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Logo of nihpaAbout Author manuscriptsSubmit a manuscriptHHS Public Access; Author Manuscript; Accepted for publication in peer reviewed journal;
Ann Neurol. Author manuscript; available in PMC 2012 December 1.
Published in final edited form as:
PMCID: PMC3247076

Genomewide meta-analysis identifies novel multiple sclerosis susceptibility loci

Nikolaos A. Patsopoulos, MD, PhD,1,2,3 the BSP MS Genetics working group and the steering committees of studies evaluating IFNb-1b and a CCR1-antagonist, ANZgene Consortium, GeneMSA, International Multiple Sclerosis Genetics Consortium, and Paul I.W. de Bakker, PhD2,3,4,5



To perform a one-stage meta-analysis of genome-wide association studies (GWAS) of multiple sclerosis (MS) susceptibility and explore functional consequences of new susceptibility loci.


We synthesized 7 MS GWAS. Each dataset was imputed using HapMap phase II and a per-SNP meta-analysis was performed across the 7 datasets. We explored RNA expression data using a quantitative trait analysis in peripheral blood mononuclear cells (PBMCs) of 228 subjects with demyelinating disease.


We meta-analyzed 2,529,394 unique SNPs in 5,545 cases and 12,153 controls. We identified three novel susceptibility alleles: rs170934T at 3p24.1 (OR=1.17, P = 1.6 × 10−8) near EOMES, rs2150702G in the second intron of MLANA on chromosome 9p24.1 (OR = 1.16, P = 3.3 × 10−8), and rs6718520A in an intergenic region on chromosome 2p21, with THADA as the nearest flanking gene (OR = 1.17, P = 3.4 × 10−8). The three new loci do not have a strong “cis” effect on RNA expression in PBMCs. Ten other susceptibility loci had a suggestive P<1×10−6, some of which have evidence of association in other inflammatory diseases, i.e. IL12B, TAGAP, PLEK, and ZMIZ1.


We have performed a meta-analysis of GWAS in MS that more than doubles the size of previous gene discovery efforts and highlights three novel MS susceptibility loci. These and additional loci with suggestive evidence of association are excellent candidates for further investigations to refine and validate their role in the genetic architecture of MS.


Multiple sclerosis (MS) is thought to emerge when genetically susceptible individuals encounter environmental triggers that initiate an inflammatory reaction against self-antigens in the central nervous system (CNS); these events result in recurring episodes of inflammatory demyelination and, in many cases, a progressive neurodegenerative process.1 The genetic architecture underlying susceptibility to MS is complex, and recent efforts have revealed over a dozen susceptibility loci of modest effect25 in addition to the major histocompatibility complex (MHC) that contains multiple independent susceptibility alleles in class I and class II loci. These discoveries were made possible by the emergence of genome-wide genotyping technologies and collaborative meta-analysis efforts to maximize statistical power.

Here, we perform a one-stage meta-analysis, of most of the genome-wide single nucleotide polymorphism (SNP) data generated in the field of MS, to conduct the largest gene discovery effort to date for this disease.


The present study comprises seven data sets of non-overlapping case and control subjects of European descent. Five strata (IMSGC-US, IMSGC-UK, GeneMSA-US, GeneMSA-NL, and GeneMSA-CH) were taken from a previously published meta-analysis.3 Details on these data sets can be found elsewhere.23 The sixth stratum (BWH/TT) is based on data from our previous study3 enriched with additional 1453 MS cases and 2176 controls, with all samples genotyped on the Affymetrix GeneChip 6.0 platform. Finally, we have added another stratum (ANZ) from a recently described genome-wide study containing 1618 cases and 1988 controls.5 Further information on these two strata and quality control applied can be found in the supplementary material. Table 1 summarizes the subject collections that have been assembled for this meta-analysis. All subjects met either 1) a diagnosis of MS per McDonald criteria6 or 2) a diagnosis of clinically isolated demyelinating syndrome (CIS) in which individuals have had one episode of inflammatory demyelination and harbor two or more T2 hyperintense lesions in their brain or spinal cord. The majority of CIS subjects go on to have a second episode of inflammatory demyelination, which results in a diagnosis of MS. An earlier study did not find differences in the distribution of susceptibility alleles in CIS and MS subjects, suggesting that their genetic architecture is similar.7

