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Modification of the association between [PM.sub.10] and lung function decline by cadherin 13 polymorphisms in the SAPALDIA cohort: a genome-wide interaction analysis.

Introduction

Lung function is a complex phenotype i nfluenced by lifestyle, environmental, and genetic factors. Inverse associations between chronic exposure to air pollution, such as particulate matter (PM), and respiratory function level as well as its decline have been reported in independent settings (Downs et al. 2007; Katanoda et al. 2011; Romieu et al. 2009; Schikowski et al. 2010). Air pollutants are thought to mediate their acute and chronic effects through an increase in oxidative stress, inflammation, and cytotoxicity (Andreau et al. 2012; Huang et al. 2012). However, mechanisms and differences in susceptibility remain poorly characterized (Brook et al. 2010). Only few candidate gene-air pollution interaction studies have been published. These reports also point to the oxidative and inflammatory effects of air pollution in mediating adverse respiratory health effects (Breton et al. 2011; Curjuric et al. 2012; Imboden et al. 2009; Melen et al. 2008; Romieu et al. 2006; Yang et al. 2005).

Genome-wide association studies (GWAS) on lung function were mostly cross-sectional in nature (Artigas et al. 2011; Hancock et al. 2010, 2012; Obeidat et al. 2011; Repapi et al. 2010; Wilk et al. 2009), and more recent reports have shown that the overlap in genetic determinants of the level of lung function and its decline is minimal (Hansel et al. 2013; Imboden et al. 2012). None of these lung function GWAS studies has considered ambient air pollution.

In the present study, we used a genomewide interaction study (GWIS) approach to uncover novel genetic loci modifying the association between particulate matter exposure and 11-year lung function decline. We applied a two-stage approach with a discovery sample (n = 763) and a replication sample (n = 3,896). Both are subpopulations of the SAPALDIA cohort study (Swiss Cohort Study on Air Pollution And Lung Diseases In Adults) (Martin et al. 1997). This multi-center population-based cohort was specifically designed to investigate long-term effects of air pollution on respiratory health. We a priori chose forced mid-expiratory flow ([FEF.sub.25-75%]) as the dependant lung function phenotype because it was the outcome most strongly associated with ambient particulate matter air pollution exposure in SAPALDIA (Downs et al. 2007). As a proxy for long-term exposure to complex air pollution mixtures, we chose personal estimates of 11-year cumulative exposure to home outdoor PM mass with [less than or equal to] 10 [micro]m in aerodynamic diameter ([PM.sub.10]) (Curjuric et al. 2012; Liu et al. 2007).

Methods

SAPALDIA cohort study. SAPALDIA was initiated in 1991. Participants, 18-60 years of age, were randomly selected from the population registries of eight geographic Swiss regions, with varying degrees of urbanization and different environmental and cultural characteristics. Participants of the baseline examination (n = 9,651) were invited in 2002 (n = 8,047) for a second examination. Ethical approval was obtained from the Swiss Academy of Medical Sciences and the Regional Ethics Committees; written informed consent was obtained from all participants before health examination and biological sample collection at each survey. Study design and data collected have been described elsewhere (Ackermann-Liebrich et al. 2005). Briefly, health examinations and standardized questionnaires focused on respiratory and cardiovascular health. Formal collection of fractioned blood and DNA samples was established at the follow-up survey.

Study population. Nonparticipation at follow-up (n = 1,604) and missing information on lung function phenotype data (n = 2,302), genotype data (n = 476), or covariates (n = 43) led to the exclusion of some SAPALDIA cohort participants from the present study. Participants reporting a history of asthma were excluded (n = 567) because of evidence of genetic heterogeneity of lung function decline in asthmatic and nonasthmatic subjects (Imboden et al. 2012). The final study population included participants with blood samples available for genetic testing and complete baseline and follow-up data on spirometry, smoking history, weight, weight change, height, [PM.sub.10] exposure, and residential history, as well as statistical model covariates (n = 4,659) (Downs et al. 2007). The discovery sample with genome-wide data was a random sample of the nonasthmatic SAPALDIA study population (n = 763) (Moffatt et al. 2010).

The replication sample consisted of the remainder of SAPALDIA participants with complete data (n = 3,896) and was subjected to targeted genotyping for replication of promising discovery interaction signals.

Phenotype and covariate assessment. For lung function assessment, identical spirometer devices (Sensormedics model 2200; Sensormedics, Yorba Linda, CA, USA) and protocols were used at both examinations (Ackermann-Liebrich et al. 2005). Comparability of devices was ascertained (Kunzli et al. 2005). Each participant performed three to a maximum of eight forced expiratory lung function maneuvers to obtain a minimum of two acceptable forced expiratory flows, forced vital capacity (FVC), forced expiratory volume in the first second ([FEV.sub.1]) complying with American Thoracic Society (1995) criteria. Expiratory flow measures during the middle half of the FVC ([FEF.sub.25-75%]) were taken from the flow-volume curves with the highest sum of FVC and [FEV.sub.1]. Given evidence from the SAPALDIA cohort, we focused in the present study on the annual rate of decline in [FEF.sub.25-75%] as a sensitive marker of age-related decline because it was more strongly associated with the [PM.sub.10] exposure than was [FEV.sub.1] or [FEV.sub.1]/FVC decline (Curjuric et al. 2010; Downs et al. 2007; Imboden et al. 2009; Thun et al. 2012). Annual decline in [FEF.sub.25-75%] was calculated as the difference between follow-up and baseline measure in milliters per second, divided by length of follow-up in years. Accordingly, declines in [FEV.sub.1], [FEV.sub.1]/FVC, and [FEF.sub.25-75%]/FVC were calculated for sensitivity analyses of the [FEF.sub.25-75%] GWIS top hits. Covariate information was assessed including a computer-assisted personal interview at baseline and follow-up examinations, including age, sex, current and past smoking status, and smoking history (number of cigarettes/day, years of smoking). The exposure to other inhaled pollutants such as environmental tobacco smoke or occupational exposure to dust and fumes, and respiratory symptoms were assessed with the same questions at both surveys. Participants who reported smoking < 20 packs of cigarettes and < 360 g of tobacco in their lifetime at both time points were defined as never-smokers. Cumulative cigarette exposure of participants was assessed by packyears smoked before the first examination and pack-years smoked during follow-up. Height was measured (without shoes) at baseline and follow-up. Weight was self-reported at baseline and measured at follow-up (without shoes and coat). Weight change was calculated as weight at follow-up minus weight at baseline, with positive values reflecting weight gain during follow-up period.

