Abstract
Background:
Whether polymorphisms in VDR gene affect the risk of postmenopausal osteoporosis or not remain unclear. Thus, the authors performed a meta-analysis to more robustly assess associations between polymorphisms in VDR gene and the risk of postmenopausal osteoporosis by integrating the results of previous literature.
Methods:
Medline, Embase, Wanfang, VIP and CNKI were searched comprehensively for eligible literature, and 67 genetic association studies were finally selected to be included in this meta-analysis.
Results:
We found that ApaI rs7975232 (dominant comparison: OR = 0.77, P = 0.007; allele comparison: OR = 0.81, P = 0.04), BsmI rs1544410 (dominant comparison: OR = 0.69, P = 0.002; allele comparison: OR = 0.78, P = 0.008) and TaqI rs731236 (recessive comparison: OR = 1.32 , P = 0.01) polymorphisms were significantly associated with the risk of postmenopausal osteoporosis in Caucasians, whereas FokI rs10735810 polymorphism was significantly associated with the risk of postmenopausal osteoporosis in Asians (dominant comparison: OR = 0.61, P = 0.0001; recessive comparison: OR = 2.02, P = 0.001; allele comparison: OR = 0.68, P = 0.002).
Conclusions:
This meta-analysis shows that ApaI rs7975232, BsmI rs1544410 and TaqI rs731236 polymorphisms may affect the risk of postmenopausal osteoporosis in Caucasians, while BsmI rs1544410 polymorphism may affect the risk of postmenopausal osteoporosis in Asians.
Introduction
Postmenopausal osteoporosis (PMOP) is featured by a decreased bone mineral density and an increased risk of bone fractures in postmenopausal women (1, 2). According to a recent epidemiological research, postmenopausal osteoporosis currently affects nearly 50% of elderly women over 60 years old, and with more and more countries entering the aging society, the incidence of osteoporosis in postmenopausal women is still rapidly increasing, making it the most common disorder of bone metabolism for elderly women across the world (3, 4, 5).
The pathogenesis mechanisms of postmenopausal osteoporosis are still unclear despite previous investigations, but substantial evidence supports that vitamin D deficiency is definitely an important contributing factor to the development of postmenopausal osteoporosis (6, 7). Considering that the action of vitamin D, one of the most crucial modulating factor of bone metabolism, is mediated by the vitamin D receptor (VDR), it is thought that polymorphisms of VDR gene may also affect the risk of postmenopausal osteoporosis (8, 9, 10). Over the last decade, investigators across the world have repeatedly attempted to assess the associations between polymorphisms in VDR gene and the risk of postmenopausal osteoporosis, yet the relationships between these polymorphisms and the risk of postmenopausal osteoporosis are still inconclusive. So a meta-analysis was performed to robustly assess the associations between polymorphisms in VDR gene and the risk of postmenopausal osteoporosis by integrating the results of previous literature.
Materials and methods
This meta-analysis was conducted in accordance with the PRISMA guideline (11).
Literature search and inclusion criteria
Medline, Embase, Wanfang, VIP and CNKI were comprehensively searched by the authors using the below keywords: (vitamin D receptor OR VDR) AND (polymorphism OR polymorphic OR variation OR variant OR mutant OR mutation OR SNP OR genotypic OR genotype OR allelic OR allele) AND (postmenopausal OR postmenopause) AND (osteoporosis OR bone loss). Moreover, we also manually screened the references of retrieved literature to make up for the potential incompleteness of literature searching from databases.
Selection criteria of this meta-analysis were listed below: (1) studies of case–control or cohort design; (2) give genotypic frequencies of VDR polymorphisms in cases with postmenopausal osteoporosis and population-based controls; (3) the full manuscript with detailed genotypic frequencies of VDR polymorphisms is retrievable or buyable. Articles would be excluded if one of the following three criteria is satisfied: (1) studies without complete genotypic data of VDR polymorphisms in cases with postmenopausal osteoporosis and population-based controls; (2) narrative or systematic reviews, meta-analysis or comments; (3) case series of subjects with postmenopausal osteoporosis only. If duplicate reports are retrieved, we would only include the most complete one for integrated analyses.
