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. Author manuscript; available in PMC: 2020 Oct 1.
Published in final edited form as: Clin Gastroenterol Hepatol. 2019 Feb 1;17(11):2227–2235.e1. doi: 10.1016/j.cgh.2019.01.041

No Association Between Vitamin D Status and Risk of Barrett’s Esophagus or Esophageal Adenocarcinoma—a Mendelian Randomization Study

Jing Dong 1, Puya Gharahkhani 2, Wong-Ho Chow 3, Marilie D Gammon 4, Geoffrey Liu 5, Carlos Caldas 6, Anna H Wu 7, Weimin Ye 8, Lynn Onstad 9, Lesley A Anderson 10, Leslie Bernstein 11, Paul D Pharoah 12,13, Harvey A Risch 14, Douglas A Corley 15,16, Rebecca C Fitzgerald 17; Stomach and Esophageal Cancer Study (SOCS) Consortium, Prasad G Iyer 18, Brian J Reid 9, Jesper Lagergren 19,20, Nicholas J Shaheen 21, Thomas L Vaughan 9, Stuart MacGregor 2, Sharon Love 22, Claire Palles 23, Ian Tomlinson 23, Ines Gockel 24, Andrea May 25, Christian Gerges 26, Mario Anders 27,28, Anne C Böhmer 29,30, Jessica Becker 31,32, Nicole Kreuser 24, Rene Thieme 24, Tania Noder 27, Marino Venerito 31, Lothar Veits 32, Thomas Schmidt 33, Claudia Schmidt 34, Jakob R Izbicki 35, Arnulf H Hölscher 34, Hauke Lang 36, Dietmar Lorenz 37, Brigitte Schumacher 38, Rupert Mayershofer 39, Yogesh Vashist 35,40, Katja Ott 33,41, Michael Vieth 32, Josef Weismüller 42, Markus M Nöthen 29,30, Susanne Moebus 43, Michael Knapp 44, Wilbert H M Peters 45, Horst Neuhaus 29, Thomas Rösch 26, Christian Ell 25, Janusz Jankowski 46, Johannes Schumacher 29,30, Rachel E Neale 47, David C Whiteman 48, Aaron P Thrift 1,49
PMCID: PMC6675666  NIHMSID: NIHMS1520503  PMID: 30716477

Abstract

Background & Aims:

Epidemiology studies of circulating concentrations of 25 hydroxy vitamin D (25(OH)D) and risk of esophageal adenocarcinoma (EAC) have produced conflicting results. We conducted a Mendelian randomization study to determine the associations between circulating concentrations of 25(OH)D and risks of EAC and its precursor, Barrett’s esophagus (BE).

Methods:

We conducted a Mendelian randomization study using a 2-sample (summary data) approach. Six single-nucleotide polymorphisms (SNPs; rs3755967, rs10741657, rs12785878, rs10745742, rs8018720, and rs17216707) associated with circulating concentrations of 25(OH)D were used as instrumental variables. We collected data from 6167 patients with BE, 4112 patients with EAC, and 17,159 individuals without BE or EAC (controls) participating in the Barrett’s and Esophageal Adenocarcinoma Consortium, as well as studies from Bonn, Germany and Cambridge and Oxford, United Kingdom. Analyses were performed separately for BE and EAC.

Results:

Overall, we found no evidence for an association between genetically estimated 25(OH)D concentration and risk of BE or EAC. The odds ratio (OR) per 20 nmol/L increase in genetically estimated 25(OH)D concentration for BE risk estimated by combining the individual SNP association using inverse variance weighting was 1.21 (95% CI, 0.77–1.92; P=.41). The OR for EAC risk, estimated by combining the individual SNP association using inverse variance weighting, was 0.68 (95% CI, 0.39–1.19; P=.18).

Conclusions.

In a Mendelian randomization study, we found that low genetically estimated 25(OH)D concentrations were not associated with risk of BE or EAC.

Keywords: risk factors, BEACON, esophageal cancer, etiology, chemoprevention

INTRODUCTION

The incidence of esophageal adenocarcinoma (EAC) has increased rapidly during the last four decades (1), and despite advances in early detection and treatment, the 5-year survival in EAC remains less than 20% (2). Barrett’s esophagus (BE), metaplastic columnar epithelial overgrowth of the distal esophagus, is the precursor for EAC (3). Established risk factors for EAC and BE include gastro-esophageal reflux disease (4, 5), obesity (6), and tobacco smoking (7, 8). Epidemiological studies have examined the association between vitamin D and risk of EAC, with conflicting results (911). However, these studies have been limited by relatively small sample sizes (< 500 EAC patients) and by potential biases, including reverse causation that may arise if serum vitamin D levels are measured at or close to the date of cancer diagnosis.