Table 1
Characteristics of the meta-analyzed datasets

We used EIGENSOFT to remove outliers in terms of genetic ancestry and to calculate the top ten eigenvectors of the genotype data within each stratum.8 The seven data sets were genotyped using different genotyping platforms. To maximize genome-wide coverage, we used the imputation algorithm implemented in MACH to yield 2.5 million SNPs across the genome in all data sets.9 Imputation based on linkage disequilibrium (LD) patterns observed in a representative European population sample in HapMap is a widely used approach to increase the power of GWAS and facilitate in silico meta-analysis.10 After imputation, we excluded all SNPs with an imputation quality score less or equal to 0.10 or minor allele frequency (MAF) <0.01 per stratum. For each stratum, we tested the imputed dosages for association to case-control status using logistic regression, including the ten first eigenvectors as covariates to correct for population stratification. For each SNP, the dosage corresponds to the (imputed) number of the coded allele in a given individual and varies from 0 to 2 on a continuous scale, thus incorporating information about the imputation uncertainty. Under a per-allele model, we calculated the odds ratio (OR), its corresponding standard error (SE) and p-value. To evaluate the robustness of the observed distribution of the test statistic, we inspected the quantile- quantile (Q-Q) plot and calculated the genomic inflation factor (λGC).11 To correct for any residual, unexplained inflation of the test statistic, we corrected the SEs by multiplying them with the square root of the λGC.10 Finally, we performed the same analyses adjusting for sex and report these sensitivity analyses in the Supplementary material.

Ensuring consistency in the strand orientation of the alleles across all strata, we meta-analyzed the ORs with the respective corrected SEs using inverse variance weighting under a fixed-effects model. We calculated the λGC of the genome-wide association results to evaluate the robustness of the meta-analysis. Furthermore, in a secondary sensitivity analysis, we used a random effects model to meta-analyze, thus allowing for between-study heterogeneity. We used Cochran’s Q to test for the presence of statistical heterogeneity and I2, with respective 95% confidence intervals, to quantify inconsistency of effects across the different strata.12, 13

We performed linkage disequilibrium (LD) pruning (r2 > 0.5) among correlated SNPs to identify the most statistically significant SNP in regions of strong LD. For non-MHC loci, we performed conditional analysis using a forward stepwise logistic regression for the most statistically significant SNPs (P < 10−6) within a 2-Mb distance from the best index SNP (with the lowest p-value) at a locus.

We pre-defined genome-wide significance for our meta-analysis at a P-value of < 5×10−8. At this type I error rate, and under a fixed effect model, we have more than 80% power to detect an OR of 1.15 for a risk allele with 0.4 minor allele frequency. The Cochran’s Q test was considered to be statistically significant at P < 0.10. For analyses we used the PLINK v1.0714 and R-2.11.

To leverage the rapidly growing list of susceptibility loci associated with inflammatory diseases, we tested all known SNP associations with Crohn’s disease (CD), ulcerative colitis (UC), celiac disease (CE), type 1 diabetes (T1D), rheumatoid arthritis (RA), systemic lupus erythematosus (SLE) and psoriasis (PS) for a role in MS. To identify these bona fide associations, we searched the online NHGRI catalog ( and PubMed for GWAs, meta-analyses of GWAS, or follow-up studies that reported a non-MHC SNP for these diseases with genome-wide significance (P < 5×10−8). For each of these SNPs we tested for replication of an effect using different p-value thresholds (0.05, 10−3, and 10−4), allowing for heterogeneity in the direction of effect. As a comparison, we also list the genome-wide non-MHC SNPs associated with type 2 diabetes (T2D),15 height (HI),16 lipid traits (LI),17 and myocardial infraction (MI)1820 as negative control diseases, because we do not expect these diseases to have an etiologic relationship with MS.

For all SNPs that reached a P < 10−6, we also performed a meta-analysis under a recessive and dominant model. We used the posterior probabilities for each of the three genotypes (AA, AB, BB) from the imputations to calculate the corresponding dominant and recessive dosage in each individual for each SNP. With these dosages, we calculated the per-stratum ORs and corrected SEs, and meta-analyzed these to obtain the overall ORs and the corresponding p-values.