Data extraction and quality assessment
The authors extracted the following data items from eligible studies: (1) last name of the leading author; (2) year of publication; (3) country and ethnicity of study population; (4) the number of cases with postmenopausal osteoporosis and population-based controls; (5) genotypic frequencies of VDR polymorphisms in cases with postmenopausal osteoporosis and population-based controls. We also examined Hardy–Weinberg equilibrium (HWE) by comparing the actual genotypic frequencies of investigated VDR polymorphisms to their expected distributions using the chi-square test. The significance threshold of HWE was set at 0.05, if P value > 0.05, then we considered that the genotypic distribution of the investigated polymorphism was in agreement with HWE. The quality of eligible literature was assessed by the Newcastle–Ottawa scale (NOS) (12), and these with a score of 7–9 were considered to be literature of good quality. Two authors extracted data and assessed quality of eligible literature in parallel. A thorough discussion until a consensus is reached would be endorsed in case of any discrepancy between two authors.
Statistical analyses
All statistical analyses in this meta-analysis were performed with the Cochrane Review Manager software version 5.3 (The Cochrane Collaboration, Software Update, Oxford, United Kingdom). Associations between VDR gene polymorphisms and the risk of postmenopausal osteoporosis were explored by using odds ratio and its 95 % CI. The statistically significant P value was set at 0.05. All investigated VDR polymorphisms have a major allele (M) and a minor allele (m), the dominant comparison was defined as MM vs Mm + mm, the recessive comparison was defined as mm vs MM + Mm, the over-dominant comparison was defined as Mm vs MM + mm, and the allele comparison was defined as M vs m. The authors used I2 statistics to estimate heterogeneities among included studies. The authors would use DerSimonian–Laird method, which is also known as the random effect model, to integrate the results of eligible studies if I2 is larger than 50%. Otherwise, the authors would use Mantel–Haenszel method, which is also known as the fixed effect model, to integrate the results of eligible studies. Meanwhile, the authors also conduct subgroup analyses by ethnic groups. Stabilities of integrated results were tested by deleting studies that violated HWE, and then integrating the results of the rest of eligible studies. Publication biases were evaluated by assessing symmetry of funnel plots.
Results
Characteristics of included studies
Five hundred and seven papers were retrieved by the authors by using our searching strategy. One hundred and thirty-three papers were then selected to screen for eligibility after omitting unrelated and repeated items. Thirty-eight reviews and 13 case series were further excluded, and another 15 papers without complete genotypic data were further excluded by the authors. Totally 67 studies met the inclusion criteria, and were finally enrolled for integrated analyses (Fig. 1). Data extracted from eligible studies were summarized in Table 1.