In the absence of convincing evidence from epidemiologic studies, Mendelian randomization is an alternative approach for exploring possible associations between 25(OH)D concentration and risks of BE and EAC (12). This approach uses instrumental variables (e.g., genetic variants as proxy markers of directly measured risk factors) to make inferences about the relation between an exposure (e.g., low 25(OH)D concentration) and outcome (e.g., BE and EAC) (1214). If 25(OH)D is related to risk of BE or EAC, then the variability in 25(OH)D that is due to genotype should confer differences in BE or EAC risk directly attributable to 25(OH)D. Since alleles are randomly allocated from parents to offspring at conception, the association between genotype and outcome is not confounded by other factors. Furthermore, genetic variants are measured reliably and are not affected by disease status, thus avoiding recall bias. However, a strong instrumental variable and large sample size are required for an unbiased Mendelian randomization study. The availability of large collections of genome-wide data on phenotypes, such as 25(OH)D concentration, and disease traits within international consortia represents an opportunity to use this approach. Here, we report the findings of a Mendelian randomization study examining associations between genetically estimated circulating 25(OH)D concentration and risks of BE and EAC. The selected six 25(OH)D-associated SNPs explained ~3% of the variance of 25(OH)D concentration.

METHODS

In the absence of a dataset with complete individual-level genetic data, 25(OH)D concentration levels, and BE/EAC status we applied a standard two-sample approach that uses GWAS summary-level data to assess indirect associations (15). That is, we first estimated the single nucleotide polymorphism (SNP)-disease associations from one study sample and the SNP-exposure associations in another study sample. Second, we used the Wald-type ratio estimator to calculate the Mendelian randomization estimate for the association between genetically estimated 25(OH)D concentration and risks of BE and EAC.

SNP-25(OH)D associations

A study involving 79,366 participants of European descent from 31 epidemiological studies conducted in Europe and North America, identified six SNPs associated with 25(OH)D levels at genome-wide significance (i.e., P < 5 ×10−8) (16). These six SNPs are uncorrelated and are located in or close to the following genes: GC (rs3755967), CYP2R1 (rs10741657), DHCR7 (rs12785878), AMDHD1 (rs10745742), SEC23A (rs8018720) and CYP24A1 (rs17216707). These genes have been shown to encode enzymes and carrier proteins involved in vitamin D synthesis or metabolism (16). As serum 25(OH)D concentration levels were not measured in cases and controls included in our BE/EAC studies, we instead retrieved summary-level data for the associations between these six SNPs and 25(OH)D directly from the published paper (16). In brief, that study estimated the associations between each individual SNP and natural log-transformed 25(OH)D concentration using linear regression models adjusted for month of sample collection, age, sex, body mass index, principal components of ancestry, and laboratory batch, where relevant. The analyses were conducted separately for each cohort, and the results were summarized using fixed-effects inverse variance weighted meta-analysis (16). The estimated magnitudes of association (i.e., β coefficients) for the six SNP-25(OH)D associations and their standard errors are shown in Table 1.

Table 1.

Characteristics of genetic variants associated with 25(OH)D concentration in published genome-wide association studies (ref.16)

SNP Chr Gene Effect/Reference Allele Effect Allele Frequency β estimate* s.e. P value
rs10741657 11 CYP2R1 A/G 0.40 0.031 0.0022 2.1 × 1−46
rs10745742 12 AMDHD1 T/C 0.40 0.017 0.0022 1.9 × 10−14
rsl2785878 11 DHCR7 T/G 0.75 0.036 0.0022 3.8 × 10−62
rs17216707 20 CYP24A1 T/C 0.79 0.026 0.0027 8.1 × 10−23
rs3755967 4 GC C/T 0.62 0.089 0.0023 4.7 × 10−343
rs8018720 14 SEC23A G/C 0.18 0.017 0.0029 4.7 × 10−9
*

25(OH)D level was reported SD increases in nmol/L in natural-log scale per copy of the effect alleles.

SNP-BE and SNP-EAC associations

We obtained individual-level epidemiologic and genetic data from 6,167 BE patients, 4,112 EAC patients, and 17,159 control participants from 15 epidemiologic studies from North America, Europe, and Australia included in the Barrett’s and Esophageal Adenocarcinoma Consortium (BEACON; http://beacon.tlvnet.net/), as well as from studies from Bonn, Germany; Cambridge, United Kingdom; and Oxford, United Kingdom (1720). The numbers of participants in each study are shown in Table 2. We have reported detailed information on study participants, genotyping, and imputation previously (17). Briefly, all participants were of European ancestry, and DNA samples extracted from blood or saliva were genotyped on high-density SNP arrays (Illumina, San Diego, CA, USA). BE patients were identified by histopathological diagnosis of intestinal metaplasia, and patients with EAC had a histopathologically confirmed diagnosis of adenocarcinoma. Each contributing study was performed under institutional review board approval and all participants gave informed consent. Standard quality control and imputation were performed for each study.