For the newly identified susceptibility loci, we sought to test the hypothesis that the identified SNPs can affect expression levels of nearby genes (within 1 Mb upstream and downstream of the SNP). We collected RNA expression data with an Affymetrix U133 v2.0 array from peripheral blood mononuclear cells (PBMCs) of 228 subjects with Relapsing Remitting (RR) MS or CIS. These data were collected between July 2002 and October 2007, as part of the Comprehensive Longitudinal Investigation of MS at the Brigham and Women’s Hospital.21,22 We regressed the observed gene expression on the SNP imputed dosages, adjusted for the treatment used. The probes that passed our quality check criteria (n=20,517) were used for the subsequent analyses. In an exploratory analysis, we performed an eQTL analysis of all of probes for each newly identified loci and organized the tail of the distribution of the results, i.e. probes that reached a nominal significance threshold (p < 0.05), using the Ingenuity Pathway Analysis (IPA) software. Ingenuity maps probe IDs to its database and performs statistical computing to identify the most significant canonical pathways and networks overrepresented in a given gene list as compared with the whole list of genes in the Human Genome U133 Plus 2.0 array. The canonical pathway analysis tool identified the pathways from the IPA library of canonical pathways that were most significant to the dataset, based upon genes within the dataset that were associated with a canonical pathway in the Ingenuity Pathways Knowledge Base. In a similar way, the software leveraged the input gene expression data to provide networks. Specifically, molecules of interest, which interact with each other, and molecules in the Ingenuity Knowledge Base were identified as Network Eligible Molecules, which served as “seeds” for generating networks.


Overall, 5,545 cases and 12,153 controls passed QC and were included in the meta- analysis (Table 1), and 2,529,394 unique SNPs were analyzed in at least two strata. The genomic inflation factor (λGC) for the seven strata ranged from 1.026 to 1.061 (Table 1), suggesting that population stratification within the individual strata was limited. The genomic inflation factor of the genome-wide meta-analysis results was 1.051, indicating that the test statistic distribution is well calibrated and that the extent of residual bias (including unaccounted for stratification and technical artifact) is minimal.

Genome-wide significant SNPs under a per-allele genetic model (P<5×10−8)

Of 2,617 SNPs that reach genome-wide significance (P < 5.0 × 10−8), 2,583 SNPs are located within the MHC on chromosome 6p21, where index SNP rs3129889 (OR = 2.97, P = 1.03×10−206) and rs9260489 (OR = 1.21, P = 1.16×10−11) tag the HLA-DRB1 and HLA-B associations, respectively.3 Outside of the MHC, we observed SNP associations at seven loci with genome-wide significance (Figure 1, Table 2, Supplementary Table 2 for the sex-adjusted analyses). Three of these loci have not been described previously as being associated with MS or other inflammatory diseases. First, rs170934 at locus 3p24.1 (P = 1.6 × 10−8) demonstrated an OR of 1.17 for the minor T allele, with little evidence for statistical heterogeneity (I2 = 2%; P = 4.7 × 10−8 under a random-effects model). Figure 2A shows the regional association plot for this SNP, which is located in an intergenic area between CMC1, a gene with no known function, and EOMES, a T-box gene family member and a paralog of TBX21/TBET.

Figure 1
Manhattan plot for the meta-analysis genome-wide – log(p-values) (fixed effects)
Figure 2
Regional association plots for the newly identified genome-wide significant loci and respective forest plots
Table 2
Meta-analysis results for SNPs with p-value <10−6 and known genes/loci.

The second novel locus we have identified is tagged by rs2150702, a SNP in the second intron of the MLANA gene on chromosome 9p24.1, which is known as a melanoma antigen (Figure 2C, D). The minor G allele of this SNP increases risk (OR = 1.16) with no evidence for statistical heterogeneity across the seven strata (P = 3.3 × 10−8 under both fixed and random-effects models).

The third novel locus is tagged by rs6718520, which maps to an intergenic region on chromosome 2p21, with THADA as the nearest flanking genes at 132kbps distance (Figure 2E). The minor A allele of this SNP has an OR of 1.17 (P = 3.4 × 10−8) with modest evidence for statistical heterogeneity (I2 = 35%, P = 2.6 × 10−4 under a random-effects model). This heterogeneity may come from the fact that the quality of this SNP’s imputation varies across the strata of the meta-analysis, that residual population substructure in some strata influences our analysis, or it may be true heterogeneity in the effect of the SNP in different groups of subjects. The stronger per-dataset effect was observed in a low imputation quality dataset (Gene MSA NL, Figure 2F), so we explored the influence of the imputation’s quality on the statistical heterogeneity and the overall effect size (Supplemental Table 3). Under the most conservative scenario of synthesizing only the high imputation quality studies (INFO>0.9) the p-value was 8.44 × 10−6, although suffering a huge power loss due to the smaller sample size.