The characteristics of included studies in current meta-analysis.
First author, year |
Country |
Ethnicity |
Sample size |
Genotypes (wtwt/wtmt/mtmt) |
P-value for HWE |
NOS score |
|
---|---|---|---|---|---|---|---|
Cases |
Controls |
||||||
ApaI rs7975232 | |||||||
Ahmad 2018 | India | Mixed | 254/254 | 62/140/52 | 75/134/45 | 0.264 | 7 |
Castelán-Martínez 2015 | Mexico | Mixed | 387/147 | 141/160/86 | 46/75/26 | 0.631 | 7 |
Chen 2007 | China | Asian | 155/113 | 108/40/7 | 60/41/12 | 0.223 | 7 |
Dabirnia 2016 | Iran | Mixed | 50/50 | 24/25/1 | 30/18/2 | 0.729 | 7 |
Douroudis 2003 | Hellenic Republic | Caucasian | 35/44 | 11/14/10 | 17/26/1 | 0.016 | 7 |
Duman 2004 | Turkey | Caucasian | 75/66 | 13/56/6 | 15/45/6 | 0.002 | 7 |
Dundar 2009 | Turkey | Caucasian | 112/24 | 26/61/25 | 8/14/2 | 0.231 | 7 |
Ge 2009 | China | Asian | 353/208 | 160/157/36 | 102/84/22 | 0.453 | 8 |
González-Mercado 2013 | Mexico | Mixed | 232/87 | 79/118/35 | 29/41/17 | 0.715 | 7 |
Gu 2010 | China | Asian | 186/148 | 79/86/21 | 74/61/13 | 0.932 | 7 |
Iván 2008 | Chile | Caucasian | 67/59 | 25/31/11 | 18/27/14 | 0.536 | 7 |
Kim 2015 | Korea | Asian | 153/47 | 97/53/3 | 24/19/4 | 0.931 | 7 |
Langdahl 2000 | Denmark | Caucasian | 78/74 | 22/44/12 | 25/32/17 | 0.283 | 7 |
Liang 2002 | China | Asian | 30/30 | 20/6/4 | 27/2/1 | 0.011 | 7 |
Luan 2011 | China | Asian | 140/88 | 71/56/13 | 44/34/10 | 0.390 | 7 |
Marozik 2013 | Belarus | Caucasian | 54/77 | 7/24/23 | 29/34/14 | 0.472 | 7 |
Marozik 2018 | Lithuania | Caucasian | 149/172 | 27/67/55 | 60/74/38 | 0.105 | 7 |
Meng 2018 | China | Asian | 90/246 | 60/25/5 | 161/69/16 | 0.028 | 8 |
Mitra 2006 | India | Mixed | 119/97 | 50/44/25 | 34/33/30 | 0.002 | 7 |
Mosaad 2014 | Egypt | Mixed | 30/150 | 13/15/2 | 69/71/10 | 0.142 | 7 |
Riggs 1995 | USA | Mixed | 30/128 | 12/19/9 | 38/59/31 | 0.394 | 7 |
Sassi 2015 | Tunisia | Mixed | 335/231 | 130/143/62 | 90/115/26 | 0.233 | 7 |
Seremak-Mrozikiewicz 2009 | Poland | Caucasian | 163/63 | 35/82/46 | 12/32/19 | 0.821 | 7 |
Tanriover 2010 | Turkey | Caucasian | 50/50 | 15/23/12 | 22/15/13 | 0.007 | 8 |
Uysal 2008 | Turkey | Caucasian | 100/146 | 35/50/15 | 46/79/21 | 0.165 | 7 |
Vandevyver 1997 | Belgium | Caucasian | 87/699 | 20/45/22 | 197/375/127 | 0.027 | 8 |
Wu 2016 | China | Asian | 79/234 | 43/27/9 | 105/111/18 | 0.123 | 7 |
Wu 2019 | China | Asian | 610/616 | 331/218/61 | 366/207/43 | 0.070 | 8 |
Xie 2005 | China | Asian | 295/56 | 240/43/12 | 34/16/6 | 0.075 | 7 |
Yoldemir 2011 | Turkey | Caucasian | 130/130 | 34/60/36 | 31/73/26 | 0.155 | 7 |
Zajickova 2002 | Czech Republic | Caucasian | 65/33 | 23/33/9 | 10/17/6 | 0.793 | 7 |
BsmI rs1544410 | |||||||
Ahmad 2018 | India | Mixed | 254/254 | 54/137/63 | 54/152/48 | 0.002 | 7 |
Berg 1996 | Norway | Caucasian | 19/30 | 4/8/7 | 8/11/11 | 0.156 | 7 |
Boroń 2015 | Poland | Caucasian | 278/292 | 101/121/56 | 128/113/51 | 0.004 | 7 |
Cheishvili 2017 | Israel | Mixed | 37/37 | 13/11/13 | 15/12/10 | 0.039 | 7 |