Table 2.

Characteristics of the studies included for the gene-25(OH)D and gene-BE/EAC associations

Data Source n studies Sample size
Gene-Vitamin D association
SUNLIGHT Consortium (ref.16) 31 79,366
Gene-BE/EAC associations
BEACON (ref. 17, 18) 15 2,406 BE, 1,508 EAC, 6,718 controls
 • United States 9 1,718 BE, 668 EAC, 1,021 controls
 • United Kingdom 1 167 BE, 102 EAC
 • Sweden 1 63 EAC, 116 controls
 • Canada 1 246 EAC, 256 controls
 • Australia 2 324 BE, 236 EAC, 567 controls
 • Ireland 1 197 BE, 193 EAC, 217 controls
 • dbGap 1 4,541 controls
Bonn (Germany) (ref. 17, 19) 1 1,037 BE, 1,609 EAC, 3,537 controls
Cambridge (UK) (ref.17) 1 873 BE, 995 EAC, 3,408 controls
Oxford (UK) (ref.17, 20) 7 1,851 BE, 3,496 controls

We used a two-stage analytic approach to estimate SNP-BE and SNP-EAC associations. Analyses were performed separately for each of the six SNPs, as well as separately for BE and EAC. First, study-specific (i.e., for BEACON, Bonn, Cambridge, and Oxford) odds ratios (OR) and corresponding 95% confidence intervals (95% CI) were estimated fitting unconditional logistic regression models which adjusted for age, sex and study-specific top principal components of ancestry, under an additive genetic model using allelic dosage. Second, for each SNP, the study-specific adjusted ORs were pooled to create a summary OR, using a fixed-effects inverse variance-weighting approach.

Mendelian randomization estimate for the association with genetically estimated 25(OH)D

We used a two-stage analytic approach to estimate the instrumental variable association between genetically estimated 25(OH)D concentration and risks of BE and EAC. In the first stage, for each instrumental variable (i.e., separately for the six SNPs), we used the Wald-type ratio estimator to compute the Mendelian randomization weighted estimates for any influence of genetically estimated 25(OH)D on risks of BE and EAC (21), and the Delta method to estimate the standard errors (22). In the second stage, the six Mendelian randomization estimates were pooled to create a summary instrumental variable OR, using an inverse-variance weighted meta-analysis approach (23). We scaled estimates to a 20-nmol/L change in 25(OH)D concentration, which is approximately the inter-tertile range (66th percentile to 33rd percentile) observed in a large European study.(24) We evaluated the presence and magnitude of heterogeneity across the six Mendelian randomization estimates with the Cochran Q and I2 statistics (25). All statistics were two sided and all analyses were conducted using Stata 14.1 (StataCorp, College Station, TX).

Assessment of pleiotropy

In order to have a valid interpretation for the Mendelian randomization analysis, our instrumental variable (the SNPs) must be independently associated with circulating 25(OH)D concentration and associated with BE or EAC only through its association with circulating 25(OH)D concentration (26, 27). To assess and account for pleiotropy (where a SNP may affect more than one phenotypic characteristic), we employed the MR-Egger regression method (an adaptation of the Egger regression in a meta-analysis) (28). The intercept statistically significantly away from zero is a valid test of directional horizontal pleiotropy, whereas the slope of the MR-Egger regression is the horizontal pleiotropy-adjusted estimated magnitude of association. We used a weighted median method to diagnose and protect against invalid genetic instruments (29), and searched the literature and publicly available GWAS databases for associations between the SNPs and other phenotypes (30).

Power

Assuming the 6 SNPs above explain 3% of the variance in 25(OH)D and with α=0.05, our study had 80% power to detect an OR of 1.25 or higher.

RESULTS

SNP-BE and SNP-EAC associations

The associations between each of the six 25(OH)D-associated SNPs and the risks of BE and EAC are shown in Table 3. Only the SNP rs12785878 was nominally associated with the risk of BE (per copy of the T allele, summary OR, 1.07; 95% CI, 1.02–1.13; P = 0.008) and none were associated with the risk of EAC (all P values > 0.1). The magnitude and direction of the individual SNP-BE or SNP-EAC associations were consistent across the 4 datasets, with no evidence of between-study heterogeneity (all I2 < 42%).

Table 3.