Home outdoor [PM.sub.10] exposure assessment. We used [PM.sub.10] as the air pollution exposure measure. Air pollution exposure assessment, dispersion model validation, as well as attribution of individual 11-year cumulative [PM.sub.10] exposure have been described elsewhere (Liu et al. 2007). Briefly, a hybrid exposure model incorporated geocoded data on seasonal, meteoroi ogical, and traffic, industrial, regional, and agricultural emission activities. Hourly concentrations of [PM.sub.10] were calculated on a spatial resolution of 200 X 200 m grid cells over the follow-up period. Annual averages of the modeled [PM.sub.10] concentrations were obtained for each grid cell. We estimated the cumulative [PM.sub.10] exposure for study participants using their residential history, in geocoded data format, assigning annual [PM.sub.10] exposure averages derived from the grid cells generated by the dispersion model, and adding up the averages over the 11-year follow-up period (Liu et al. 2007).

Genotyping, imputation, population stratification, and quality control. DNA extraction from EDTA-buffered whole blood has been previously described (Ackermann Liebrich et al. 2005; Imboden et al. 2006). Genome-wide genotyping was obtained using the platform Illumina 610K quad Bead Chip. Discovery genotyping quality control, imputation, and correction for population stratification was applied as previously described (Moffatt et al. 2010). Briefly, genome-wide genotyping was centrally performed for the GABRIEL asthma Consortium at the Centre National de Genotypage (CNG, Evry, France). We satisfactorily genotyped 567,589 autosomal single nucleotide polymorphisms (SNPs) (mean call rate, 99.7%). We obtained 2,588,592 autosomal HapMap-based SNPs by cohort-specific imputation using the MACH v1.00 software and the HapMap2 release 22 CEU reference sample (Moffatt et al. 2010). Statistical power to detect gene-environment interaction is expected to be limited, so we excluded SNPs with minor allele frequencies < 5% to avoid inflation of false positive findings produced by rare genetic variants. Final number of SNPs used for interaction association testing was 2,198,793. To account for population stratification, we relied on inferred ancestry-informative principal components (Moffatt et al. 2010) that were previously carried out using EIGENSTRAT 2.0 software and the all ethnicity HapMap data, as well as additional European reference samples (Heath et al. 2008). Subjects of non-European descent were excluded based on the first and second principal components. Adjustment for population stratification in the linear regression analyses was done by incorporating the third and fourth principal component in the statistical model. Cryptic relatedness was detected based on identity-by-state analysis, and one participant per family cluster was retained in the study population.

Statistical analysis. Discovery sample.

We performed agnostic GWIS analysis in the discovery sample using an additive genetic model, with a priori selection of potential confounders based on previous analyses of the association between air pollution and lung function decline (Curjuric et al. 2010; Downs et al. 2007; Imboden et al. 2009). We regressed each SNP with cumulative [PM.sub.10] on [FEF.sub.25-75%] annual decline adjusting for study center, age, sex, height, never-smoking status, seasonal effects (sine and cosine function of day of examination), and population stratification factors. In addition, models were adjusted for weight at baseline, weight change during follow-up, and the multiplicative interaction between baseline weight and weight change, based on our recent analysis demonstrating an interaction between air pollution and obesity on lung function in the study population (Schikowski et al. 2013). Potential interaction effects between genotype and [PM.sub.10] were captured by the inclusion of a multiplicative interaction term in the linear multivariate regression analyses. We used a joint test with two degrees of freedom to derive p-values for the joint effects of gene marginal and gene-environment interactions. This approach has been shown under a range of scenarios to have greater power for identifying novel genetic candidates than tests of the gene marginal effect or gene-environment interaction effects alone (Hancock et al. 2012; Kraft et al. 2007). We used the following terminology to report the results of the genetic effects related to the gene marginal ([p.sub.main]), the gene-environment (pint), and the joint ([p.sub.joint]) effects referring to their respective null hypothesis of gene marginal ([[beta].sub.main] = 0), the gene-environment ([[beta].sub.int] = 0), and the joint ([[beta].sub.main] = 0 and [[beta].sub.int] = 0) effects. We defined the genome-wide significance level at p < 5 x [10.sup.-8] using Bonferroni adjustment for one million independent tests. The lambda ([lambda]) for the main GWIS--a metric for estimating genomic inflation of the observed associations--was calculated as the ratio of the observed versus expected median of the chisquare distribution with 2 degrees of freedom [[summation]Chi2(2df); medianobserved divided by 1.386 ([median.sub.expected])]. GWIS sensitivity analyses were additionally performed on [FEV.sub.1], [FEV.sub.1]/FVC, and [FEF.sub.25-75%]/FVC decline to determine the genome-wide ranking of the [FEF.sub.25-75%] top hits in the GWIS results for other lung function phenotypes.

Replication sample. The replication analyses was performed on two intronic CDH13 SNPs exhibiting the lowest or very low p-values in the discovery phase without being in high linkage disequilibrium with one other (top hit, rs232593, and rs17284098). Replication de novo genotyping of rs2325934 and rs17284098 was performed on a 7900HT Fast Real-Time PCR System (Applied Biosystems, Foster City, CA, USA) by using 5-nuclease allelic discrimination assays. A random sample of approximately 10% of all DNA samples was re-genotyped, and all genotypes were confirmed. The genotype call rate was > 99%. The same adjustments as for the discovery GWIS were used, except that adjustment for population stratification was not possible in the replication sample. We do not, however, expect associations to be confounded in the replication sample because adjustment for population stratification did not influence associations in the discovery sample (data not shown). Given the gene-environment interaction identified, we performed genotype stratified analyses in the combined sample (discovery and replication) as well as additional explorative analyses assessing the robustness of the observed [PM.sub.10]-CDH13 interaction with a particular focus on smoking and on weight-related variables.