Chen 2003 | China | Asian | 78/81 | 65/13/0 | 69/12/0 | 0.472 | 7 |
Douroudis 2003 | Hellenic Republic | Caucasian | 35/44 | 20/12/3 | 29/10/5 | 0.019 | 7 |
Duman 2004 | Kuwait | Mixed | 75/66 | 54/18/3 | 42/17/7 | 0.021 | 7 |
Efesoy 2011 | Turkey | Caucasian | 40/30 | 12/23/5 | 10/15/5 | 0.876 | 7 |
Ge 2009 | China | Asian | 353/208 | 314/33/6 | 192/12/4 | <0.001 | 8 |
Gennari 1998 | Italy | Caucasian | 155/136 | 23/92/40 | 49/76/11 | 0.013 | 7 |
González-Mercado 2013 | Mexico | Mixed | 232/88 | 143/76/13 | 46/38/4 | 0.267 | 7 |
Houston 1996 | UK | Caucasian | 44/44 | 17/19/8 | 16/19/9 | 0.450 | 7 |
Huang 2000 | China | Asian | 14/27 | 13/1/0 | 26/1/0 | 0.922 | 7 |
Hussien 2013 | Egypt | Mixed | 150/50 | 50/57/43 | 19/21/10 | 0.351 | 7 |
Iván 2008 | Chile | Caucasian | 67/59 | 10/46/11 | 13/37/9 | 0.046 | 7 |
Kim 2015 | Korea | Asian | 153/47 | 142/11/0 | 42/5/0 | 0.700 | 7 |
Langdahl 2000 | Denmark | Caucasian | 80/80 | 23/38/19 | 25/34/21 | 0.186 | 7 |
Li 2000 | China | Asian | 96/42 | 54/36/6 | 20/21/1 | 0.095 | 7 |
Liang 2002 | China | Asian | 30/30 | 28/1/1 | 30/0/0 | NA | 7 |
Lim 1995 | Korea | Asian | 72/70 | 61/9/2 | 60/9/1 | 0.349 | 7 |
Liu 2005 | China | Asian | 56/89 | 50/6/0 | 76/11/2 | 0.060 | 7 |
Marozik 2013 | Belarus | Caucasian | 54/77 | 11/31/12 | 40/26/11 | 0.062 | 7 |
Marozik 2018 | Lithuania | Caucasian | 149/172 | 32/64/53 | 64/73/35 | 0.098 | 7 |
Melhus 1994 | Sweden | Caucasian | 70/76 | 14/29/27 | 34/35/7 | 0.637 | 8 |
Mencej-Bedrac 2009 | Slovenia | Caucasian | 240/228 | 103/110/27 | 88/100/40 | 0.215 | 8 |
Meng 2017 | China | Asian | 90/246 | 74/12/4 | 216/24/6 | <0.001 | 7 |
Mitra 2006 | India | Mixed | 119/97 | 51/46/22 | 40/38/19 | 0.080 | 7 |
Mosaad 2014 | Egypt | Mixed | 30/150 | 2/19/9 | 36/74/40 | 0.877 | 7 |
Musumeci 2009 | Iran | Mixed | 50/20 | 27/15/8 | 17/2/1 | 0.047 | 7 |
Perez 2008 | Argentina | Mixed | 64/68 | 17/35/12 | 20/32/16 | 0.649 | 7 |
Pollak 2001 | Israel | Mixed | 75/143 | 24/38/13 | 60/67/16 | 0.675 | 7 |
Pouresmaeili 2013 | Iran | Mixed | 64/82 | 17/33/14 | 36/33/13 | 0.252 | 7 |
Riggs 1995 | USA | Mixed | 40/129 | 9/20/11 | 20/61/48 | 0.932 | 7 |
Seremak-Mrozikiewicz 2009 | Poland | Caucasian | 163/63 | 70/66/27 | 26/27/10 | 0.506 | 7 |
Tanriover 2010 | Turkey | Caucasian | 50/50 | 16/19/15 | 24/19/7 | 0.320 | 8 |
Techapatiphandee 2018 | Thailand | Asian | 105/132 | 85/19/1 | 103/25/4 | 0.123 | 7 |
Uysal 2008 | Turkey | Caucasian | 100/146 | 18/48/34 | 24/78/44 | 0.283 | 7 |
Vandevyver 1997 | Belgium | Caucasian | 86/698 | 24/50/12 | 203/368/127 | 0.076 | 8 |
Wang 2007 | China | Asian | 50/48 | 43/7/0 | 39/9/0 | 0.474 | 7 |
Yanagi 1996 | Japan | Asian | 66/66 | 22/12/12 | 57/7/2 | 0.013 | 7 |
Yoldemir 2011 | Turkey | Caucasian | 130/130 | 35/73/22 | 43/65/22 | 0.760 | 7 |
Zajickova 2002 | Czech Republic | Caucasian | 65/33 | 20/24/21 | 10/13/10 | 0.223 | 7 |
Zhang 1998 | China | Asian | 17/164 | 14/3/0 | 148/16/0 | 0.511 | 8 |
Zhang 2000 | China | Asian | 77/35 | 38/33/6 | 14/18/3 | 0.403 | 7 |
Zhu 2004 | China | Asian | 40/158 | 26/8/6 | 105/46/7 | 0.500 | 7 |