Characteristics of genetic variants associated with Barrett’s esophagus and esophageal adenocarcinoma

SNP Chr Gene Effect/Reference Allele BE EAC
OR (95% CI) P OR (95% CI) P
rs10741657 11 CYP2R1 A/G 1.01 (0.97–1.06) 0.577 0.98 (0.93–1.04) 0.465
rs10745742 12 AMDHD1 T/C 0.97 (0.92–1.01) 0.122 1.01 (0.95–1.06) 0.811
rsl2785878 11 DHCR7 T/G 1.07 (1.02–1.13) 0.008 0.99 (0.93–1.05) 0.785
rs17216707 20 CYP24A1 T/C 0.98 (0.92–1.04) 0.495 1.00 (0.93–1.08) 0.920
rs3755967 4 GC C/T 1.00 (0.96–1.05) 0.844 0.96 (0.91–1.02) 0.213
rs8018720 14 SEC23A G/C 1.01 (0.95–1.06) 0.841 0.99 (0.92–1.06) 0.778

Mendelian randomization estimate for the association with genetically estimated 25(OH)D

The results of the instrumental variables analyses are shown in Figure 1. They show no associations between genetically estimated 25(OH)D concentration and the risk of BE (per 20 nmol/L increase in 25(OH)D, summary instrumental variable OR, 1.21; 95% CI, 0.77–1.92). We found little heterogeneity in the estimated magnitudes of association between the six individual SNP variables (I2 = 46.8%, Pheterogeneity = 0.09). Likewise, in the instrumental variables analysis of EAC, there were no associations with genetically estimated 25(OH)D concentration (per 20 nmol/L increase in 25(OH)D, summary instrumental variable OR, 0.68; 95% CI, 0.39–1.19; I2 = 0%, Pheterogeneity = 0.99).

Figure 1A. Mendelian randomization estimates of the association between increased 25(OH)D concentration and risk of Barrett’s esophagus.

Figure 1A.

The OR estimates are per 20 nmol/L increase in 25(OH)D concentration. The hollow diamond represents the overall IV estimate with its 95% CI.

Assumptions of Mendelian randomization

To satisfy the first assumption that the instrumental variable is associated with the exposure of interest, we selected only SNPs with genome-wide statistically significant association with 25(OH)D concentration. We found no evidence for pleiotropy, with an MR-Egger intercept of −0.005 (P = 0.79) for BE and 0.007 (P = 0.75) for EAC. The weighted median method also yielded no statistically significant estimates (Supplementary Table 1). Finally, we evaluated whether the SNPs that we used as instrumental variables for 25(OH)D were associated with various other phenotypes. As shown in Supplementary Table 2, we did not find any associations at genome-wide significance (P < 5 ×10−8), other than rs17216707 with eGFR creatinine (P = 6 ×10−13).

DISCUSSION

In this Mendelian randomization study, we used genetic variants as instrumental variables for 25(OH)D and examined associations between 25(OH)D and risks of BE and EAC. We found no evidence that 25(OH)D concentration, as predicted by genotype, was associated with risks of BE or EAC. Thus, the study provides little evidence that 25(OH)D concentration is associated with risk of BE or EAC.

Observational studies have examined the association between 25(OH)D concentration and the risk of various cancers. A large number of case-control studies have reported conflicting results; however, these studies are susceptible to reverse causation. Likewise, results from prospective cohort studies have been inconclusive as a result of measuring 25(OH)D concentration at relatively unspecified times (anywhere from 0 to 20+ years) in the past before diagnosis. Given the limitations of these observational studies, it remains difficult to draw causal inferences, especially when inconsistent results are observed. Therefore, several Mendelian randomization studies have been recently conducted to examine associations between genetically predicted 25(OH)D concentration and risk of specific cancers. The advantage of Mendelian randomization studies is that the estimated magnitudes of associations are less likely to be affected by confounding and recall bias. A Mendelian randomization study involving data from 70,563 cancer patients and 84,418 control participants found that 25(OH)D concentration, as predicted by genotype, was not associated with the risks of prostate, breast, lung, colorectal, ovarian, pancreatic cancers or neuroblastoma (31). Likewise, a Mendelian randomization study found no association between genetically predicted 25(OH)D concentration and risks of oral or oropharyngeal cancer (32). Another Mendelian randomization study indicated an increased risk of ovarian cancer (OR, 1.27; 95% CI, 1.06–1.51) per 20nmol/L decrease in genetically predicted 25(OH)D concentrations in 10,065 ovarian cancer and 21,654 controls (33), but this association was not confirmed in a subsequent Mendelian randomization study of ovarian cancer.(31)