Post hoc analysis on CDH13. In a post hoc analysis, we first searched the dbGaP database (http://www.ncbi.nlm.nih. gov/projects/gapplusprev/sgap_plus.htm) for reported associations of CDH13 genetic variants using "CDH13" as the search term and looked up the GWIS result of these SNPs for interaction with [PM.sub.10] on decline in [FEF.sub.25-75%]. Second, we used the imputed data obtained in the SAPALDIA discovery sample to construct haplotypes in a 200-kb chromosomal window centered on the GWIS top hit using the software Haploview (Barrett et al. 2005). Third, based on the strong functional link between CDH13 and adiponectin, we looked up the GWIS result of SNPs in the ADIPOQ gene, the adiponectin precursor protein, for interaction with [PM.sub.10] on decline in [FEF.sub.25-75%] and made a regional association plot of the ADIPOQ locus using the software LocusZoom (Pruim et al. 2010).

Results

Baseline characteristics of the SAPALDIA cohort study participants included in the current GWIS analysis of the discovery and replication sample are presented in Table 1. We observed a highly comparable distribution of sex, age, baseline body mass index, weight change during follow-up, baseline lung function level, and average [PM.sub.10] exposure at baseline and during follow-up, except for a small difference in proportion in smokers and smoking intensity between the two samples (Table 1).

GWIS discovery results. We observed significant association signals with a group of 13 SNPs, interacting with cumulative [PM.sub.10] exposure on annual decline in [FEF.sub.25-75%], at a single locus on chromosome 16 (Figure 1A). The quantile-quantile plot of interaction p-values showed evidence for a higher number of significant signals than expected by chance (Figure 1B). Based on the lambda observed ([lambda] = 1.0476), adequate genomic control of the genome-wide associations had been applied.

The association signal at 16q23.3, located intronic to gene CDH13 (Table 2), had the strongest interaction ([p.sub.int] = 8.8 x [10.sup.-10]) for rs2325934, an uncommon variant [MAF (frequency of the least common allele in the study sample), 9.6%]. There was evidence for additional potentially independent interaction signals in this locus, as variants with varying MAFs and differing linkage disequilibrium (LD) values also showed significant interactions with cumulative [PM.sub.10] on annual [FEF.sub.25-75%] decline (e.g., rs11643197: MAF, 13.4%, [p.sub.int] = 6.87 x [10.sup.-8], LD with the CDH13 top hit rs2325934 [r.sup.2] = 0.585 and D' = 1) (Figure 2; see also Supplemental Material, Figure S1). p-Values for gene main effects ([p.sub.main]), gene-environment interaction effects (pint), and the joint test ([p.sub.joint]) are provided in Table 2 for intronic CHD13 SNPs, and in Supplemental Material, Table S1, for the top 1,000 SNPs associated with the decline in [FEF.sub.25-75%] in the discovery GWIS, ranked by gene-environment interaction effects (pint). The joint test of the SNP main effect and the interaction effect ([p.sub.joint], null hypothesis: [[beta].sub.ain] = 0 and [[beta].sub.int] = 0) did not identify additional genetic modifiers of the association between cumulative [PM.sub.10] and lung function decline beyond those already identified based on [p.sub.int] for the gene-environment interaction, and the CDH13 variants ranked high according to gene main effect, interaction, and joint tests (maximum genome-wide rank = 22 for the joint test; Table 2).

Next, we performed sensitivity GWIS analyses for annual decline in [FEV.sub.1], in [FEV.sub.1]/FVC, and in [FEF.sub.25-75%]/FVC to assess the ranking of the CDH13 variants (see Supplemental Material, Table S2). Briefly, although genome-wide significance was not reached, the CDH13 locus was the top-ranking locus in the GWIS for decline in ratios of both [FEV.sub.1]/FVC and [FEF.sub.25-75%]/FVC, but it was not strongly associated with annual decline in [FEV.sub.1] ([p.sub.int] [greater than or equal to] 0.001). For [FEV.sub.1]/FVC and [FEF.sub.25-75%]/FVC, the CDH13 SNP with the strongest interaction p-value was rs2325934 (for [FEV.sub.1]/FVC: [p.sub.int] = 1.99 x [10.sup.-6]; for [FEF.sub.25-75%]/FVC: [p.sub.int] = 1.47 x [10.sup.-6]).

GWIS replication results. We selected two genome-wide significant CDH13 SNPs for de novo genotyping in the replication study sample (n = 3,896). The rs2325934 variant was selected because it exhibited the lowest p-value of association (pint) in the discovery analysis. A second SNP, rs17284098 (MAF, 12.9%; discovery pint = 3.98 x [10.sup.-8]) was chosen for its higher MAF compared with the top hit. Both replication SNPs were in moderate LD ([r.sup.2] = 0.685 and D' = 1). They replicated yielding p-values below the Bonferroni corrected significance level for two tests (p < 0.025; rs2325934: pint = 0.008; rs17284098: [p.sub.int] = 0.016; Table 3). Interactions between the CDH13 replication SNPs and [PM.sub.10] were robust to adjustment for different covariates (Table 3). The observed association became slightly stronger despite diminished sample size (n = 3,504) when adjusted for history of smoking intensity, including pack-years at baseline and pack-years smoked during follow-up. However, it is not possible to determine whether the change was attributable to adjustment or to a difference in the sample. Omitting smoking adjustment resulted in weakened signal, as did omitting the interaction term between weight and weight change. In contrast, adjusting additionally for age-squared slightly strengthened the associations. The [PM.sub.10] effect modification by the CDH13 SNPs remained significant even in minimally adjusted (age, sex, and study area) models (rs2325934: [p.sub.int] = 0.019; rs17284098: [p.sub.int] = 0.020; Table 3).

In a genotype-stratified analysis, combining discovery and replication sample, for both CDH13 SNPs, the [PM.sub.10]-[FEF.sub.25-75%] association appeared to be restricted to participants who were homozygous for the major allele (see Supplemental Material, Table S3). For rs2325934, the major homozygous genotype strata (n = 3,750) was estimated to have an average annual change in [FEF.sub.25-75%] of -0.102 mL per increase of 1 [micro]g/[m.sup.3] [PM.sub.10] [95% confidence interval (CI): -0.19, -0.01; p = 0.03] in contrast with the group carrying at least one minor allele (estimated average annual change of 0.074 mL; 95% CI: -0.16, 0.31; p = 0.53, n = 886).