FokI rs10735810 | |||||||
Ahmad 2018 | India | Mixed | 254/254 | 148/92/14 | 169/80/5 | 0.20 | 7 |
Castelán-Martínez 2015 | Mexico | Mixed | 232/88 | 61/118/53 | 24/45/19 | 0.807 | 7 |
Choi 2000 | Korea | Asian | 48/65 | 12/23/13 | 26/33/6 | 0.327 | 7 |
González-Mercado 2013 | Mexico | Mixed | 88/88 | 25/48/15 | 24/45/19 | 0.807 | 7 |
Gu 2010 | China | Asian | 186/148 | 46/100/40 | 40/84/24 | 0.071 | 7 |
Iván 2008 | Chile | Caucasian | 67/59 | 29/27/11 | 27/25/7 | 0.744 | 7 |
Kanan 2013 | Jordan | Mixed | 120/90 | 40/62/18 | 29/48/13 | 0.336 | 7 |
Kim 2015 | Korea | Asian | 153/47 | 50/83/20 | 14/25/8 | 0.577 | 7 |
Langdahl 2000 | Denmark | Caucasian | 30/128 | 12/19/9 | 38/59/31 | 0.394 | 7 |
Li 2019 | China | Asian | 224/155 | 66/103/55 | 58/68/29 | 0.259 | 7 |
Lisker 2003 | Mexico | Mixed | 65/57 | 27/29/9 | 20/29/8 | 0.625 | 7 |
Lucotte 1999 | France | Caucasian | 124/105 | 45/69/10 | 40/52/13 | 0.535 | 7 |
Mamolini 2017 | Italy | Caucasian | 170/73 | 97/60/13 | 40/25/8 | 0.194 | 7 |
Mansour 2010 | Iran | Mixed | 50/20 | 34/9/7 | 20/0/0 | NA | 7 |
Mencej-Bedrac 2009 | Slovenia | Caucasian | 240/228 | 88/108/44 | 105/97/26 | 0.618 | 8 |
Mitra 2006 | India | Mixed | 119/97 | 38/42/39 | 46/33/18 | 0.011 | 7 |
Mohammadi 2015 | Iran | Mixed | 96/356 | 52/36/8 | 198/128/30 | 0.158 | 7 |
Mosaad 2014 | Egypt | Mixed | 30/150 | 23/6/1 | 93/55/2 | 0.049 | 7 |
Pérez 2008 | Argentina | Mixed | 64/68 | 22/32/10 | 22/36/10 | 0.444 | 7 |
Tanriover 2010 | Turkey | Caucasian | 50/50 | 27/22/1 | 29/18/3 | 0.926 | 8 |
Techapatiphandee 2018 | Thailand | Asian | 105/132 | 31/46/28 | 41/73/18 | 0.106 | 7 |
Wu 2019 | China | Asian | 610/616 | 296/235/79 | 404/186/26 | 0.436 | 8 |
Xing 2011 | China | Asian | 32/70 | 7/14/11 | 27/35/8 | 0.506 | 7 |
Yasovanthi 2011 | India | Mixed | 247/254 | 104/119/24 | 122/124/8 | <0.001 | 8 |
Yoldemir 2011 | Turkey | Caucasian | 130/130 | 66/55/9 | 62/55/13 | 0.876 | 7 |
Zajickova 2002 | Czech Republic | Caucasian | 78/74 | 22/44/12 | 25/32/17 | 0.283 | 7 |
TaqI rs731236 | |||||||
Ahmad 2018 | India | Mixed | 254/254 | 124/96/34 | 89/123/42 | 0.964 | 7 |
Dabirnia 2016 | Iran | Mixed | 50/50 | 20/24/6 | 16/29/5 | 0.121 | 7 |
Duman 2004 | Kuwait | Mixed | 75/66 | 10/42/23 | 15/28/23 | 0.259 | 7 |
Gennari 1998 | Italy | Caucasian | 160/144 | 33/87/40 | 62/71/11 | 0.126 | 7 |
González-Mercado 2013 | Mexico | Mixed | 232/88 | 142/77/13 | 46/36/6 | 0.769 | 7 |
Iván 2008 | Chile | Caucasian | 67/59 | 26/31/10 | 17/34/8 | 0.167 | 7 |
Kim 2015 | Korea | Asian | 153/47 | 140/12/1 | 42/5/0 | 0.700 | 7 |
Langdahl 2000 | Denmark | Caucasian | 46/284 | 11/30/5 | 91/159/34 | 0.005 | 7 |
Larin 2015 | Ukraine | Caucasian | 44/30 | 20/18/6 | 14/12/4 | 0.584 | 7 |
Marozik 2013 | Belarus | Caucasian | 54/77 | 17/26/11 | 39/24/14 | 0.008 | 7 |
Marozik 2018 | Lithuania | Caucasian | 149/172 | 38/62/49 | 58/74/40 | 0.088 | 7 |
Masi 1998 | Italy | Caucasian | 90/111 | 41/36/13 | 38/64/9 | 0.013 | 7 |
Mitra 2006 | India | Mixed | 119/97 | 34/42/43 | 44/31/22 | 0.001 | 7 |
