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Erschienen in: BMC Medical Genetics 1/2010

Open Access 01.12.2010 | Research article

The role of height-associated loci identified in genome wide association studies in the determination of pediatric stature

verfasst von: Jianhua Zhao, Mingyao Li, Jonathan P Bradfield, Haitao Zhang, Frank D Mentch, Kai Wang, Patrick M Sleiman, Cecilia E Kim, Joseph T Glessner, Cuiping Hou, Brendan J Keating, Kelly A Thomas, Maria L Garris, Sandra Deliard, Edward C Frackelton, F George Otieno, Rosetta M Chiavacci, Robert I Berkowitz, Hakon Hakonarson, Struan FA Grant

Erschienen in: BMC Medical Genetics | Ausgabe 1/2010

Abstract

Background

Human height is considered highly heritable and correlated with certain disorders, such as type 2 diabetes and cancer. Despite environmental influences, genetic factors are known to play an important role in stature determination. A number of genetic determinants of adult height have already been established through genome wide association studies.

Methods

To examine 51 single nucleotide polymorphisms (SNPs) corresponding to the 46 previously reported genomic loci for height in 8,184 European American children with height measurements. We leveraged genotyping data from our ongoing GWA study of height variation in children in order to query the 51 SNPs in this pediatric cohort.

Results

Sixteen of these SNPs yielded at least nominally significant association to height, representing fifteen different loci including EFEMP1-PNPT1, GPR126, C6orf173, SPAG17, Histone class 1, HLA class III and GDF5-UQCC. Other loci revealed no evidence for association, including HMGA1 and HMGA2. For the 16 associated variants, the genotype score explained 1.64% of the total variation for height z-score.

Conclusion

Among 46 loci that have been reported to associate with adult height to date, at least 15 also contribute to the determination of height in childhood.
Hinweise

Electronic supplementary material

The online version of this article (doi:10.​1186/​1471-2350-11-96) contains supplementary material, which is available to authorized users.
Jianhua Zhao, Mingyao Li contributed equally to this work.

Competing interests

The authors declare that they have no competing interests.

Authors' contributions

JZ, HH and SFAG designed the study and supervised the data analysis and interpretation. JZ, ML, HZ and SFAG conducted the statistical analyses. CEK, CH, KAT, MLG, SD, ECF and FGO directed the genotyping and related sample handling. JPB, FDM, KW, PMS, JTG and BJG provided bioinformatics support. RMC and RIB coordinated the sample recruitment. JZ, ML, HH and SFAG drafted the manuscript. All the authors read and approved the final manuscript.

Background

Height has been correlated with various disorders, including the observations that taller people are at a higher risk of developing cancer and shorter people are more likely to present with type 2 diabetes [13]. Determination of height in humans has long been considered to be largely influenced by genetic factors; indeed, twin and family studies have suggested that as much as 90% of variation in human height is genetically determined[48].
For many years, studies have attempted to identify genetic factors influencing human height in order to provide insights into human growth and development. Prior to 2007, genome-wide linkage and candidate-gene association studies had limited success in this regard; however, with the recent emergence of genome wide association (GWA) studies, tens of common genetics variants influencing height have now been uncovered, primarily in adults[914].
Weedon et al published the first GWA study of height using the Affymetrix GeneChip Human Mapping 500 K platform on nearly 5,000 individuals of self-reported European ancestry[9]. As a consequence, they observed association to common variation in the mobility group-A2 (HMGA2) oncogene. Follow-up analyses in approximately 19,000 more individuals (both adults and children) revealed strong replication of this observation. A subsequent GWA study uncovered another height locus, GDF5-UQCC, using data from the FUSION and SardiNIA cohorts[10].
These initial discoveries were followed by four meta-analyses with larger sample sizes, which collectively revealed 44 additional height loci [1114]. However, some lack of overlap between the results of these GWA studies has been observed, which may be partly explained by the different statistical powers of the studies[15].
Although the causal variants at these loci have still to be elucidated, it has been shown that many of the implicated genes are involved in pathways influencing bone and cartilage development, including skeletal development signaling (PTCH1, HHIP, BMPs, GDF5), the extracellular matrix (ACAN, FBLN5, EFEMP1, ADAMTS17, ADAMTSL3), chromatin structure and regulation (DOT1L, SCMH1, HMGA2) and cell cycle regulation and mitosis (CDK6, ANAPC13, NCAPG)[15]. In addition, some of the loci were novel and are now a clear focus of attention in height biology.
In this study we aimed at examining these initial and meta-analysis findings that were previously reported to be genome wide significant in a large European American pediatric cohort with height measurements to determine the relative impact of these variants on childhood stature. For this purpose, we leveraged genotyping data from our ongoing GWA study of height variation in children.

