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. 2006 Aug 17;7:71. doi: 10.1186/1471-2350-7-71

Genome-wide significance for a modifier of age at neurological onset in Huntington's Disease at 6q23-24: the HD MAPS study

Jian-Liang Li 1,2,3, Michael R Hayden 4, Simon C Warby 4, Alexandra Durr 5, Patrick J Morrison 6,7, Martha Nance 8, Christopher A Ross 9,10,11, Russell L Margolis 9,10, Adam Rosenblatt 9, Ferdinando Squitieri 12, Luigi Frati 13, Estrella Gómez-Tortosa 14, Carmen Ayuso García 14, Oksana Suchowersky 15, Mary Lou Klimek 15, Ronald JA Trent 16, Elizabeth McCusker 17, Andrea Novelletto 18, Marina Frontali 19, Jane S Paulsen 20, Randi Jones 21, Tetsuo Ashizawa 22, Alice Lazzarini 23,24, Vanessa C Wheeler 25, Ranjana Prakash 1, Gang Xu 1,2, Luc Djoussé 26, Jayalakshmi Srinidhi Mysore 25, Tammy Gillis 25, Michael Hakky 25, L Adrienne Cupples 27, Marie H Saint-Hilaire 1, Jang-Ho J Cha 28, Steven M Hersch 28, John B Penney 28, Madaline B Harrison 29, Susan L Perlman 30, Andrea Zanko 31, Ruth K Abramson 32, Anthony J Lechich 33, Ayana Duckett 33, Karen Marder 33, P Michael Conneally 34, James F Gusella 25,35, Marcy E MacDonald 25, Richard H Myers 1,2,✉
PMCID: PMC1586197  PMID: 16914060

Abstract

Background

Age at onset of Huntington's disease (HD) is correlated with the size of the abnormal CAG repeat expansion in the HD gene; however, several studies have indicated that other genetic factors also contribute to the variability in HD age at onset. To identify modifier genes, we recently reported a whole-genome scan in a sample of 629 affected sibling pairs from 295 pedigrees, in which six genomic regions provided suggestive evidence for quantitative trait loci (QTL), modifying age at onset in HD.

Methods

In order to test the replication of this finding, eighteen microsatellite markers, three from each of the six genomic regions, were genotyped in 102 newly recruited sibling pairs from 69 pedigrees, and data were analyzed, using a multipoint linkage variance component method, in the follow-up sample and the combined sample of 352 pedigrees with 753 sibling pairs.

Results

Suggestive evidence for linkage at 6q23-24 in the follow-up sample (LOD = 1.87, p = 0.002) increased to genome-wide significance for linkage in the combined sample (LOD = 4.05, p = 0.00001), while suggestive evidence for linkage was observed at 18q22, in both the follow-up sample (LOD = 0.79, p = 0.03) and the combined sample (LOD = 1.78, p = 0.002). Epistatic analysis indicated that there is no interaction between 6q23-24 and other loci.

Conclusion

In this replication study, linkage for modifier of age at onset in HD was confirmed at 6q23-24. Evidence for linkage was also found at 18q22. The demonstration of statistically significant linkage to a potential modifier locus opens the path to location cloning of a gene capable of altering HD pathogenesis, which could provide a validated target for therapeutic development in the human patient.

Background

Huntington's disease (HD [MIM 143100]) is a progressive neurodegenerative disorder with an age at neurological onset commonly in midlife. The major clinical features of HD include involuntary choreiform movements, psychiatric symptoms, and cognitive dysfunction [1-3]. The genetic mutation associated with HD is located in 4p16.3 and is characterized by expansion of a CAG repeat in the first exon of the gene encoding the huntingtin protein [4]. Many studies have examined the relationship of the CAG repeat to neurological onset in HD, and found that its length accounts for about 70% of the variation in age at onset [5,6]. Our recent studies [7] and those of others [5,6] suggest that the remaining variation in HD age at onset is strongly heritable and about 56% [8] of the variance remaining in age at onset is attributable to genes other than the HD gene, supporting the existence of genes capable of modifying HD pathogenesis. Although Wexler et al. [5] suggest that 60% of the variance may be attributable to environmental factors, remarkable similarity for onset age in monozygotic twins [3] support primarily genetic modifiers for this trait.

Identification of genetic modifiers in HD could be of enormous importance for defining the mechanisms that may be capable of delaying the onset of the disorder. We recently reported a whole-genome scan for modifiers of age at onset for HD in 295 pedigrees containing 629 sibling pairs, with six regions, 2q33, 4p16, 5q31-32, 6p22, 6q23-24, and 18q22 exhibiting LOD scores > 1.5 [8]. In the present study, we sought to confirm our original whole-genome scan findings by conducting a follow-up study of the peak regions observed in the original scan using a newly recruited expanded follow-up sample.