The other four loci with genome-wide significant SNPs correspond to already known MS susceptibility loci. At the IL2RA gene, we observed two index SNPs (rs2104286 and rs7089861), with independent effects (r2=0.128 in HapMap-CEU) that correspond to the two previously described independent effects within the IL2RA locus.23 Another SNP, rs1335532, tags the known association in the CD58 locus (r2=0.87 with rs2300747, the previously described best marker).21 The fourth SNP, rs2293152, captures the recently described association of the STAT3 locus with MS susceptibility.24 Many of the subjects are shared between the present study and the original discoveries of these three loci, so the findings here do not constitute independent evidence for replication of these loci. In addition to the CD58, IL2RA and STAT3 loci that reach genome-wide significance in the present meta-analysis, we have tabulated the association results for all MS susceptibility loci reported to date (Table 2). We observe substantial evidence of association for all known loci with three exceptions (KIF1B,25 CBLB,4 and chr5p15.3226) that do not reach nominal statistical significance (Table 2).

SNPs with suggestive evidence of association (p < 10−6)

Ten additional SNPs present strongly suggestive evidence of association with MS (defined as p < 10−6) (Table 2). Two of these are found the IL12B locus, which is known to be associated with Crohn’s disease and psoriasis (Table 3, supplementary table 1).27,28 Another 3 loci -- TAGAP (rs1738074), ZMIZ1 (rs1250542), and PLEK (rs7592330) -- have been described previously as susceptibility loci for other inflammatory diseases (Table 3),29,30 and ZMIZ1 has been described previously as having suggestive evidence of association with MS.3 Of the remaining loci, two contain genes that have long been described as being involved in the immune dysregulation seen in MS: TBX21 and CD86. The rs8070463 SNP (OR = 0.87, p-value = 9.55×10−8) lies within 42kb of TBX21, which is also known as TBET and is a paralog of the EOMES gene found in the novel 3p24.1 susceptibility locus described above. TBX21 is of great interest in T cell function because it is a master regulatory gene necessary for the differentiation of pathogenic Th1 lymphocytes that play an important role in murine inflammatory demyelination.31,32 Nonetheless, this locus contains another gene, TBKBP1, that is involved in NFKB signaling and could also be implicated in the effect of this locus; functional dissection will be required to differentiate the role of the different genes found in this locus. The second locus of immunological interest is tagged by rs2681424 (OR =1.16, p-value=2.33 × 10−7) and contains CD86, a costimulatory molecule that is the receptor for the CD28 and CTLA4 molecules and is an important component of the machinery regulating the activation of T cells 33. These two genes are found in loci associated with susceptibility to rheumatoid arthritis (CD28) and T1D as well as thyroiditis (CTLA4).34

Table 3
Meta-analysis results for previously published known (p<5×10−8) non-MHC SNPs in inflammatory diseases that are nominally (<0.05) significant in the current meta-analysis.

Susceptibility allele overlap between MS and other inflammatory diseases

Motivated by recent progress in the identification of susceptibility loci of other inflammatory diseases, we sought to test the effect of all non-MHC SNPs described to date as bona fide inflammatory disease associated polymorphisms. Of these 145 SNPs, 48 are associated with MS risk at nominal significance, consistent with a shared genetic etiology of inflammatory diseases (Table 3, Supplementary Table 1, Figure 3A). Of all the listed inflammatory diseases, SNPs identified in ulcerative colitis and celiac disease seem to replicate better in MS (60% and 45% at a nominal level, respectively. Figure 3A). Under more stringent statistical significance cut-offs (< 10−3 and < 10−4) few SNPs replicated in our MS dataset, with celiac disease being the most replicated (34% at <10−3 and 15% at 10−4, Figure 3A). It is interesting to note that, for celiac disease (and most of the other inflammatory diseases) a minority of loci appears to demonstrate association with MS, but in the opposite direction such that a celiac disease risk allele is protective for MS. While such opposite effects have been noted before, we gain an appreciation that they are widespread and that they highlight the complexity of the shared architecture among the inflammatory disease. One example of this complexity is the TAGAP locus in which rs1738074 reaches a p-value < 10−6 in MS (Table 2); this locus has attained genome-wide significance in celiac disease35 (opposite direction of effect relative to MS) and type 1 diabetes30 (same direction of effect as MS) (Table 3, Figure 3B). Further, within the TAGAP locus, another SNP (rs212389, r2=0.268 with rs1738074) that is associated with susceptibility to RA34 has the same direction of effect in MS (Table 3, Figure 3B). Given the extended evidence of association of the TAGAP locus in many inflammatory diseases, it is a strong candidate MS susceptibility locus, although it has not reached a level of genome-wide significance in our study.