Previously published CDH13 genomewide association results and linkage disequilibrium in the 200-kb GWIS window. In GWAS, variants of the CDH13 gene were previously associated with a number of different phenotypes (see Supplemental Material, Table S4). Genetic variants in the 5' end of the CDH13 gene have been repeatedly associated with circulating adiponectin levels (Chung et al. 2011; Dastani et al. 2012; Jee et al. 2010; Morisaki et al. 2012; Wu et al. 2010). We thus looked up the interactions of these previous CDH13 GWAS hits with [PM.sub.10] on decline in [FEF.sub.25-75%], but none of these SNPs ranked high in the current GWIS ([p.sub.int] [greater than or equal to] 0.02; see Supplemental Material, Table S4). Pairwise LD in the CDH13 gene between the GWAS SNPs and the [PM.sub.10] interacting SNPs was low ([r.sup.2] [less than or equal to] 0.33).

The structure of linkage disequilibrium (see Supplemental Material, Figure S1) and haplotypes (see Supplemental Material, Figure S2) in the 200-kb window centered on rs2325934 were constructed using the imputed genotype data of the discovery sample. The LD pattern and derived haplotypes suggested that the GWIS top hit tagged specifically one 33 kb-long haplotype (block 9, stretching from rs2352934 to rs1426166). The second replication variant, rs17284098, was located in a different 11 kb-long haplotype (block 11, stretching from rs1424168 to rs17284098) in an intron downstream of the GWIS top hit.

Discussion

To our knowledge, this is the first report presenting a genome-wide interaction study aiming to identify novel genes modifying the association of PM on lung function decline. We identified a cluster of SNPs intronic to the gene CDH13 that modified the estimated effect of cumulative [PM.sub.10] on the decline in [FEF.sub.25-75%] in our study population. We estimated that participants who were homozygous for the major allele of rs2325934 experienced an excess average decline of 11 mL/sec in [FEF.sub.25-75%] per 10-[micro]g/[m.sup.3] increase in cumulative [PM.sub.10] exposure over 11 years. Interestingly, cadherin 13, the protein encoded by CDH13 is functionally linked to adiponectin, a predominantly anti-inflammatory adipokine.

Experimental animal studies have provided strong evidence that major cellular responses to PM exposure include oxidative stress (Manzo et al. 2012) and inflammation (Uski et al. 2012). Results from 125 subjects monitored before, during, and after the Beijing Olympics were consistent with oxidative and inflammatory effects of ambient air pollution in the respiratory tract (Huang et al. 2012). The relationship between PM exposure and systemic inflammation, as indicated by serum C-reactive protein (CRP), was the subject of a recent systematic review reporting more consistent results for a positive PM-CRP association in longitudinal studies of healthy subjects than in short-term studies or longitudinal studies of subjects with chronic inflammatory conditions (Li et al. 2012). The few candidate gene-air pollution interaction studies published to date also support the oxidative and inflammatory effects of air pollution in mediating adverse respiratory health effects (Breton et al. 2011; Curjuric et al. 2010; Imboden et al. 2009; Melen et al. 2008; Romieu et al. 2006; Yang et al. 2005).

In humans, CDH13 is expressed in various lung cell types, including bronchial epithelium and airway smooth muscle cells. The CDH13 gene, spanning 1.17 Mb, encodes 15 different transcripts with alternate exons that produce structural proteins, which are expressed in endothelia, epithelia (including bronchial epithelial cells), smooth muscle cells, and in nervous tissue. The major CDH13 transcript contains 14 exons (Figure 3), encoding an open reading frame for a 713-amino acid polypeptide, cadherin 13, also known as T-cadherin, H-cadherin, or vascular adiponectin receptor. Previous GWAS have indicated that CDH13 genetic variants may contribute to various phenotypes. The predicted molecular and cellular functions of cadherin 13 are congruent with some of the GWAS findings. The strongest and most consistent GWAS signals have been SNPs in the 5' untranslated region or in intron 1 associated with circulating adiponectin levels, consistent with the molecular function of adiponectin binding (GO:0055100) (Chung et al. 2011; Dastani et al. 2012; Jee et al. 2010; Morisaki et al. 2012; Wu et al. 2010). CDH13 SNPs have also been reported to be associated with body height (Okada et al. 2010) and with respiratory function (http://www.ncbi.nlm.nih. gov/projects/gapplusprev/sgap_plus.htm).

Cadherin 13 is one type of adiponectin-binding protein (Hug et al. 2004), among others such as adiponectin receptors (AdipoR1, AdipoR2) (Yamauchi et al. 2003) or calreticulin (Takemura et al. 2007), and might exert its role in respiratory health through adiponectin. Adiponectin--a 244 amino acid protein resembling collagen VII, X, and complement factor C1--has been identified as a potent and pleiotropic regulator of inflammation (Ohashi et al. 2012). Experimental evidence in mice demonstrated that cadherin 13 was required to mediate the protective effect of adiponectin on allergen-induced airway inflammation (Williams et al. 2012). In human studies, CDH13 has been consistently identified by GWAS as a determinant of circulating adiponectin (Dastani et al. 2012), and serum adiponectin concentrations were positively associated with peak lung function in a prospective study of young healthy adults (Thyagarajan et al. 2010).

Adiponectin is secreted primarily by visceral adipocytes (Arita et al. 1999). Body composition and especially visceral adiposity have been associated with lower lung function and accelerated age-related decline (Rossi et al. 2011; Wehrmeister et al. 2012). We were among the first to report evidence of a modifying effect of obesity on the association of air pollution with lung function decline (Schikowski et al. 2013).