Methods

Subjects

Three sample sets, newly recruited (Follow-up Sample), original (Original Sample) and combined (Combined Sample) were used in this study. Prior to the data cleaning, the Follow-up Sample consists of 149 newly recruited HD patients. Fifteen of the newly recruited siblings were members of 12 pedigrees used in the Original Study [8]. For these individuals a single sibling was randomly selected from the Original Study pedigree to create a sibling pair for the Follow-up study. The remaining 134 new patient samples were recruited from 61 new pedigrees. Only 57 of the newly recruited pedigrees, with 126 siblings were kept after removing three apparently identical twin pairs and one pair lacking onset information. Thus, the final Follow-up Sample contained 69 pedigrees (12 original and 57 newly recruited) with 141 (15 + 126) newly recruited subjects and 102 sibling pairs (Table 1).

Table 1.

The Study Subjects.

Original Sample Follow-up Sample Combined Sample
Pedigrees 295 69a 352
Sibling-pairs 629 102 753b
Patients 695 141 836
Mean Onset ± SD 39.3 ± 12.1 39.2 ± 11.8 39.3 ± 12.0
Mean HD repeat ± SD 46.4 ± 5.9 45.5 ± 5.5 46.2 ± 5.7
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Note (details provided in Subjects section of Materials and Methods):

a 57 pedigrees are newly recruited, and the remaining 12 are from the Original Sample with newly recruited siblings.

b The number of pairs in the Combined Sample exceeds that for the sum of the Original Sample and Follow-up Sample because additional sibling pairs (21 new sibling pairs and one half sib) were created when new siblings were added to existing pedigrees.

The Original Sample, used in the genome scan paper [8], consisted of 295 pedigrees with 629 sibling pairs. The Original Sample contained 20 unaffected parents and 9 unaffected siblings to increase precision in the estimation of identity by descend [8]. The Combined Sample, consisting of both the Original Sample and the Follow-up Sample, had 352 pedigrees with 836 HD subjects. Twenty-one new sibling pairs and one half sib-pair were created when new siblings were added to existing pedigrees for a total of 753 sibling pairs in the Combined Sample (Table 1).

Age at onset

Age at onset, defined as the onset of motor impairment, was reported for all affected participants [9,10]. Cases with 36 or more repeats, were designated HD mutation carriers in accordance with published associations with disease expression [11]. The quantitative trait utilized in linkage analysis was adjusted for the effects of the CAG repeat expansion using two different regression models. Both models used the logarithmically transformed age at onset as the dependent variable. The first model (Model One) adjusted only for the size of the expanded CAG repeat [log(onset) = α + β(HD)CAG]. The second model (Model Two), that we had used in our original genome scan [8] and previously described [7], adjusted for the HD repeat, the normal repeat and their interaction [log(onset) = α + β1(HD)CAG + β2(Normal)CAG + β3(HD)CAG × (Normal)CAG]. Random effect models (Proc MIXED in SAS) were used in these models to account for familial clustering. Each model was used to determine the expected age at onset for a given expanded CAG repeat, and the residual was computed as the difference between the observed and expected age at onset. Residuals were standardized to a mean of zero and a standard deviation of 1. Both models show similar modest negative skewness. The skewness of the residual generated by Model One is -0.42 and the kurtosis is 1.82. Corresponding values for Model Two were -0.49 and 1.11, respectively.

Residual onset ages for all analyses were computed using the 836 combined sample plus 234 locally studied HD patients recruited from the New England HD Research Center and 303 brain specimens from the McLean Brain Tissue Resource Center, for a total sample of 1373. While the local and brain samples are not included in this linkage analysis, they provide an additional randomly ascertained samples to more accurately model the relationship between age at onset and CAG repeat sizes. Finally, because our future studies will involve SNP association studies in all of three samples (HD MAPS families, the locally collected DNAs, and the brain specimens), we sought to define the repeat adjusted age at onset uniformly across all three samples.

The heritability analyses were conducted using maximum likelihood procedures as implemented in the SOLAR program [12].

CAG repeat size determination

HD CAG repeat sizes were determined by polymerase chain reaction using an assay that does not include the adjacent proline (CCG) repeat. Cases with 36 or more repeats were designated HD mutation carriers.

Genotyping

All the newly recruited HD samples were genotyped by three microsatellite markers at each of the six regions with maximum multipoint LOD scores greater than or equal to 1.5 in the original genome scan [8]. The markers at each locus comprised the peak marker and the two markers from the original scan that flank it (see Table 2). Prior to the analysis, the sib_kin program in the ASPEX package [13] was used to verify sibling relationships. Mendelian inconsistencies were then identified using INFER, in the PEDSYS package [14] and MERLIN [15]. Genotypes for the entire nuclear family were deleted for the particular marker when an inconsistency was detected. The genotyping data set was 93% complete, with 7% genotyping failure or error rate.