Figure 3
Overlap of the genetic architecture of MS with that of other inflammatory diseases

Analysis under dominant and recessive genetic models

For the SNP associations with P < 10−6, we also explored dominant and recessive genetic models (Supplementary Table 2) to assess whether these models fit our data better than our default additive model.36 In several cases, association is enhanced when considering a different model, which could guide the design of replication studies. For example, at the 2p21 locus, the recessive model for the minor rs6718520A allele is slightly more significant (OR = 1.29, P = 2.9 × 10−8) than the additive model (OR = 1.17, P = 3.4×10−8). For two other SNPs, rs1335532 in CD58 and rs2293152 in STAT3, the dominant model was more significant than the additive model. Finally, SNP rs9901869, which is found in an intergenic region on chromosome 17 near NPEPPS gene, reached genome-wide significance under the recessive model for the minor G allele (OR = 1.26, P = 3.7 × 10−8 under both fixed and random-effects models). Thus, considering non-additive models for certain loci appears to be warranted and informs the potential mechanism of a variant’s effect.

Transcriptional and exploratory pathway analysis

To explore the functional consequences of our new MS susceptibility loci, we assessed whether each of the three index SNPs influenced the level of RNA expression from genes located in the vicinity of each SNP (cis expression quantitative trait locus (eQTL) analysis). We performed these analyses in a set of 228 subjects with demyelinating disease on which we have obtained a genome-wide RNA expression profile from PBMC. While a few suggestive cis associations (P<0.05) with RNA expression were noted in the MLANA (rs2150702) locus, none of the three newly identified susceptibility alleles had statistically significant cis effects after correcting for the number of hypotheses tested in these data (Supplementary Table 3). This is not unusual as only 625 out of 1598 SNPs associated with a human trait were found to have a cis eQTL effect in a recent survey of validated loci.37

In an exploratory analysis, we implemented a pathway analysis approach by highlighting those pathways or networks in which the expression of multiple genes is influenced by a given SNP in a modest manner (P<0.05). Of the three tested SNPs, rs2150702 in the MLANA locus has a number of pathways that are involved in immune system function. Specifically the best-scoring pathway is related to CD28 signaling, but T and B cell receptor signaling and the IL-2 signaling appear to be involved as well (Supplementary Table 4). We subsequently evaluated the networks generated for each of the new MS susceptibility loci. In the highest scoring network of the EOMES locus (Supplementary Figure 4A), TNFα signaling appears to play a central role, connecting the locus to our previously described TNFRSF1A susceptibility one. The network also contains a decrease in HLA-A gene expression relative to the susceptibility allele, which is in agreement with the validation of at least one protective allele (HLA-A*02) in this gene.38 The highest scoring network for the MLANA locus (Supplementary Figure 4B) contains ERK and connections with type 1 interferon responses previously implicated in MS with the IRF8 locus. Reducing the activity of the ERK signaling pathway has been reported to ameliorate experimental inflammatory encephalomyelitis (EAE), a murine model systems that captures many features of MS. 39 The best network of the THADA locus includes STAT3 (Supplementary Figure 4A), one of the other genes with genome-wide significance in our meta-analysis (Table 2). The expression of STAT3 RNA is enhanced relative to the risk allele rs6718520A which is consistent with reports that diminished expression of STAT3 in humans blocks the development of Th17 cells that play an important role in mediating inflammatory demyelination in MS.38 Further, STAT3 is part of a broader network that includes key regulators of cellular signaling such as ERK.