A strength of the current analysis is the detailed characterization of the cohort participants, as well as the cohort's prospective design to specifically investigate longitudinally air pollution health effects. The fact that discovery and replication samples derive from the SAPALDIA cohort pool is a strength of this analysis. Both samples were recruited at the same time by the same field workers using the same standardized procedures. Nonetheless, larger studies in independent populations with different environmental and ethnic characteristics are needed to confirm the observed interactions between CDH13 genetic variants and [PM.sub.10]. Genome-wide interactions between environmental exposures and genetic variants on complex health phenotypes form an active field of investigation, and novel methodologies are being developed to address analytical challenges associated with this research (Ege et al. 2011; Gauderman et al. 2013; Hutter et al. 2013; Sohns et al. 2013). Recently, a genomewide analysis investigating genetic modifiers of associations between occupational exposures and lung function combined the GWIS approach with an in silico pathway analysis that indicated the involvement of inflammatory pathways (Liao et al. 2013).

There are several limitations, in addition to low power, in the present study. First, less than half of all baseline cohort participants were included in the analysis, leaving room for potential bias. Second, given the pleiotropic health outcomes associated with CDH13 in previous GWAS, it is conceivable that modification of the air pollution-lung function association reflected an underlying susceptibility caused by health conditions associated with CDH13 genotypes, such as cardiovascular phenotypes, rather than a causal interaction between the genotypes and [PM.sub.10]. In the absence of measured adiponectin levels we cannot verify whether the apparent modifying effect of CDH13 is mediated through this adipokine. Genetic variants of the adiponectin precursor protein encoded by the gene ADIPOQ were by definition included in our GWIS analysis. We looked up the interactions between [PM.sub.10] exposure and nine haplotype tagging variants of the ADIPOQ gene (Peters et al. 2013). None of these SNPs showed significant interactions (pint = 0.07 to pint = 0.95; for regional association plot of the ADIPOQ locus, see Supplemental Material, Figure S3). The CDH13 SNPs associated with adiponectin circulating level (rs3865188, rs4783244, rs12051272) (Chung et al. 2011; Dastani et al. 2012; Jee et al. 2010; Morisaki et al. 2012; Wu et al. 2010) were in very low LD ([r.sup.2] < 0.1) and thus contained in a different haplotype block than the CDH13 SNPs interacting with [PM.sub.10] (Figure 3). Nevertheless, rs3865188 previously associated with adiponectin (Jee et al. 2010; Wu et al. 2010) interacted with [PM.sub.10] at a nominal p-value of 0.06 in our study.

Because we focused a priori on [FEF.sub.25-75%] decline for this GWIS, we did not evaluate interactions between [PM.sub.10] and previously identified GWAS signals on associations with [FEV.sub.1] or FVC (Artigas et al. 2011; Hancock et al. 2010, 2012; Obeidat et al. 2011; Repapi et al. 2010; Wilk et al. 2009). Another limitation is that although asthmatic subjects appear to be more vulnerable to effects of air pollution exposure (Trasande and Thurston 2005), we restricted the current analyses to nonasthmatics. This sample restriction was based on our previous finding of an extended heterogeneity in the GWAS-identified determinants of lung function decline of healthy individuals compared with asthmatics (Imboden et al. 2012). Finally, comparing genotype-stratified analyses in the SAPALDIA cohort, the size of effect modification by the CDH13 SNPs reported here on the [PM.sub.10]-[FEF.sub.25-75%] association is substantially smaller than the size of effect modification by SERPINA1 genotypes (underlying intermediate alpha 1 antitrypsin deficiency) on the association of [FEF.sub.25-75%] decline with occupational exposure to vapors, dusts, gases, and fumes (Mehta et al. 2012). This is not unexpected for genome-wide signals of unknown functional relevance. The limitation of genome-wide signals with regard to clinical utility is a well-known problem of GWAS.

In conclusion, the mechanistic link between adiponectin (its modulating action on inflammatory processes systemically and locally in the lung) and cadherin 13 (its sequestering action on circulating adiponectin levels) make our GWIS finding, CDH13, a biologically plausible candidate gene for modifying the air pollution exposure effect. Follow-up studies need to confirm the observed interaction with CDH13 SNPs and must assess whether the finding is related to recent evidence on the modifying effect of obesity on the association between [PM.sub.10] and decline in lung function.

Caption: Figure 1. Genome-wide interactions between cumulative PM10 exposure on annual decline in FEF25-75% in the discovery sample (n = 763) of the SAPALDIA cohort study. (A) Manhattan plot of the negative log of the p-values (pint) of 2,198,793 SNPs used for interaction association testing. CDH13 SNP cluster with interaction p-values reaching genome-wide significance are above the line and SNPs in the CDH13 locus are highlighted in green. (B) Quantile--quantile plot representing calculated p-values (pint) for each PM10 by SNP interaction tested plotted against the expected chi-square--distributed p-values. Deviation from the diagonal identity line points to the presence of potentially true associations.

Caption: Figure 2. Regional association plot showing the p-values of interaction between cumulative PM10 exposure and CDH13 SNPs on annual decline in FEF25--75% in the discovery sample (n = 763) of the SAPALDIA cohort study. Shown is the regional association plot for the genome-wide significant GWIS association signal located in the CDH13 gene at 16q23.3. Negative log of the p-values are plotted on the y-axis. Genomic coordinates (Mb) of the plotted SNPs refer to genome build 36/hg18 and dbSNP128 and are given on the x-axis. Linkage disequilibrium information (r2 values) refers to HapMap Phase II data of Caucasian samples. Recombination rate shown over this chromosomal window indicates recombination sites as vertical lines. The plot was generated using LocusZoom (Pruim et al. 2010). Genes in the genomic vicinity are HSBP1, heat-shock factor-binding protein 1; MBTPS1, membrane-bound transcription factor protease, site 1; MIR3182, microRNA 3182; MLYCD, malonyl-CoA decarboxylase; NECAB2, N-terminal EF-hand calcium binding protein 2; OSGIN1, oxidative stress-induced growth inhibitor 1; SLC38A8, solute carrier family 38 (amino acid transporter), member 8.