Few studies, and no Mendelian randomization studies, have examined associations between 25(OH)D and risks of BE and EAC (9, 11, 34). A nested case-control study from the Cohort Consortium Vitamin D Pooling Project of Rarer Cancers reported no association between circulating 25(OH)D and the risk of EAC (N=104) (34). A recent meta-analysis investigating associations between makers of vitamin D exposure (i.e., ultraviolet B exposure, vitamin D intake and vitamin D status) and risk of BE or EAC also found no association (11). Conversely, a case-control study in Australia reported a decreased risk of EAC with higher ultraviolet B exposure although, even if a true finding, this is not necessarily due to vitamin D (9). While there is some evidence that BE patients are often vitamin D insufficient (35, 36), studies to date have found no association between vitamin D intake and the risk of BE (10), and vitamin D supplementation has been shown to have no effect on risk of neoplastic progression in BE patients (35). Finally, a BE registry cohort study found no association between circulating 25(OH)D concentration and risk of prevalent or incident dysplasia or EAC in BE patients (36). The findings from the present Mendelian randomization study provide further evidence that 25(OH)D concentration is not associated with the risk of BE or EAC. Interestingly, the point estimates (i.e., ORs) for BE and EAC show opposite direction of effect for some of these SNPs, with evidence of moderate heterogeneity in the associations with BE but no heterogeneity for associations with EAC. Nonetheless, the point estimates are not significantly different from zero. Thus, a chance finding may explain the opposite directions.

Strengths of the current study include the high quality of the case-control and cohort studies used. The majority of the studies were population-based in design. Compared to results from traditional analyses of observational studies, the risk estimates using instrumental variables are less likely to be affected by confounding and other types of bias. We used six SNPs known to be associated with 25(OH)D concentration, all located in or near genes encoding enzymes and carrier proteins involved in vitamin D synthesis or metabolism, which provided a strong and valid instrumental variable for 25(OH)D concentration. Furthermore, through various statistical tests and database searches, we found little evidence of pleiotropic effects.

Our study also has limitations. Although we used a large worldwide consortial sample of patients, our study population was relatively small compared to other Mendelian randomization studies of vitamin D. However, few additional BE and EAC patients with non-genetic and genetic data are currently available, so such work may require additional time for study patients to accrue. While our findings are consistent with vitamin D not having a large causal effect on BE/EAC risk, as the six 25(OH)D-associated SNPs explain only ~3% of the variance of 25(OH)D concentration our study may have nonetheless been underpowered to detect medium to small effects. We are unable to evaluate whether the associations between 25(OH)D concentration and the risks of BE and EAC are nonlinear. It is possible that in populations with low 25(OH)D due to limited sun exposure, genetically determined variation in 25(OH)D may be associated with BE or EAC. Finally, we used summary-level data, which did not allow us to stratify analyses by covariates of interest, such as age, sex, smoking, body mass index, and gastroesophageal reflux symptoms.

In conclusion, this Mendelian randomization study provides little evidence that genetically estimated circulating 25(OH)D concentration is associated with the risk of BE and EAC.

Supplementary Material

1

Figure 1B. Mendelian randomization estimates of the association between increased 25(OH)D concentration and risk of esophageal adenocarcinoma.

Figure 1B.

The OR estimates are per 20 nmol/L increase in 25(OH)D concentration. The hollow diamond represents the overall IV estimate with its 95% CI.

Need to Know.

Background:

Epidemiology studies on 25(OH)D and the risk of EAC have produced conflicting results. We conducted a Mendelian randomization study to evaluate the association between 25(OH)D and risks of BE and EAC.

Findings:

In this Mendelian randomization study, genetically estimated 25(OH)D concentration was not associated with risk of BE or EAC.

Implications for patient care:

Together with data from prior studies of BE and EAC risk, our findings do not support screening for vitamin D deficiency for primary prevention of EAC.