Mosaad 2014 | Egypt | Mixed | 30/150 | 9/19/2 | 39/74/37 | 0.872 | 7 |
Riggs 1995 | USA | Mixed | 31/130 | 11/23/7 | 53/57/20 | 0.475 | 7 |
Sassi 2015 | Tunisia | Mixed | 335/231 | 165/128/42 | 103/95/33 | 0.152 | 7 |
Seremak-Mrozikiewicz 2009 | Poland | Caucasian | 163/63 | 78/59/26 | 22/29/12 | 0.659 | 7 |
Tanriover 2010 | Turkey | Caucasian | 50/50 | 15/29/6 | 25/17/8 | 0.102 | 8 |
Techapatiphandee 2018 | Thailand | Asian | 105/132 | 97/6/2 | 116/15/1 | 0.513 | 7 |
Uysal 2008 | Turkey | Caucasian | 100/146 | 40/46/14 | 54/75/17 | 0.237 | 7 |
Vandevyver 1997 | Belgium | Caucasian | 46/284 | 11/30/5 | 91/159/34 | 0.005 | 8 |
Wang 2013 | China | Asian | 92/98 | 47/48/7 | 48/40/10 | 0.698 | 7 |
Yoldemir 2011 | Turkey | Caucasian | 130/130 | 51/59/20 | 49/59/22 | 0.558 | 7 |
Zajickova 2002 | Czech Republic | Caucasian | 65/33 | 11/31/23 | 8/14/11 | 0.407 | 7 |
Ziablitsev 1994 | Ukraine | Caucasian | 44/30 | 20/18/6 | 14/12/4 | 0.584 | 7 |
HWE, Hardy–Weinberg equilibrium; mt, Mutant type; NA, not available; NOS, Newcastle-Ottawa scale; wt, Wild type;.
ApaI rs7975232 polymorphism and the risk of postmenopausal osteoporosis
Thirty papers assessed relationship between ApaI rs7975232 polymorphism and the risk of postmenopausal osteoporosis. The integrated analyses demonstrated that ApaI rs7975232 polymorphism was significantly associated with the risk of postmenopausal osteoporosis in overall population (recessive comparison: OR = 1.20, P = 0.004) and Caucasians (dominant comparison: OR = 0.77, P = 0.007; allele comparison: OR = 0.81, P = 0.04), but not in Asians (Table 2).
Integrated analyses results of the current meta-analysis.
Variables | Sample size | Dominant comparison | Recessive comparison | Over-dominant comparison | Allele comparison | ||||
---|---|---|---|---|---|---|---|---|---|
P-value | OR (95% CI) | P-value | OR (95% CI) | P-value | OR (95% CI) | P-value | OR (95% CI) | ||
ApaI rs7975232 | |||||||||
Overall | 4693/4567 | 0.64 | 0.96 (0.83–1.12) | 0.004 | 1.20 (1.06–1.37) | 0.59 | 0.98 (0.89–1.07) | 0.53 | 0.96 (0.85–1.09) |
Caucasian | 1165/1637 | 0.007 | 0.77 (0.64–0.93) | 0.11 | 1.31 (0.94–1.82) | 0.85 | 0.98 (0.83–1.16) | 0.04 | 0.81 (0.67–0.99) |
Asian | 2091/1786 | 0.39 | 1.14 (0.85–1.52) | 0.59 | 0.90 (0.61–1.32) | 0.40 | 0.91 (0.72–1.14) | 0.38 | 1.12 (0.87–1.45) |
BsmI rs1544410 | |||||||||
Overall | 4312/5015 | 0.002 | 0.77 (0.65–0.91) | 0.0001 | 1.28 (1.13–1.45) | 0.17 | 1.07 (0.97–1.18) | 0.002 | 0.80 (0.70–0.92) |
Caucasian | 1825/2388 | 0.002 | 0.69 (0.55–0.87) | 0.08 | 1.29 (0.97–1.71) | 0.05 | 1.14 (1.00–1.30) | 0.008 | 0.78 (0.65–0.94) |
Asian | 1297/1443 | 0.30 | 0.81 (0.54–1.21) | 0.06 | 1.76 (0.98–3.17) | 0.99 | 1.00 (0.79–1.27) | 0.17 | 0.74 (0.48–1.14) |
FokI rs10735810 | |||||||||
Overall | 3612/3602 | <0.0001 | 0.76 (0.69–0.84) | 0.005 | 1.40 (1.11–1.78) | 0.07 | 1.10 (0.99–1.21) | 0.04 | 0.86 (0.75–0.99) |
Caucasian | 889/847 | 0.30 | 0.90 (0.74–1.10) | 0.89 | 1.02 (0.76–1.37) | 0.08 | 1.19 (0.98–1.45) | 0.71 | 1.04 (0.83–1.31) |
Asian | 1358/1233 | 0.0001 | 0.61 (0.52–0.72) | 0.001 | 2.02 (1.32–3.08) | 0.18 | 1.12 (0.95–1.31) | 0.002 | 0.68 (0.54–0.87) |