Caption: Figure 3. Schematic representation of CDH13 gene and genetic variants identified by GWAS to be associated with various phenotypes. The CDH13 gene, spanning 1.17 Mb, at 82.6 Mb (build 36) on chromosome 16, encodes 15 different transcripts with alternate exons which produce structural proteins. The major CDH13 transcript contains 14 exons, encoding an open reading frame for a 713-amino acid polypeptide. In this schematic view of the CDH13 gene, we pinpoint SNPs identified in the dbGaP database (http://www.ncbi.nlm.nih.gov/projects/gapplusprev/sgap_plus.htm) for reported associations with various phenotypes using "CDH13" as the search term. For a list of the associated phenotypes, see Supplemental Material, Table S4. * SNPs, rs2325934 and rs17284098, identified in the present report to interact with PM10 exposure on decline in FEF25--75%.

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Medea Imboden, (1,2) Ashish Kumar, (1,2,3) Ivan Curjuric, (1,2) Martin Adam, (1,2) Gian Andri Thun, (1,2) Margot Haun, (4) Ming-Yi Tsai, (1,2) Marco Pons, (5) Robert Bettschart, (6) Alexander Turk, (7) Thierry Rochat, (8) Nino Kunzli, (1,2) Christian Schindler, (1,2) Florian Kronenberg, (4) and Nicole M. Probst-Hensch (1,2)

(1) Swiss Tropical and Public Health Institute, Basel, Switzerland; (2) University of Basel, Basel, Switzerland; (3) Wellcome Trust Centre for Human Genetics, University of Oxford, Oxford, United Kingdom; (4) Division of Genetic Epidemiology, Department of Medical Genetics, Molecular and Clinical Pharmacology, Innsbruck Medical University, Innsbruck, Austria; (5) Division of Pulmonary Medicine, Regional Hospital of Lugano, Lugano, Switzerland; (6) Lungenzentrum, Hirslanden Klinik, Aarau, Switzerland; (7) Zurcher Hohenklinik, Wald, Faltigberg-Wald, Switzerland; (8) Division of Pulmonary Medicine, University Hospitals of Geneva, Geneva, Switzerland

Address correspondence to M. Imboden, SwissTPH, Socinstr. 59, 4002 Basel, Switzerland. Telephone: 41 61 284 82 40. E- mail: medea.imboden@unibas.ch Supplemental Material is available online (http://dx.doi.org/10.1289/ehp.1307398).

The SAPALDIA Team: Study directorate: N.M. Probst Hensch (e/g), T. Rochat (p), N. Kunzli (e/exp), C. Schindler (s), J.M. Gaspoz (c). Scientific team: J.C. Barthelemy (c), W. Berger (g), R. Bettschart (p), A. Bircher (a), O. Brandli (p), C. Brombach (n), M. Brutsche (p), L. Burdet (p), D. Felber Dietrich (exp), M. Frey (p), U. Frey (pd), M.W. Gerbase (p), D. Gold (e/c/p), E. de Groot (c), W. Karrer (p), R. Keller (p), B. Martin (pa), D. Miedinger (o), U. Neu (exp), L. Nicod (p), M. Pons (p), F. Roche (c), T. Rothe (p), E. Russi (p), P. Schmid-Grendelmeyer (a), A. Schmidt-Trucksass (pa), A. Turk (p), J. Schwartz (e), D. Stolz (p), P. Straehl (exp), J.M. Tschopp (p), A. von Eckardstein (cc), E. Zemp Stutz (e). Scientific team at coordinating centers: M. Adam (e/g), C. Autenrieth (pa), P.O. Bridevaux (p), D. Carballo (c), E. Corradi (exp), I. Curjuric (e), J. Dratva (e), A. Di Pasquale (s), E. Dupuis Lozeron (s), E. Fischer (e), M. Germond (s), L. Grize (s), D. Keidel (s), S. Kriemler (pa), A. Kumar (g), M. Imboden (g), N. Maire (s), A. Mehta (e), H. Phuleria (exp), E. Schaffner (s), G.A. Thun (g), A. Ineichen (exp), M. Ragettli (e), M. Ritter (exp), T. Schikowski (e), M. Tarantino (s), M. Tsai (exp). Abbreviations: (a) allergology, (c) cardiology, (cc) clinical chemistry, (e) epidemiology, (exp) exposure, (g) genetic and molecular biology, (m) meteorology, (n) nutrition, (o) occupational health, (p) pneumology, (pa) physical activity, (pd) pediatrics, (s) statistics.

The study could not have been done without the help of the study participants, technical and administrative support and the medical teams, and field workers at the local study sites.

This research was supported by the Swiss National Science Foundation (grants 33CSCO-134276/1, 33CSCO-108796, 3247BO- 104283, 3247BO-104288, 3247BO-104284, 3247-065896, 3100-059302, 3200-052720, 3200-042532, 4026-028099); the Federal Office for Forest, Environment and Landscape; the Federal Office of Public Health; the Federal Office of Roads and Transport; the canton's government of Aargau, Basel- Stadt, Basel-Land, Geneva, Luzern, Ticino, Valais, and Zurich; the Swiss Lung League; the canton's Lung League of Basel Stadt/Basel Landschaft, Geneva, Ticino, Valais, and Zurich; SUVA (Schweizerische Versicherungsanstalt); Freiwillige Akademische Gesellschaft; UBS Wealth Foundation; Talecris Biotherapeutics GmbH; Abbott Diagnostics; European Commission 018996 (GABRIEL); Wellcome Trust (WT 084703MA).

The authors declare they have no actual or potential competing financial interests.

Received: 20 July 2013; Accepted: 13 August 2014; Advance Publication: 15 August 2014; Final Publication: 1 January 2015.

Table 1. Baseline characteristics of the study population of the
SAPALDIA cohort, discovery and replication sample (mean [+ or -] SD
or %).