We have performed a meta-analysis of GWAS in multiple sclerosis and have highlighted three novel loci that reach genome-wide significance. The EOMES and MLANA loci showed no evidence of statistical heterogeneity, while the third locus near THADA showed some degree of heterogeneity among the strata of data. In addition, we point out several loci as having suggestive evidence of being associated with MS, such as the locus containing the TAGAP gene (previously associated with celiac disease, type 1 diabetes, and rheumatoid arthritis) and a locus on chromosome 17 that includes the transcription factor TBX21 which plays an important role in the immunopathogenesis of murine models of MS.32

These results extend the list of loci associated with MS from earlier genome scans25 and confirm theoretical predictions that increasing sample sizes will lead to additional discoveries given the magnitude of effect seen for non-MHC MS susceptibility loci. However, >10,000 subjects are needed to be fully powered to identify such common susceptibility alleles of modest effect.41 One element of our strategy that enhances the likelihood for gene discovery is imputation of genotypes at SNPs not sampled by genotyping arrays using reference maps such as HapMap that catalogue the correlation structure among SNPs in human populations. Imputation allows the integrated analysis of datasets generated on different platforms and extends the analysis from roughly 750,000 genotyped SNPs at the end of quality control pipelines to the 2.5 million SNPs that we considered in this meta-analysis. Critically, confidence in an imputed genotype varies depending on how well it correlates with genotyped SNPs, and, if any uncertainty is present, it is incorporated into the test statistic, down-weighting the importance of the association results at that SNP. Imputation can be a very valuable tool: for example, when a genotyped SNP is an imperfect surrogate marker for a causal variant, the genotyped SNP may not display very strong evidence of association, and such a result may be lost in a genome-wide analysis. By estimating the results of the association test with a causal variant that is not genotyped, imputation can provide more robust evidence of association with a locus than a genotyped marker that is poorly correlated with the causal variant. Thus, imputed SNPs enhance our ability to detect and localize the effect of a new susceptibility locus. 41, 42 However, such results, as with any result from genome scans, needs to be independently replicated before being considered a validated locus.

Several limitations are present in our study. First, not all samples were genotyped with the same microarray platform, which can incorporate heterogeneity due to differences in coverage or genotype quality despite genome-wide imputation of >2 million SNPs on the HapMap reference dataset. Second, residual population substructure (even after excluding outliers and incorporating principal components into our analysis as covariates) may have inflated the test statistic. When implementing a very conservative correction for the modest level of genomic inflation seen in each stratum, we find that the EOMES locus remains significant at a genome-wide level, but that the other two new loci fluctuate over this threshold of significance. Thus, the EOMES locus is our most robust result, and we look forward to efforts to validate the role of these loci that we describe in additional collections of MS subjects.

In conclusion, we report three new loci involved in the etiology of MS. Several additional loci are involved in inflammatory disease or immunologic function. Replication in large samples is now required to validate these loci as bona fide susceptibility loci in MS. Once validated, future fine-mapping studies across these loci are needed to provide a comprehensive picture of which variants have causal relationships with MS risk.

Supplementary Material

Supp Table S1-S5 & Fig S1-S4

Supp Table S6

Supp Table S7


P.L.D. is a Harry Weaver Neuroscience Scholar Award Recipient of the National MS Society (NMSS). This project was also supported in part by R01 NS067305 and RC2 NS070340. We thank the subjects with MS who have generously donated DNA samples for theses studies. We thank individuals with MS in Australia and New Zealand for supporting this research. We are grateful to J. Wright and C. Remediakis from Multiple Sclerosis Research Australia (MSRA) for expediting this research. This work was supported by MSRA, John T. Reid Charitable Trusts, Trish MS Research Foundation and the Australian Research Council, under the Linkage Projects Scheme (LP0776744). We thank the International MS Genetics Consortium for the use of genotype data. We thank the Myocardial Infarction Genetics Consortium (MIGen) study for the use of their genotype data as control data in our study. The MIGen study was funded by the U.S. National Institutes of Health and National Heart, Lung, and Blood Institute’s STAMPEED genomics research program and a grant from the National Center for Research Resources. We acknowledge use of genotype data from the British 1958 Birth Cohort DNA collection, funded by the Medical Research Council grant G0000934 and the Wellcome Trust grant 068545/Z/02.