TaqI rs731236 | |||||||||
Overall | 2684/2956 | 0.57 | 0.94 (0.76–1.16) | 0.13 | 1.13 (0.96–1.32) | 0.67 | 1.04 (0.87–1.24) | 0.93 | 0.99 (0.86–1.15) |
Caucasian | 1208/1613 | 0.20 | 0.83 (0.62–1.10) | 0.01 | 1.32 (1.06–1.63) | 0.81 | 1.02 (0.87–1.20) | 0.16 | 0.87 (0.73–1.05) |
Asian | 350/277 | 0.33 | 1.24 (0.80–1.93) | 0.79 | 0.89 (0.37–2.14) | 0.77 | 0.89 (0.40–1.96) | 0.06 | 1.42 (0.98–2.06) |
The values in bold represent there is statistically significant differences between cases and controls.
NA, not available; OR, odds ratio.
BsmI rs1544410 polymorphism and the risk of postmenopausal osteoporosis
Forty-five papers assessed relationship between BsmI rs1544410 polymorphism and the risk of postmenopausal osteoporosis. The integrated analyses demonstrated that BsmI rs1544410 polymorphism was significantly associated with the risk of postmenopausal osteoporosis in overall population (dominant comparison: OR = 0.77, P = 0.002; recessive comparison: OR = 1.28, P = 0.0001; allele comparison: OR = 0.80, P = 0.002) and Caucasians (dominant comparison: OR = 0.69, P = 0.002; allele comparison: OR = 0.78, P = 0.008), but not in Asians (Table 2).
FokI rs10735810 polymorphism and the risk of postmenopausal osteoporosis
Twenty-six papers assessed relationship between FokI rs10735810 polymorphism and the risk of postmenopausal osteoporosis. The integrated analyses demonstrated that FokI rs10735810 polymorphism was significantly associated with the risk of osteoporosis in overall population (dominant comparison: OR = 0.76, P < 0.0001; recessive comparison: OR = 1.40, P = 0.005; allele comparison: OR = 0.86, P = 0.04) and Asians (dominant comparison: OR = 0.61, P = 0.0001; recessive comparison: OR = 2.02, P = 0.001; allele comparison: OR = 0.68, P = 0.002), but not in Caucasians (Table 2).
TaqI rs731236 polymorphism and the risk of postmenopausal osteoporosis
Twenty-five papers assessed relationship between TaqI rs731236 polymorphism and the risk of postmenopausal osteoporosis. The integrated analyses demonstrated that TaqI rs731236 polymorphism was significantly associated with the risk of postmenopausal osteoporosis in Caucasians (recessive comparison: OR = 1.32, P = 0.01), but not in Asians (Table 2).
Sensitivity analyses
The authors examined stabilities of integrated analyses results by deleting studies that violated HEW, and then integrating the results of the rest of studies. The trends of associations were not significantly altered in sensitivity analyses, which indicated that from statistical perspective, our integrated analyses results were reliable and stable.
Publication biases
The authors examined potential publication biases in this meta-analysis by assessing symmetry of funnel plots. Funnel plots were found to be generally symmetrical, which indicated that our integrated analyses results were not likely to be severely deteriorated by publication biases (Supplementary Fig. 1, see section on supplementary materials given at the end of this article).