Characteristic                         Discovery

n                                         763
Female (%)                               51.1
Age (years)                       41.6 [+ or -] 11.0
Body mass index (kg/[m.sup.2])     23.5[+ or -] 3.5
Height (cm)                       169.6 [+ or -] 9.0
Weight (kg)                       67.9 [+ or -] 12.6
Weight change (a) (kg)             5.4 [+ or -] 6.2
Baseline lung function
  [FEF.sub.25-75%] (L/sec)         3.5 [+ or -] 1.2
  [FEV.sub.1](L)                   3.6 [+ or -] 0.8
  [FEV.sub.1]/FVC (%)              79.6 [+ or -] 7.0
[FEF.sub.25-75%]/FVC (%)          78.1 [+ or -] 24.5
Air pollution exposure
  [PM.sub.10] annual mean          27.4 [+ or -] 9.4
    ([micro]g/[m.sup.3])
  [PM.sub.10] cumulative (a)      246.5 [+ or -] 79.0
    ([micro]g/[m.sup.3])
Smoking status
  Never-smokers (b) (%)                  42.9
  Pack-years (c)                  16.5 [+ or -] 17.3
  Pack-years (a,c)                 5.4 [+ or -] 6.5

Characteristic                        Replication

n                                        3,896
Female (%)                               51.6
Age (years)                       41.1 [+ or -] 11.4
Body mass index (kg/[m.sup.2])     23.7 [+ or -] 3.6
Height (cm)                       169.5 [+ or -] 8.7
Weight (kg)                       68.4 [+ or -] 12.6
Weight change (a) (kg)             5.6 [+ or -] 6.0
Baseline lung function
  [FEF.sub.25-75%] (L/sec)         3.5 [+ or -] 1.2
  [FEV.sub.1](L)                   3.6 [+ or -] 0.8
  [FEV.sub.1]/FVC (%)              79.4 [+ or -] 7.2
[FEF.sub.25-75%]/FVC (%)          77.6 [+ or -] 24.7
Air pollution exposure
  [PM.sub.10] annual mean          27.3 [+ or -] 9.7
    ([micro]g/[m.sup.3])
  [PM.sub.10] cumulative (a)      245.2 [+ or -] 81.4
    ([micro]g/[m.sup.3])
Smoking status
  Never-smokers (b) (%)                  43.8
  Pack-years (c)                  17.0 [+ or -] 18.2
  Pack-years (a,c)                 6.3 [+ or -] 8.3

Abbreviations: [FEF.sub.25-75%], forced mid-expiratory flow;
[FEF.sub.25-75%]-FVC, ratio of forced mid-expiratory flow and of
forced vital capacity; [FEV.sub.1] forced expiratory volume in the
first second; [FEV.sub.1]FVC, ratio of forced expiratory volume in
the first second and of forced vital capacity; FVC, forced vital
capacity.

(a) During 11-year follow-up. (b) Never-smokers defined as nonsmoker
at baseline and at follow-up survey. (c) Discovery sample: missing
data on pack-years at baseline (n = 20, 2.6%) and during follow-up (n
= 62, 7.3%); replication sample: missing data on pack-years at
baseline (n = 67, 1.7%) and during follow-up (n = 326, 8.4%).

Table 2. Discovery GWIS top hits with p-values for interaction
([p.sub.int]) < [10.sup.-7], clustered intronically to the CDH13
gene: adjusted interaction association with individualized cumulative
[PM.sub.10] exposure on annual decline in [FEF.sub.25-75%] in the
SAPALDIA cohort.

                                           Minor allele
dbSNP ID         Chromosome    Position    frequency (%)

rs2325934 (b)        16       81,900,000    9.64
rs17282232           16       81,905,824   11.12
rs10514582           16       81,910,432    8.66
rs10514580           16       81,910,872    9.71
rs16960234           16       81,913,512    9.95
rs12325503           16       81,917,248   11.21
rs10514578           16       81,917,312   11.20
rs17210599           16       81,918,568    9.93
rs10514575           16       81,931,320    9.85
rs17211371           16       81,933,040    9.98
rs1424168            16       81,935,600   10.10
rs17211581           16       81,937,240   10.11
rs17284098 (b)       16       81,947,576   12.87
rs17284265           16       81,949,792   12.14
rs17284390           16       81,954,784   11.90
rs17212165           16       81,955,688   11.96
rs11643197           16       81,964,792   13.36

                        Main             Interaction
dbSNP ID            [P.sub.main]         [P.sub.int]

rs2325934 (b)    6.94 x [10.sup.11]   8.80 x [10.sup.10]
rs17282232       5.26 x [10.sup.9]    7.28 x [10.sup.8]
rs10514582       3.71 x [10.sup.9]    3.93 x [10.sup.8]
rs10514580       1.89 x [10.sup.10]   4.10 x [10.sup.9]
rs16960234       9.90 x [10.sup.11]   1.82 x [10.sup.9]
rs12325503       5.98 x [10.sup.9]    6.23 x [10.sup.8]
rs10514578       6.01 x [10.sup.9]    6.07 x [10.sup.8]
rs17210599       1.18 x [10.sup.10]   1.49 x [10.sup.9]
rs10514575       3.95 x [10.sup.10]   2.61 x [10.sup.9]
rs17211371       7.20 x [10.sup.10]   4.03 x [10.sup.9]
rs1424168        1.36 x [10.sup.9]    6.95 x [10.sup.9]
rs17211581       1.44 x [10.sup.9]    7.40 x [10.sup.9]
rs17284098 (b)   1.56 x [10.sup.8]    3.98 x [10.sup.8]
rs17284265       5.13 x [10.sup.9]    1.57 x [10.sup.8]
rs17284390       2.01 x [10.sup.9]    5.08 x [10.sup.9]
rs17212165       1.71 x [10.sup.9]    3.30 x [10.sup.9]
rs11643197       6.35 x [10.sup.8]    6.87 x [10.sup.8]

                                          Genome-wide test rank
                       Joint
dbSNP ID           [P.sub.joint]      Main   Interaction   Joint

rs2325934 (b)    5.80 x [10.sup.10]    1          1          1
rs17282232       3.64 x [10.sup.8]     13        17         13
rs10514582       2.72 x [10.sup.8]     11        12         11
rs10514580       1.47 x [10.sup.9]     4          7          4
rs16960234       8.05 x [10.sup.10]    2          3          2
rs12325503       4.30 x [10.sup.8]     14        15         14
rs10514578       4.34 x [10.sup.8]     15        14         15
rs17210599       9.77 x [10.sup.10]    3          2          3
rs10514575       3.12 x [10.sup.9]     5          4          5
rs17211371       5.56 x [10.sup.9]     6          6          6
rs1424168        1.03 x [10.sup.8]     7          9          7
rs17211581       1.09 x [10.sup.8]     8         10          9
rs17284098 (b)   1.02 x [10.sup.7]     16        13         16
rs17284265       3.55 x [10.sup.8]     12        11         12
rs17284390       1.33 x [10.sup.8]     10         8         10
rs17212165       1.05 x [10.sup.8]     9          5          8
rs11643197       3.17 x [10.sup.7]     17        16         22