Author Index

Nikolaos A. Patsopoulos14,, Federica Esposito46, Joachim Reischl7,8, Stephan Lehr7,8, David Bauer7,8, Jürgen Heubach7,8, Rupert Sandbrink7,8,9, Christoph Pohl7,8,10, Gilles Edan11,12,13, Ludwig Kappos11,12,14,15,16, David Miller11,12,17, Javier Montalbán11,12,18, Chris H. Polman11,12, 16, 19, Mark S. Freedman11,12,20, Hans-Peter Hartung11,12,15,21,22, Barry G.W. Arnason11,15,23, Giancarlo Comi4-6,11,15, Stuart Cook11,15,24, Massimo Filippi4,11,15,22,25, Douglas S. Goodin11,15,26,27, Douglas Jeffery11,15,28, Paul O’Connor11,15,29, George C. Ebers11,27,30, Dawn Langdon11,27,31, Anthony T. Reder11,27,32, Anthony Traboulsee11,27,33, Frauke Zipp11,22,34, Jan Schimrigk11,22,35, Jan Hillert4,11,22,36, Melanie Bahlo36,37, David R Booth36,38, Simon Broadley36,39,40, Matthew A Brown36,41,42, Brian L Browning36,43, Sharon R Browning36,43, Helmut Butzkueven36,44,45, William M Carroll36,46,47, Caron Chapman48, Simon J Foote49, Lyn Griffiths50, Allan G Kermode36,46,47, ,Trevor J Kilpatrick36,44,51,52, Jeanette Lechner-Scott36,53,43, Mark Marriott36,52, Deborah Mason36,55, Pablo Moscato36,54,56, Robert N Heard36,38, Michael P Pender36,57,58, Victoria M Perreau36,51, Devindri Perera36,49, Justin P Rubio44, Rodney J Scott36,53,54,56, Mark Slee36,58, Jim Stankovich36,44, Graeme J Stewart36,38, Bruce V Taylor36,44, Niall Tubridy36,60, Ernest Willoughby36,61, James Wiley36,62, Paul Matthews16,63, Filippo M. Boneschi4-6, Alastair Compston4,64, Jonathan Haines4,65, Stephen L Hauser4,66, Jacob McCauley4,67, Adrian Ivinson4,68, Jorge R Oksenberg4,66, Margaret Pericak-Vance 4,67, Stephen J Sawcer4,64, Philip L. De Jager#*,14, David A. Hafler*3,4,68, Paul I.W. de Bakker24,69,70


#Corresponding author: Philip L. De Jager, MD PhD, Program in NeuroPsychiatric Genomics, Department of Neurology, Brigham & Women’s Hospital, 77 Avenue Louis Pasteur, NRB168, Boston, MA 02115, Tel: 617 525 4529, Fax: 617 525 5722, ude.dravrah.hwb.scir@regajedp

*contributed equally with PIW de Bakker

1Program in Translational NeuroPsychiatric Genomics, Neurosciences Institute, Departments of Neurology & Psychiatry, Brigham & Women’s Hospital, Boston, MA 02115, USA.

2Division of Genetics, Department of Medicine, Brigham & Women’s Hospital, Harvard Medical School, Boston, MA 02115, USA.

3Program in Medical and Population Genetics, Broad Institute of Harvard and Massachusetts Institute of Technology, Cambridge, MA 02139, USA.

4International Multiple Sclerosis Genetics Consortium (IMSGC)

5Department of Neurology, Scientific Institute San Raffaele, 20132 Milan, Italy

6Institute of Experimental Neurology, Scientific Institute San Raffaele, 20132 Milan, Italy

7The Bayer Schering Pharma Genomics (BSP-Gen) working group

8Bayer Schering Pharma AG, 13342, Berlin, Germany.

9Department of Neurology, Heinrich Heine University Düsseldorf, Germany

10Department of Neurology, University Hosptial Bonn, Germany

11steering committees of studies evaluating IFNb-1b and a CCR1-antagonist

12The BEtaferon®/BEtaseron® in Newly Emerging Multiple Sclerosis For Initial Treatment (BENEFIT) study

13Service Neurologie, C.H.U. Rennes Hôpital Pontchaillou/France.

14Neurologische Klinik und poliklinik, Universitaetsspital Basel/Switzerland.