Methods

Study population

All subjects were consecutively recruited from the Greater Philadelphia area from 2006 to 2009 at the Children's Hospital of Philadelphia and its Primary Care Centers. Our study cohort consisted of 8,184 children of European ancestry with height information. All subjects were biologically unrelated and were aged between 0 and 18 years old. The basic characteristics of the study subjects are outlined in Table 1. This study was approved by the Institutional Review Board of the Children's Hospital of Philadelphia. Parental informed consent was given for each study participant for both the blood collection and subsequent genotyping.
Table 1
Basic characteristics of the study subjects, including sample size and mean height plus standard deviation (S.D.) for each age and gender separately
 
MALE
FEMALE
Age
N
Average Height (cm)
S.D.
N
Average Height (cm)
S.D.
Under 2
673
73.51
10.33
424
73.04
8.86
2
319
88.92
5.79
200
87.87
6.40
3
318
97.72
5.50
244
96.17
5.58
4
279
104.22
5.97
183
103.66
6.30
5
215
110.75
7.05
175
110.40
6.88
6
218
119.01
7.23
177
117.98
6.52
7
219
125.14
7.42
159
124.19
7.23
8
197
130.01
7.81
157
128.87
7.56
9
196
135.56
8.20
145
133.52
9.99
10
184
139.98
8.73
177
139.64
8.62
11
188
145.59
9.39
188
147.47
9.06
12
220
150.60
10.64
181
152.92
9.17
13
221
157.79
10.28
243
157.21
8.40
14
237
164.66
9.40
248
160.25
7.25
15
252
169.09
9.48
260
161.39
7.69
16
201
172.90
7.90
275
162.64
6.77
17
171
174.38
8.52
216
162.89
7.29
18
113
174.60
7.01
111
163.47
7.58

Genotyping

We performed high throughput genome-wide SNP genotyping using either the Illumina Infinium™ II HumanHap550 or Human 610 BeadChip technology in the same manner as our center has reported previously[16]. The SNPs analyzed survived the filtering of the genome wide dataset for SNPs with call rates < 95%, minor allele frequency < 1%, missing rate per person < 2% and Hardy-Weinberg equilibrium P < 10-5.
Loci described from GWA studies published to date have been found using either the Affymetrix or Illumina platform. In the event a locus was reported using both the Illumina and Affymetrix arrays, we used the SNPs present on the Illumina array. In the event of a signal only being described on the Affymetrix array, we either already had that SNP on our Illumina array or we identified and used the best surrogate SNP available (see Additional file 1: Supplemental Table S1 for the surrogates employed).

Statistical analyses

From our database of heights for our multi-dimensional scaling (MDS) determined Caucasians, as previously described[1719] and resulting in a low genomic inflation factor, we eliminated height outliers using 2% cutoff for each age category in order to remove potential measurement error. As height values vary widely across pediatric age groups and gender, we calculated the Z-scores using inverse-normal transformation for each age (one year bin) and gender category, and conducted association analysis with the Z-scores as the outcome variable.
We queried the data for the indicated SNPs in our pediatric samples. All statistical analyses were carried out using the software package plink[20]. By treating the Z-score for height as a quantitative trait, association analysis for each SNP was carried out using linear regression with the SNP included as an independent variable (coded as 0, 1, and 2, counting the number of minor alleles at the SNP).
The results for Figure 1 were generated by summing the number of height increasing alleles across all 16 height-associated SNPs in our study to in order to produce a scatter plot showing the impact of the genotype score on the cumulative height Z-score.