Discussion
This meta-analysis, robustly assessed associations between gene polymorphisms in VDR and the risk of postmenopausal osteoporosis. The integrated analyses results showed that ApaI rs7975232, BsmI rs1544410 and TaqI rs731236 polymorphisms were significantly associated with the risk of postmenopausal osteoporosis in Caucasians, whereas FokI rs10735810 polymorphism was significantly associated with the risk of postmenopausal osteoporosis in Asians.
The following points should be considered when interpreting our integrated findings. First, based on the findings of previous observational studies, we speculated that these investigated VDR polymorphisms may alter mRNA expression level or protein function of VDR, impact vitamin D metabolism, and then affect the risk of postmenopausal osteoporosis (13, 14). Nevertheless, further experimental studies are still warranted to figure out the exact mechanisms underlying the observed positive associations between VDR gene polymorphisms and the risk of postmenopausal osteoporosis in the current meta-analysis. Second, we want to study all polymorphic loci of VDR gene initially. Nevertheless, our comprehensive literature searching did not reveal sufficient eligible literature to support integrated analyses for other polymorphic loci of VDR gene, so we only explored associations with the risk of postmenopausal osteoporosis for four most commonly investigated polymorphisms of VDR gene in this meta-analysis. Third, it is worth noting that previously, Zhang et al. (15) also tried to investigate associations between VDR gene polymorphisms and postmenopausal osteoporosis through a meta-analysis. Nevertheless, this previous meta-analysis only covered relevant genetic association studies that were published before 2015. Since our literature searching revealed that many related studies were published after 2015, an updated meta-analysis like ours is of course warranted to get more reliable findings. Consistent with the previous meta-analysis, similar significant findings for ApaI rs7975232, FokI rs10735810 and TaqI rs731236 polymorphisms were observed in our integrated analyses. Additionally, we also found that BsmI rs1544410 polymorphism was significantly associated with the risk of postmenopausal osteoporosis in overall population and Caucasians, which was failed to be detected by the previous meta-analysis. Considering that our integrated analyses were derived from more eligible studies, our observations should be considered as a valuable supplement to pre-existing literature.
The major limitations of our integrated analyses were listed below. First, our integrated analyses results were derived from unadjusted pooling of previous literature. Without access to raw data of eligible studies, we can only assess associations between VDR gene polymorphisms and the risk of postmenopausal osteoporosis based on recalculations of raw genotypic frequencies provided by eligible literature, and we need to admit that lack of further adjustment for baseline characteristics may possibly influence reliability of our findings (16). Secondly, environmental factors such as food intake, sunshine exposure or exercise levels may also influence associations between polymorphisms in VDR gene and the risk of postmenopausal osteoporosis. However, most of the authors only paid attention to genetic associations in their publications, so it is impossible for us to explore genetic–environmental interactions in a meta-analysis based on these previous literature (17). Thirdly, we did not select gray literature for integrated analyses because this literature is generally considered to be incomplete and it is almost impossible for us to extract all necessary data items, or assess their quality through the NOS scale. Nevertheless, since we did not select gray literature for integrated analyses, despite that funnel plots were found to be overall symmetrical, it should be acknowledged that publication biases still may influence reliability of our integrated analyses results (18).
In conclusion, this meta-analysis shows that ApaI rs7975232, BsmI rs1544410 and TaqI rs731236 polymorphisms may affect the risk of postmenopausal osteoporosis in Caucasians, while FokI rs10735810 polymorphism may affect the risk of postmenopausal osteoporosis in Asians. Further studies with larger sample sizes are still needed to confirm our findings. In addition, scholars should also try to reveal the exact underlying mechanisms of the positive associations observed between aforementioned VDR polymorphisms and the risk of postmenopausal osteoporosis in the future.
Supplementary materials
This is linked to the online version of the paper at https://doi.org/10.1530/EC-20-0296.
Declaration of interest
The authors declare that there is no conflict of interest that could be perceived as prejudicing the impartiality of the research reported.
Funding
This work did not receive any specific grant from any funding agency in the public, commercial, or not-for-profit sector.
Author contribution statement
Lijuan Fu and Qijun Si conceived and designed this meta-analysis. Lijuan Fu and Jinhuan Ma searched literature. Sumei Yan analyzed data. Lijuan Fu and Qijun Si wrote the manuscript. All authors have approved the final manuscript as submitted.
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