15The Betaferon® Efficacy Yielding Outcomes of a New Dose (BEYOND) study

16The GeneMSA Consortium

17Institute of Neurology, The National Hospital, Queen Square, London/GB

18Unitat de Neuroimmunología Clínica Hospitals Vall dHebrón, Madrid/Spain

19Dept. Neurology Free University Hospital, Amsterdam/The Netherlands

20General Campus - Division of Neurology, The Ottawa Hospital, Ottawa/Canada

21Neurologische Klinik der Heinrich-Heine-Universität, Düsseldorf/Germany

22The CCR1-antagonist study

23Department of Neurology, Surgery Brain Research Institutes, Chicago/USA

24Department of Neurology and Neuroscience, UMDNJ-New Jersey Medical School, Newark, New Jersey/USA

25Neuroimaging Research Unit, University Hospital San Raffaele, Milano/Italy

26Department of Neurology, University of California San Francisco, San Francisco/USA

27The 16 year long term follow-up of the pivotal study on IFNB-1b in RRMS

28Wake Forest University, Department of Neurology, Winston-Salem/USA

29Division of Neurology, St. Michael’s Hospital, Toronto/Canada

30University Dept of Clinical Neurology, Oxford/UK

31Psychology Department, Royal Holloway, University of London/UK

32The University of Chicago, Department of Neurology, Chicago/USA

33UBC Hospital, Vancouver/Canada

34Cecilie-Vogt-Klinik, Charite – University Hospital Berlin, Germany

34University Hospital Bochum/Germany

35Karolinska Institutet at Huddinge University Hospital, Huddinge/Sweden

36ANZGene Consortium

37The Walter and Eliza Hall Institute of Medical Research, Parkville, VIC, AUS, 3050.

38The Westmead Millenium Institute, Westmead, NSW, AUS 2145.

39School of Medicine, Griffith University, QLD, AUS, 4222.

40Department of Neurology, Gold Coast Hospital, QLD, AUS 4215.

41Diamantina Institute of Cancer, Immunology and Metabolic Medicine, Princess Alexandra Hospital, University of Queensland, Brisbane, QLD, AUS 4102.

42Botnar Research Centre, Nuffield Department of Orthopaedic Surgery, University of Oxford, Oxford, OX3 7BN, UK.

43Department of Statistics, The University of Auckland, Auckland, NZ.

44The Howard Florey Institute, University of Melbourne, VIC, AUS 3010.

45Department of Medicine, University of Melbourne, VIC, AUS 3010.

46Sir Charles Gairdner Hospital, Nedlands, WA, AUS 6009.

47Australian Neuromuscular Research Institute, Nedlands WA, AUS 6009.

48Barwon Health, Geelong, VIC, AUS 3220.

49Menzies Research Institute, University of Tasmania, Hobart TAS 7001.

50Genomics Research Centre, Griffith University, QLD, AUS 4222.

51Centre for Neuroscience, University of Melbourne, VIC, AUS 3010.

52Royal Melbourne Hospital, Parkville, VIC, AUS 3050.

53John Hunter Hospital, Hunter New England Health Service, Newcastle NSW, AUS 2310.

54Hunter Medical Research Institute, Newcastle, NSW, AUS 2308.

55Canterbury District Health Board, Christchurch, NZ.

56Centre for Bioinformatics, Biomarker Discovery and Information-based Medicine, University of Newcastle, NSW, AUS 2308.

57School of Medicine, University of Queensland, QLD, AUS 4029.

58Department of Neurology, Royal Brisbane and Women’s Hospital, QLD, AUS 4029.

59School of Medicine, Department of Neurology, Flinders University of SouthAustralia, Bedford Park, Adelaide, SA, AUS 5042.

60Department of Neurology, St. Vincent’s University Hospital, Dublin, Republic of Ireland.

61Auckland District Health board, Auckland, NZ.

62Department of Medicine, Nepean Hospital, Penrith, NSW, AUS 2751.

63GSK Clinical Imaging Centre, Hammersmith Hospital and Department of Clinical Neurosciences, Imperial College, London.

64University of Cambridge, Department of Clinical Neuroscience, Addenbrooke’s Hospital, Hills Road, Cambridge, CB2 2QQ, UK

65Center for Human Genetics Research, Vanderbilt University Medical Center, Nashville, TN 37232-0700, USA

66Department of Neurology, University of California San Francisco, San Francisco, CA, 94143, USA

67John P. Hussman Institute for Human Genomics, University of Miami, Miller School of Medicine, Miami, FL 33136, USA

68Department of Neurology, Yale University School of Medicine, New Haven, CT 06520, USA.

69Department of Medical Genetics, Division of Biomedical Genetics, University Medical Center, Utrecht, The Netherlands

70Julius Center for Health Sciences and Primary Care, University Medical Center, Utrecht, The Netherlands


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