                   Strong LD
dbSNP ID          groups (a)

rs2325934 (b)    Reference (A)
rs17282232       Reference (B)
rs10514582             A
rs10514580             A
rs16960234             A
rs12325503             B
rs10514578             B
rs17210599             A
rs10514575             A
rs17211371             A
rs1424168              A
rs17211581             A
rs17284098 (b)   Reference (C)
rs17284265             C
rs17284390             C
rs17212165             C
rs11643197             C

Ranks shown in the table refer to the genome-wide ranking over
2,198,793 SNPs. The following terminology defined genetic effects
referring to their respective null hypothesis: [p.sub.main]: gene
marginal ([[beta].sub.main] = 0); pmt: gene-environment
([[beta.sub.int] = 0); [p.sub.joint]: joint effect ([[beta].sub.main]
= 0 and [[beta].sub.int] = 0). GWIS was adjusted for study center,
age, sex, height, never-smoking status, weight at baseline, weight
change during follow-up, interaction between baseline weight and
weight change, seasonal effects of time point of baseline and follow-
up examination date (sine and cosine function of day of examination)
and population stratification components. Cohort participants with
self-report of asthma history had been excluded from the analysis.
Discovery sample size was n = 763.

(a) LD (linkage disequilibrium): A indicates strong LD with rs2325934
([r.sup.2] > 0.85; D' = 1), B indicates strong LD with rs17282232
([r.sup.2] > 0.85; D' = 1), and C indicates strong LD with rs17284098
([r.sup.2] > 0.85; D' = 1). The replication SNPs, rs2325934 and
rs17284098, were in the moderate linkage disequilibrium with each
other ([r.sup.2] = 0.685, D' = 1). 'SNPs selected for replication;
they were in the moderate linkage disequilibrium with respect to
[r.sup.2] ([r.sup.2] = 0.685, D' = 1).

Table 3. Replication results of adjusted3 interaction of CDH13
intronic SNPs (rs2325934 and rs17284098) with cumulative [PM.sub.10]
during 11-year follow-up on annual decline in [FEF.sub.25-75%], the
SAPALDIA cohort study.

dbSNP ID                           n       Coefficient (b) (95% CI)

Adjusted model (a)
  rs2325934                        3,879   0.0742 (0.0191, 0.1294)
  rs17284098                       3,878   0.0632 (0.0117, 0.1147)
Adjusted + smoking history (c)
  rs2325934                        3,504   0.0766 (0.0198, 0.1335)
  rs17284098                       3,504   0.0723 (0.0188, 0.1257)
Adjusted + age-squared (c)
  rs2325934                        3,879   0.0755 (0.0205, 0.1306)
  rs17284098                       3,878   0.0645 (0.0130, 0.1160)
Adjusted: smoking status (d)
  rs2325934                        3,879   0.074 (0.0188, 0.1291)
  rs17284098                       3,878   0.0632 (0.0118, 0.1147)
Adjusted: interaction between
baseline weight and weight
change (d)
  rs2325934                        3,879   0.0742 (0.0191, 0.1293)
  rs17284098                       3,878   0.0629 (0.0114, 0.1144)
Adjusted: weight change and
interaction between baseline
weight and weight change (d)
  rs2325934                        3,879   0.0757 (0.0212, 0.1301)
  rs17284098                       3,878   0.0626 (0.0116, 0.1136)
Adjusted: weight at baseline
and interaction between baseline
weight and weight change (d)
  rs2325934                        3,879   0.0766 (0.0211, 0.1320)
  rs17284098                       3,878   0.0657 (0.0141, 0.1173)
Minimal adjustment (e)
  rs2325934                        3,879   0.0659 (0.0108, 0.1211)
  rs17284098                       3,878   0.0606 (0.0095, 0.1117)

dbSNP ID                           SE       [P.sub.int]

Adjusted model (a)
  rs2325934                        0.0281   0.008
  rs17284098                       0.0263   0.016
Adjusted + smoking history (c)
  rs2325934                        0.029    0.008
  rs17284098                       0.0273   0.008
Adjusted + age-squared (c)
  rs2325934                        0.0281   0.007
  rs17284098                       0.0263   0.014
Adjusted: smoking status (d)
  rs2325934                        0.0281   0.009
  rs17284098                       0.0262   0.016
Adjusted: interaction between
baseline weight and weight
change (d)
  rs2325934                        0.0281   0.008
  rs17284098                       0.0263   0.017
Adjusted: weight change and
interaction between baseline
weight and weight change (d)
  rs2325934                        0.0278   0.006
  rs17284098                       0.026    0.016
Adjusted: weight at baseline
and interaction between baseline
weight and weight change (d)
  rs2325934                        0.0283   0.007
  rs17284098                       0.0263   0.013
Minimal adjustment (e)
  rs2325934                        0.0282   0.019
  rs17284098                       0.0261   0.02

(a) Same adjustments applied as for discovery GWIS, including study
center, age, sex, height, never/smoking status, weight at baseline,
weight change during follow/up, interaction between baseline weight
and weight change, seasonal effects of time point of baseline and
follow/up examination date (sine and cosine function of day of
examination). No adjustment for population stratification was
available. (b) Coefficient refers to the additive SNP effect in
annual change in [FEF.sub.25/75%] (mL/sec) per 1-[micro]g/[m.sup.3]
change in [PM.sub.10] exposure. (c) Same adjustments as for the
discovery GWIS, adding indicated additional covariate(s) in the
model. (d) Same adjustments as for the discovery GWIS, omitting
indicated covariate(s) in the model. (e) Basic adjustment including
only study center, age, and sex in the model.


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Title Annotation:Research
Author:Imboden, Medea; Kumar, Ashish; Curjuric, Ivan; Adam, Martin; Thun, Gian Andri; Haun, Margot; Tsai, M
Publication:Environmental Health Perspectives
Article Type:Report
Date:Jan 1, 2015
Words:9705
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