Acknowledgements

The following UK hospitals participated in sample collection through the Stomach and Esophageal Cancer Study (SOCS) collaboration network: Addenbrooke’s Hospital, University College London, Bedford Hospital, Hinchingbrooke Hospital, Peterborough City Hospital, West Suffolk Hospital, Norfolk and Norwich University Hospital, Churchill Hospital, John Radcliffe Hospital, Velindre Hospital, St Bartholomew’s Hospital, Queen’s Hospital Burton, Queen Elisabeth Hospital, Diana Princess of Wales, Scunthorpe General Hospital, Royal Devon & Exeter Hospital, New Cross Hospital, Belfast City Hospital, Good Hope Hospital, Heartlands Hospital, South Tyneside District General Hospital, Cumberland Infirmary, West Cumberland Hospital, Withybush General Hospital, Stoke Mandeville Hospital, Wycombe General Hospital, Wexham Park Hospital, Southend Hospital, Guy’s Hospital, Southampton General Hospital, Bronglais General Hospital, Aberdeen Royal Infirmary, Manor Hospital, Clatterbridge Centre for Oncology, Lincoln County Hospital, Pilgrim Hospital, Grantham & District Hospital, St Mary’s Hospital London, Croydon University Hospital, Whipps Cross University Hospital, Wansbeck General Hospital, Hillingdon Hospital, Milton Keynes General Hospital, Royal Gwent Hospital, Tameside General Hospital, Castle Hill Hospital, St Richard’s Hospital, Ipswich Hospital, St Helens Hospital, Whiston Hospital, Countess of Chester Hospital, St Mary’s Hospital IOW, Queen Alexandra Hospital, Glan Clwyd Hospital, Wrexham Maelor Hospital, Darent Valley Hospital, Royal Derby Hospital, Derbyshire Royal Infirmary, Scarborough General Hospital, Kettering General Hospital, Kidderminster General Hospital, Royal Lancaster Infirmary, Furness General Hospital, Westmorland General Hospital, James Cook University Hospital, Friarage Hospital, Stepping Hill Hospital, St George’s Hospital London, Doncaster Royal Infirmary, Maidstone Hospital, Tunbridge Hospital, Prince Charles Hospital, Hartlepool Hospital, University Hospital of North Tees, Ysbyty Gwynedd, St. Jame’s University Hospital, Leeds General Infirmary, North Hampshire Hospital, Royal Preston Hospital, Chorley and District General, Airedale General Hospital, Huddersfield Royal Infirmary, Calderdale Royal Hospital, Torbay District General Hospital, Leighton Hospital, Royal Albert Edward Infirmary, Royal Surrey County Hospital, Bradford Royal Infirmary, Burnley General Hospital, Royal Blackburn Hospital, Royal Sussex County Hospital, Freeman Hospital, Royal Victoria Infirmary, Victoria Hospital Blackpool, Weston Park Hospital, Royal Hampshire County Hospital, Conquest Hospital, Royal Bournemouth General Hospital, Mount Vernon Hospital, Lister Hospital, William Harvey Hospital, Kent and Canterbury Hospital, Great Western Hospital, Dumfries and Galloway Royal Infirmary, Poole General Hospital, St Hellier Hospital, North Devon District Hospital, Salisbury District Hospital, Weston General Hospital, University Hospital Coventry, Warwick Hospital, George Eliot Hospital, Alexandra Hospital, Nottingham University Hospital, Royal Chesterfield Hospital, Yeovil District Hospital, Darlington Memorial Hospital, University Hospital of North Durham, Bishop Auckland General Hospital, Musgrove Park Hospital, Rochdale Infirmary, North Manchester General, Altnagelvin Area Hospital, Dorset County Hospital, James Paget Hospital, Derriford Hospital, Newham General Hospital, Ealing Hospital, Pinderfields General Hospital, Clayton Hospital, Dewsbury & District Hospital, Pontefract General Infirmary, Worthing Hospital, Macclesfield Hospital, University Hospital of North Staffordshire, Salford Royal Hospital, Royal Shrewsbury Hospital, Manchester Royal Infirmary.

Grant support: This work was primarily funded by National Institutes of Health (R01CA136725). The funders of the study had no role in the design, analysis, or interpretation of the data, nor in writing or publication decisions related to this article. JD was supported by a Research Training Grant from the Cancer Prevention and Research Institute of Texas (CPRIT; RP160097). PG was supported by a grant from National Health and Medical Research Council of Australia (1123248). GL was supported by the Alan B. Brown Chair in Molecular Genomics and by the CCO Chair in Experimental Therapeutics and Population Studies. The University of Cambridge received salary support for PDP from the NHS in the East of England through the Clinical Academic Reserve. BJR was supported by a grant (P01CA91955) from the National Institutes of Health /National Cancer Institute. NJS was supported by a grant (P30 DK034987) from the National Institutes of Health. TLV was supported by National Institutes of Health Established Investigator Award K05CA124911. SM was supported by an Australian Research Council Future Fellowship. DCW and REN were supported by Research Fellowships from the National Health and Medical Research Council of Australia.

Abbreviations:

EAC

esophageal adenocarcinoma

BE

Barrett’s esophagus

25(OH)D

25 hydroxy vitamin D

Footnotes

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Conflicts of Interest: The authors disclose no potential conflicts of interest.