Results

The 51 SNPs corresponding to the 46 previously reported height loci were investigated with respect to their association to normalized pediatric height in MDS-determined European Americans (Table 2; also Additional file 2: Supplemental Table S2 for analyses by age categories).
Table 2
Quantitative association results for the candidate loci in the European American height cohort (n = 8,184), sorted by chromosomal location.
Chr
Minor Allele
SNP
Position (Build 36)
Nearby genes(s)
NMISS
MAF
BETA
SE
R2
T
P
1
A
rs11809207
26205282
CATSPER4
8106
0.1730
0.02775
0.0213
0.0002095
1.303
0.1926
1
C
rs6663565
41232781
SCMH1
8184
0.4297
0.03744
0.01587
0.0006802
2.36
0.0183
1
C
rs17038164
118574711
SPAG17
8182
0.2601
-0.06029
0.01784
0.001395
-3.38
0.0007274
1
G
rs11205277
146705945
Histone class 2A, MTMR11, SV2A, SF3B4
8182
0.4195
0.0109
0.01579
5.83E-05
0.6906
0.4898
1
G
rs678962
168921546
DNM3
8178
0.2183
0.01272
0.0192
5.37E-05
0.6625
0.5077
1
A
rs2274432
180752602
C1orf19, GLT25D2
7965
0.3237
0.04568
0.01722
0.0008828
2.653
0.008003
1
A
rs3942992
224079131
ZNF678
8181
0.1725
9.96E-05
0.02072
2.83E-09
0.004809
0.9962
2
G
rs3791679
56008543
EFEMP1, PNPT1
8179
0.2539
-0.0782
0.01798
0.002308
-4.349
1.39×10 -5
2
T
rs1052483
219759853
IHH, CRYBA2, FEV, SLC23A3, TUBA1
8110
0.0956
-0.04701
0.02686
0.0003777
-1.75
0.08009
3
C
rs9841212
135674636
ANAPC13, CEP63
8154
0.3289
-0.006868
0.01676
2.06E-05
-0.4098
0.682
3
A
rs6763931
142585531
ZBTB38
8174
0.4091
0.04634
0.01587
0.001042
2.92
0.003513
4
T
rs6842303
17530324
LCORL, NCAPG
8173
0.2466
0.02231
0.01823
0.0001834
1.224
0.2209
4
C
rs6830062
17693999
LCORL, NCAPG
8184
0.1883
-0.05215
0.02014
0.0008192
-2.59
0.009613
4
A
rs1812175
145932449
HHIP
8172
0.1639
-0.03329
0.02125
0.0003002
-1.566
0.1173
5
T
rs10472828
32924575
NPR3
8182
0.4585
-0.005366
0.01589
1.39E-05
-0.3376
0.7357
6
A
rs12198986
7665058
BMP6
8183
0.4516
-0.0003072
0.01598
4.52E-08
-0.01922
0.9847
6
G
rs10946808
26341366
Histone class 1, Butyrophilin genes
8164
0.2923
-0.05734
0.01736
0.001336
-3.304
0.0009572
6
C
rs2844479
31680935
HLA class III
8183
0.3890
-0.03031
0.01605
0.0004355
-1.888
0.05907
6
G
rs3130050
31726740
HLA class III
8178
0.1249
0.06717
0.02369
0.0009819
2.835
0.004598
6
T
rs185819
32158045
HLA class III
8178
0.4576
0.0516
0.01576
0.001309
3.274
0.001066
6
G
rs1776897
34302989
HMGA1, LBH
8183
0.0940
0.02524
0.02701
0.0001068
0.9348
0.3499
6
A
rs2814993
34726871
C6orf106
8091
0.1390
0.06941
0.02284
0.001141
3.039
0.002378
6
A
rs4713858
35510763
ANKS1, TCP11, ZNF76, DEF6, SCUBE3
