).

#### Power

*each of*the rare variants, but had 100 % power for the low-frequency and the common variants at the significance levels of 0.01 and 0.05. For the low-frequency variants, tests had discrepant

*p*values, and differential power at a stricter significance level. For example, in Fig. 5b, all the tests for var_3_47957996 (MAF = 0.0024) had

*p*values of less than 0.01; however, the 2 LR tests had consistently lower

*p*values than the 3 score tests. At a significance level of 1e–06, the standard and penalized LR tests had 91 and 82 % power, respectively, whereas the standard, the small-sample-variance, and the small-sample-variance-kurtosis score tests had less than 10 % power.

Empirical power estimates of the collapsing-variant tests based on 200 simulated data sets in SIMPHEN, according to the *MAP4* subregions containing at least 1 functional variant

Burden | SKAT | SKAT-O | ||||||||
---|---|---|---|---|---|---|---|---|---|---|

Significance level | Subregion | Rare | Rare & low- frequency | All | Rare | Rare & low- frequency | All | Rare | Rare & low- frequency | All |

0.01 | 1 | 0 | 0 | 0.260 | 0.005 | 0.005 | 0.840 | 0.005 | 0.005 | 0.805 |

2 | 0 | 0.005 | 0.005 | 0 | 0.145 | 0.145 | 0 | 0.090 | 0.080 | |

4 | 0 | 0.955 | 0.955 | 0 | 1.000 | 1.000 | 0 | 1.000 | 1.000 | |

6 | 0 | 0.990 | 0.995 | 0 | 1.000 | 1.000 | 0 | 1.000 | 1.000 | |

0.05 | 1 | 0.045 | 0.045 | 0.555 | 0.015 | 0.020 | 0.960 | 0.015 | 0.015 | 0.970 |

2 | 0.060 | 0.030 | 0.030 | 0.020 | 0.330 | 0.330 | 0.005 | 0.255 | 0.250 | |

4 | 0.030 | 0.990 | 0.990 | 0.025 | 1.000 | 1.000 | 0.015 | 1.000 | 1.000 | |

6 | 0.105 | 1.000 | 1.000 | 0.075 | 1.000 | 1.000 | 0.085 | 1.000 | 1.000 |

## Discussion and conclusions

In this article, we evaluated standard and sparse-data methods for single-variant and variant-collapsing tests to examine the association between a hypertension phenotype and exonic variants in *MAP4* gene on chromosome 3, using both the real and the simulated phenotypes in unrelated Mexican Americans.

In the analysis of the real phenotype data, none of the single-variant and the variant-collapsing methods detected *MAP4* variants significantly associated with hypertension. A limitation of our analysis is that we did not make any adjustment for ancestry admixture/population structure. In genetic association studies of admixed populations such as Mexican Americans, addressing differential ancestral backgrounds is important to avoid false positive or negative association signals [14, 15].

In our simulation investigation, we found that the sparse-data approaches improve type 1 error control, but their power remains low for detecting the rare variant effects. Because power of the association tests depends on both frequency and effect size of rare variants, even with large effects, the tests may detect rare variants only in studies with large samples. We may be more successful in identifying rare variants when we use joint or meta-analyses combining data or summary statistics from different studies (eg, Ma et al. [3]). For the low-frequency variants, all the single-variant tests seem to have improved type 1 error rates and power. It seems that the LR tests have higher power than the score tests at a stringent significance level. However, we cannot make any concrete conclusions because of the limited number of replications provided in the simulation design. Although more thorough investigation is necessary, overall, the penalized LR test and the score test with small-sample variance and kurtosis seem to be better choices than the standard tests for the analyses of rare and low-frequency variants. Moreover, caution is indicated when different tests of the same hypothesis give inconsistent *p* values as it suggests large-sample approximations for test statistics may be invalid.

Although previous simulation studies have shown that collapsing tests can have greater power than single-variant tests (see, eg, Madsen and Browning [1]), our investigation suggests that power of collapsing tests can be low when the tests include only the rare variants (see, eg, Fig. 5d). In addition to MAF and effect size, power of collapsing tests depends on the number of associated variants, the number of neutral variants, and whether the direction of effects is consistent within gene, so that selection of good binning and weighting strategies may boost power for detecting regions containing only rare variants.

## Declarations

### Acknowledgements

We thank the reviewers for their careful reading of the manuscript and thoughtful comments.

### Declarations

This work was supported in part by grants from the MITACS Network of Centres of Excellence in Mathematical Sciences and the Natural Sciences and Engineering Research Council of Canada.

This article has been published as part of *BMC Proceedings* Volume 17 Supplementary 7, 2016: Genetic Analysis Workshop 19: Sequence, Blood Pressure and Expression Data. Summary articles. The full contents of the supplement are available online at www.biomedcentral.com/bmcgenet/supplements/17/S2. Publication of the proceedings of Genetic Analysis Workshop 19 was supported by National Institutes of Health grant R01 GM031575.

### Authors’ contributions

JS and SBB designed the overall study and drafted the manuscript. JS and RY conducted statistical analyses. All authors read and approved the final manuscript.

### Competing interests

The authors declare that they have no competing interests.

**Open Access**This 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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