REFERENCES

  • 1.Thrift AP, Whiteman DC. The incidence of esophageal adenocarcinoma continues to rise: analysis of period and birth cohort effects on recent trends. Ann Oncol. 2012;23(12):3155–62. [DOI] [PubMed] [Google Scholar]
  • 2.Thrift AP. The epidemic of oesophageal carcinoma: Where are we now? Cancer Epidemiol. 2016;41:88–95. [DOI] [PubMed] [Google Scholar]
  • 3.Reid BJ, Li X, Galipeau PC, Vaughan TL. Barrett’s oesophagus and oesophageal adenocarcinoma: time for a new synthesis. Nat Rev Cancer. 2010;10(2):87–101. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 4.Cook MB, Corley DA, Murray LJ, Liao LM, Kamangar F, Ye W, et al. Gastroesophageal reflux in relation to adenocarcinomas of the esophagus: a pooled analysis from the Barrett’s and Esophageal Adenocarcinoma Consortium (BEACON). PLoS One. 2014;9(7):e103508. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 5.Thrift AP, Kramer JR, Qureshi Z, Richardson PA, El-Serag HB. Age at onset of GERD symptoms predicts risk of Barrett’s esophagus. Am J Gastroenterol. 2013;108(6):915–22. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 6.Thrift AP, Shaheen NJ, Gammon MD, Bernstein L, Reid BJ, Onstad L, et al. Obesity and risk of esophageal adenocarcinoma and Barrett’s esophagus: a Mendelian randomization study. Journal of the National Cancer Institute. 2014;106(11). [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 7.Cook MB, Kamangar F, Whiteman DC, Freedman ND, Gammon MD, Bernstein L, et al. Cigarette smoking and adenocarcinomas of the esophagus and esophagogastric junction: a pooled analysis from the international BEACON consortium. Journal of the National Cancer Institute. 2010;102(17):1344–53. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 8.Cook MB, Shaheen NJ, Anderson LA, Giffen C, Chow WH, Vaughan TL, et al. Cigarette smoking increases risk of Barrett’s esophagus: an analysis of the Barrett’s and Esophageal Adenocarcinoma Consortium. Gastroenterology. 2012;142(4):744–53. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 9.Tran B, Lucas R, Kimlin M, Whiteman D, Neale R, Australian Cancer S. Association between ambient ultraviolet radiation and risk of esophageal cancer. Am J Gastroenterol. 2012;107(12):1803–13. [DOI] [PubMed] [Google Scholar]
  • 10.Mulholland HG, Murray LJ, Anderson LA, Cantwell MM, group Fs. Vitamin D, calcium and dairy intake, and risk of oesophageal adenocarcinoma and its precursor conditions. Br J Nutr. 2011;106(5):732–41. [DOI] [PubMed] [Google Scholar]
  • 11.Zgaga L, O’Sullivan F, Cantwell MM, Murray LJ, Thota PN, Coleman HG. Markers of Vitamin D Exposure and Esophageal Cancer Risk: A Systematic Review and Meta-analysis. Cancer Epidemiol Biomarkers Prev. 2016;25(6):877–86. [DOI] [PubMed] [Google Scholar]
  • 12.Smith GD, Ebrahim S. ‘Mendelian randomization’: can genetic epidemiology contribute to understanding environmental determinants of disease? International journal of epidemiology. 2003;32(1):1–22. [DOI] [PubMed] [Google Scholar]
  • 13.Lawlor DA, Harbord RM, Sterne JA, Timpson N, Davey Smith G. Mendelian randomization: using genes as instruments for making causal inferences in epidemiology. Stat Med. 2008;27(8):1133–63. [DOI] [PubMed] [Google Scholar]
  • 14.Greenland S An introduction to instrumental variables for epidemiologists. International journal of epidemiology. 2000;29(4):722–9. [DOI] [PubMed] [Google Scholar]
  • 15.Burgess S, Butterworth A, Thompson SG. Mendelian randomization analysis with multiple genetic variants using summarized data. Genetic epidemiology. 2013;37(7):658–65. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 16.Jiang X, O’Reilly PF, Aschard H, Hsu YH, Richards JB, Dupuis J, et al. Genome-wide association study in 79,366 European-ancestry individuals informs the genetic architecture of 25-hydroxyvitamin D levels. Nature communications. 2018;9(1):260. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 17.Gharahkhani P, Fitzgerald RC, Vaughan TL, Palles C, Gockel I, Tomlinson I, et al. Genome-wide association studies in oesophageal adenocarcinoma and Barrett’s oesophagus: a large-scale meta-analysis. The Lancet Oncology. 2016;17(10):1363–73. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 18.Levine DM, Ek WE, Zhang R, Liu X, Onstad L, Sather C, et al. A genome-wide association study identifies new susceptibility loci for esophageal adenocarcinoma and Barrett’s esophagus. Nature genetics. 2013;45(12):1487–93. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 19.Schmermund A, Mohlenkamp S, Stang A, Gronemeyer D, Seibel R, Hirche H, et al. Assessment of clinically silent atherosclerotic disease and established and novel risk factors for predicting myocardial infarction and cardiac death in healthy middle-aged subjects: rationale and design of the Heinz Nixdorf RECALL Study. Risk Factors, Evaluation of Coronary Calcium and Lifestyle. Am Heart J. 2002;144(2):212–8. [DOI] [PubMed] [Google Scholar]