8184
0.1730
-0.02058
0.02103
0.000117
-0.9786
0.3278
6
C
rs314263
105499438
LIN28B, HACE1, BVES, POPDC3
8184
0.3129
0.02821
0.01698
0.0003373
1.661
0.09665
6
T
rs1490388
126877348
C6orf173/LOC387103
8179
0.4784
0.05315
0.01571
0.001398
3.383
0.0007196
6
G
rs3748069
142809326
GPR126
8184
0.3126
-0.06047
0.01695
0.001552
-3.566
0.0003641
7
T
rs798544
2536343
GNA12
8184
0.2897
0.009501
0.01746
3.62E-05
0.5441
0.5864
7
C
rs1182188
2643226
GNA12
8184
0.2948
0.01528
0.01742
9.40E-05
0.8769
0.3806
7
A
rs849141
27958331
JAZF1
8180
0.2729
0.05199
0.01769
0.001055
2.939
0.0033
7
C
rs2282978
91909061
CDK6, PEX1, GATAD1, ERVWE1
8180
0.3562
-0.0002285
0.01639
2.38E-08
-0.01394
0.9889
7
C
rs11765954
91925346
CDK6, PEX1, GATAD1, ERVWE1
8183
0.2866
0.006002
0.01744
1.45E-05
0.3441
0.7307
8
C
rs10958476
57258362
PLAG1, MOS, CHCHD7, RDHE2, RPS20, LYN, TGS1, PENK
8158
0.2015
0.05689
0.01979
0.001012
2.874
0.004062
8
C
rs7846385
78322734
PXMP3, ZFHX4
8175
0.2753
0.004128
0.01761
6.72E-06
0.2344
0.8147
9
G
rs4448343
95345925
PTCH1
8182
0.3217
-0.007508
0.01686
2.42E-05
-0.4453
0.6561
9
A
rs4743034
106711908
ZNF462
8183
0.2250
0.01859
0.01872
0.0001206
0.9933
0.3206
12
C
rs8756
64646019
HMGA2
8175
0.4607
0.02308
0.01586
0.0002588
1.455
0.1458
12
G
rs3825199
92479422
SOCS2, MRPL42, CRADD, UBE2N
8183
0.2088
0.02109
0.0194
0.0001445
1.087
0.2769
13
C
rs1239947
50004556
DLEU7
8183
0.3287
0.03243
0.01678
0.0004563
1.933
0.05333
14
C
rs910316
74695795
TMED10
8184
0.4863
-0.02021
0.01577
0.0002006
-1.281
0.2002
14
C
rs7153027
91496975
TRIP11, FBLN5, ATXN3, CPSF2
8149
0.4316
-0.02966
0.0158
0.0004323
-1.877
0.06054
15
C
rs2554380
82106888
ADAMTSL3, SH3GL3
8067
0.1991
0.01455
0.02029
6.38E-05
0.7171
0.4734
15
T
rs11633371
87157836
ACAN
8184
0.4636
0.02862
0.01575
0.0004032
1.817
0.06929
15
A
rs4533267
98603794
ADAMTS17
8184
0.2933
-0.001093
0.01737
4.84E-07
-0.06294
0.9498
17
A
rs3760318
26271841
CRLF3, ATAD5, CENTA2, RNF135
8184
0.3821
-0.03009
0.01627
0.0004178
-1.849
0.06444
17
A
rs4794665
52205328
NOG, DGKE, TRIM25, COIL, RISK
8183
0.4756
0.006489
0.01569
2.09E-05
0.4135
0.6792
17
A
rs757608
56852059
BCAS3, NACA2, TBX2, TBX4
8126
0.3322
0.02008
0.01676
0.0001767
1.198
0.2309
18
G
rs4800148
18978326
CABLES1, RBBP8, C18orf45
8183
0.2043
-0.04987
0.01943
0.0008048
-2.567
0.01028
18
T
rs530550
45105636
DYM
8182
0.3572
-0.01124
0.01631
5.81E-05
-0.6892
0.4907
19
G
rs12459350
2127586
DOT1L
8179
0.4744
0.02751
0.01579
0.0003711
1.742
0.08149
20
A
rs967417
6568893
BMP2
8184
0.4495
-0.02479
0.01591
0.0002964
-1.558
0.1194