  • 20.Palles C, Chegwidden L, Li X, Findlay JM, Farnham G, Castro Giner F, et al. Polymorphisms near TBX5 and GDF7 are associated with increased risk for Barrett’s esophagus. Gastroenterology. 2015;148(2):367–78. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 21.Didelez VMS, Sheehan NA. Assumptions of IV Methods for Observational Epidemiology. Stat Sci. 2010;25:22–40. [Google Scholar]
  • 22.Thomas DC, Lawlor DA, Thompson JR. Re: Estimation of bias in nongenetic observational studies using “Mendelian triangulation” by Bautista et al. Ann Epidemiol. 2007;17(7):511–3. [DOI] [PubMed] [Google Scholar]
  • 23.Burgess S, Bowden J, Fall T, Ingelsson E, Thompson SG. Sensitivity Analyses for Robust Causal Inference from Mendelian Randomization Analyses with Multiple Genetic Variants. Epidemiology. 2017;28(1):30–42. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 24.Afzal S, Brondum-Jacobsen P, Bojesen SE, Nordestgaard BG. Genetically low vitamin D concentrations and increased mortality: Mendelian randomisation analysis in three large cohorts. BMJ. 2014;349:g6330. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 25.Pierce BL, Burgess S. Efficient design for Mendelian randomization studies: subsample and 2-sample instrumental variable estimators. American journal of epidemiology. 2013;178(7):1177–84. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 26.Burgess S, Small DS, Thompson SG. A review of instrumental variable estimators for Mendelian randomization. Stat Methods Med Res. 2017;26(5):2333–55. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 27.Sheehan NA, Didelez V, Burton PR, Tobin MD. Mendelian randomisation and causal inference in observational epidemiology. PLoS Med. 2008;5(8):e177. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 28.Bowden J, Davey Smith G, Burgess S. Mendelian randomization with invalid instruments: effect estimation and bias detection through Egger regression. International journal of epidemiology. 2015;44(2):512–25. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 29.Bowden J, Davey Smith G, Haycock PC, Burgess S. Consistent Estimation in Mendelian Randomization with Some Invalid Instruments Using a Weighted Median Estimator. Genetic epidemiology. 2016;40(4):304–14. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 30.Staley JR, Blackshaw J, Kamat MA, Ellis S, Surendran P, Sun BB, et al. PhenoScanner: a database of human genotype-phenotype associations. Bioinformatics. 2016;32(20):3207–9. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 31.Dimitrakopoulou VI, Tsilidis KK, Haycock PC, Dimou NL, Al-Dabhani K, Martin RM, et al. Circulating vitamin D concentration and risk of seven cancers: Mendelian randomisation study. BMJ. 2017;359:j4761. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 32.Dudding T, Johansson M, Thomas SJ, Brennan P, Martin RM, Timpson NJ. Assessing the causal association between 25-hydroxyvitamin D and the risk of oral and oropharyngeal cancer using Mendelian randomization. Int J Cancer. 2018. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 33.Ong JS, Cuellar-Partida G, Lu Y, Australian Ovarian Cancer S, Fasching PA, Hein A, et al. Association of vitamin D levels and risk of ovarian cancer: a Mendelian randomization study. International journal of epidemiology. 2016;45(5):1619–30. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 34.Abnet CC, Chen Y, Chow WH, Gao YT, Helzlsouer KJ, Le Marchand L, et al. Circulating 25-hydroxyvitamin D and risk of esophageal and gastric cancer: Cohort Consortium Vitamin D Pooling Project of Rarer Cancers. American journal of epidemiology. 2010;172(1):94–106. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 35.Cummings LC, Thota PN, Willis JE, Chen Y, Cooper GS, Furey N, et al. A nonrandomized trial of vitamin D supplementation for Barrett’s esophagus. PloS one. 2017;12(9):e0184928. [DOI] [PMC free article] [PubMed] [Google Scholar]
  • 36.Thota PN, Kistangari G, Singh P, Cummings L, Hajifathalian K, Lopez R, et al. Serum 25-Hydroxyvitamin D Levels and the Risk of Dysplasia and Esophageal Adenocarcinoma in Patients with Barrett’s Esophagus. Dig Dis Sci. 2016;61(1):247–54. [DOI] [PubMed] [Google Scholar]

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