20
C
rs4911494
33435328
UQCC, GDF5, CEP250, EIF6, MMP24
8182
0.3864
0.05107
0.01621
0.001212
3.151
0.001633
The SNPs in bold are those that survived correction for multiple testing.
NMISS: number of individuals tested; MAF: minor allele frequency; BETA: regression coefficient for the test SNP; SE: standard error of the regression coefficient; R2: r2 value in linear regression; T: test statistic; P: two-sided trend test P-value. The direction of effect is shown for the minor allele in each case.
In summary, sixteen of these SNPs yielded at least nominally significant association to height (P < 0.05), representing fifteen different loci with the same direction of effect as previously reported. Of these fifteen loci, variation at the EFEMP1-PNPT1 locus yielded the strongest association with P = 1.39×10-5, namely rs3791679.
With a slightly lower magnitude of association was GPR126 with rs3748069 yielding a P = 3.64×10-4, C6orf173 (also known as LOC387103) with rs1490388 yielding a P = 7.20×10-4, SPAG17 with 118574711 yielding a P = 7.27×10-4 and the Histone class 1 gene cluster with rs10946808 yielding a P = 9.57×10-4.
Overall, in addition to these loci, we found evidence for association at the HLA class III region, UQCC-GDF5, C6orf106, JAZF1, ZBTB38, PLAG1, C1orf19-GLT25D2, LCORL-NCAPG, CABLES1-RBBP8-C18orf45 and SCMH1 loci. One could argue that we have carried out multiple testing in our height cohort for these previously reported SNPs, albeit at a number of magnitudes less than for a full GWA study. If we were to apply the strictest correction, i.e. the Bonferroni correction based on 51 SNPs, then EFEMP1-PNPT1, GPR126, C6orf173, SPAG17 and the Histone class 1 gene cluster would still be considered significant and their effects are consistent with the outcomes of the adult GWA studies.
It was also observed that SNPs residing at the 31 other loci did not reveal any evidence of association with height in our pediatric cohort, most notably HMGA2.
Finally, we investigated the sixteen significant SNPs further by testing for association between height Z-score and the genotype score, by summing the number of height increasing alleles across all these SNPs. The resulting P-value for the genotype score was < 2×10-16 (Figure 1). The genotype score explains 1.64% of the total variation for height z-score. We also tested pair-wise interactions between the sixteen significant SNPs, but none of the interaction effects were significant, suggesting that these sixteen SNPs act additively on pediatric height.

Discussion

We queried the existing dataset from our ongoing GWAS of pediatric height in European Americans for adult height loci uncovered in GWAS to date. We examined 51 single nucleotide polymorphisms (SNPs) corresponding to 46 genomic loci in 8,184 children with height measurements. Sixteen of these SNPs yielded at least nominally significant association to the trait, representing fifteen different loci.
One of the more notable results is the negative association with HMGA2. This gene is one of the most strongly associated loci with adult height[9] so its lack of association with childhood stature in this study is striking. We previously published a replication attempt with this locus and pediatric height when our cohort was substantially smaller[21]; at that time, we observed nominal association but it is clear that as our cohort has grown, this signal has failed to strengthen. Despite the wealth the evidence from adult GWA studies and from previous work with knock-out mouse models, it is of surprise not to observe association with HMGA2. However, when considering the age bins presented in Additional file 2: Supplemental Table S2, the T statistic generally increases with age, with the strongest value being for the 15-18 age group. Although none of these observations are significant, it may point to an age-specific effect at a particular point during childhood that is undetected in the overall analysis; however our large cohort size may still not be powered enough to tease out this effect.
For the loci we did not observe any evidence for association at all may be due to power issues, but could also indicate that they have a less pronounced role in a pediatric setting. In addition, only a portion of the published adult height loci have been independently and robustly replicated to date[22]. It should also be noted that childhood growth is an ongoing process where development factors may cloud detection at certain loci, including at the two rapid growth stages, where nutrition plays a major role in infant growth and hormone signaling impacts at puberty. Our study may lack power to detect stage specific association when using a mixed age childhood cohort; however we have presented the association results for specific age bins in Additional file 2: Supplemental Table S2.
From this analysis, it is clear that a number of loci previously reported from GWA analyses of adult height also play a role in our phenotype of interest. While these recently discovered loci unveil several new biomolecular pathways not previously associated with height, it is important to note that these well established genetic associations with stature explain very little of the genetic contribution for this pediatric phenotype, suggesting the existence of additional loci whose number and effect size remain unknown.

Conclusions

Among 46 loci that have been reported to associate with adult height to date, at least 15 also contribute to the determination of height in childhood. Once our GWA study is complete, we will have the opportunity to look for other variants in the genome that are associated with height in childhood.

Acknowledgements

We would like to thank all participating subjects and families. Hope Thomas, Kisha Harden, Andrew Hill, Kenya Fain, Crystal Johnson-Honesty, Alex Moy, Cynthia Drummond, Shanell Harrison and Sarah Wildrick provided expert assistance with genotyping or data collection and management. We would also like to thank Smari Kristinsson, Larus Arni Hermannsson and Asbjörn Krisbjörnsson of Raförninn ehf for their extensive software design and contribution. This research was financially supported by the Children's Hospital of Philadelphia. The study is supported in part by a Research Development Award from the Cotswold Foundation (H.H. & S.F.A.G.) and NIH grant 1R01HD056465-01A1.
Open Access This article is published under license to BioMed Central Ltd. This is an Open Access article is distributed under the terms of the Creative Commons Attribution License ( https://​creativecommons.​org/​licenses/​by/​2.​0 ), which permits unrestricted use, distribution, and reproduction in any medium, provided the original work is properly cited.

Competing interests

The authors declare that they have no competing interests.

Authors' contributions

JZ, HH and SFAG designed the study and supervised the data analysis and interpretation. JZ, ML, HZ and SFAG conducted the statistical analyses. CEK, CH, KAT, MLG, SD, ECF and FGO directed the genotyping and related sample handling. JPB, FDM, KW, PMS, JTG and BJG provided bioinformatics support. RMC and RIB coordinated the sample recruitment. JZ, ML, HH and SFAG drafted the manuscript. All the authors read and approved the final manuscript.
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Metadaten
Titel
The role of height-associated loci identified in genome wide association studies in the determination of pediatric stature
verfasst von
Jianhua Zhao
Mingyao Li
Jonathan P Bradfield
Haitao Zhang
Frank D Mentch
Kai Wang
Patrick M Sleiman
Cecilia E Kim
Joseph T Glessner
Cuiping Hou
Brendan J Keating
Kelly A Thomas
Maria L Garris
Sandra Deliard
Edward C Frackelton
F George Otieno
Rosetta M Chiavacci
Robert I Berkowitz
Hakon Hakonarson
Struan FA Grant
Publikationsdatum
01.12.2010
Verlag
BioMed Central
Erschienen in
BMC Medical Genetics / Ausgabe 1/2010
Elektronische ISSN: 1471-2350
DOI
https://doi.org/10.1186/1471-2350-11-96

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