Table 2.

Eighteen microsatellite markers genotyped, three at each of the six loci, for Follow-up study. Marker 2 is the peak marker in original study at each locus.

Chromosome Marker 1 Position (cM) Marker 2 Position (cM) Marker 3 Position (cM)
2q33 D2S1391 186 D2S1384 200 D2S2944 210
4p16 D4S3360 0 D4S2366 13 D4S403 26
5q31-32 D5S816 139 D5S1480 147 D5S820 160
6p22.3 D6S1006 27 D6S1959 34 D6S2439 42
6q23-24 D6S1009 138 GATA184A08 146 D6S2436 155
18q22 D18S851 75 D18S858 80 D18S1357 89
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Linkage analysis

Variance component linkage analysis to repeat adjusted age at onset was performed using MERLIN [15]. We performed multipoint linkage analysis in the Original 295 pedigrees, the Follow-up 69 pedigrees, and the Combined 352 pedigrees. Adjusted age at onset was available for all HD affected participants. Age at onset was coded as "missing" for all unaffected individuals.

The oligogenic linkage analysis and epistatic interaction analysis were performed by the SOLAR program [12]. MERLIN was used to generate the IBD estimates and these were converted into SOLAR format for analyses. The viability of epistatic model was tested. The interaction term was constrained to non-interaction, and then the difference between interaction and non-interaction models was tested by chi-square.

Results

Three sample sets, newly recruited (Follow-up Sample), original (Original Sample) and combined (Combined Sample) were used in this study. The Original, Follow-up and Combined samples are described in Table 1. The mean age at onset is similar for the Follow-up (range 17 to 70 y) and Original samples (range 9 to 82 y). All three samples exhibited strong heritability estimates. The heritability estimates (h2 ± SE) for expanded repeat adjusted age at onset (Model One) are 0.72 ± 0.09 for the Original Sample, 0.74 ± 0.20 for the Follow-up Sample and 0.74 ± 0.08 for the Combined Sample.

Multipoint linkage analyses were completed using both Model One, adjusting for expanded HD repeats only, and Model Two, adjusting for expanded HD repeats, normal repeats and their interactions. Multipoint LOD scores obtained in these three sample sets for the six chromosome regions (2q33, 4p16, 5q31-32, 6p22, 6q23-24, and 18q22) are presented in Table 3 and Figure 1. For the Follow-up Sample, the highest LOD score was observed at the 6q23-24 region (LOD = 1.87, p = 0.002, Model One; or LOD = 2.27, p = 0.0006, Model Two). One additional region provided modest confirmation for linkage, 18q22 (LOD = 0.79, p = 0.03, Model One; or LOD = 0.79, p = 0.02, Model Two). However, no evidence for linkage was seen at 2q33 (LOD = 0.17, p = 0.2, Model One; LOD = 0.21, p = 0.2, Model Two), 4p16 (LOD = 0.0, p = 0.5, Model One and Model Two), 5q31-32 (LOD = 0.15, p = 0.2, Model One; LOD = 0.12, p = 0.2, Model Two), and 6p22 (LOD = 0.01, p = 0.4, Model One and Model Two).

Table 3.

Multipoint LOD score and chromosomal location in the Original, Follow-up and Combined samples are shown.

A Model One LOD scores.
Chromosome Location Original Sample Follow-up Sample Combined Sample
Distance *
(cM)		 LOD p-value Distance *
(cM)		 LOD p-value Distance *
(cM)		 LOD p-value
2q33 200 1.37 0.006 210 0.17 0.2 200 1.37 0.006
4p16 2 2.19 0.0007 0 0 0.5 0 1.94 0.0014
5q31-32 147 1.23 0.009 160 0.15 0.2 142 0.98 0.02
6p22.3 34 1.13 0.011 34 0.01 0.4 34 1.14 0.011
6q23-24 149 2.75 0.0002 142 1.87 0.002 149 4.05 0.00001
18q22 89 1.23 0.009 75 0.79 0.03 89 1.78 0.002
B Model Two LOD scores.
2q33 200 1.56 0.004 210 0.21 0.2 200 1.62 0.003
4p16 2 2.15 0.0008 0 0 0.5 0 1.9 0.002
5q31-32 147 1.27 0.008 160 0.12 0.2 147 0.98 0.02
6p22.3 34 0.88 0.02 34 0.01 0.4 34 0.95 0.02
6q23-24 148 3.5 0.00003 142 2.27 0.0006 149 4.94 <10-6
18q22 89 0.96 0.02 75 0.79 0.02 89 1.55 0.004
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A. Model One was used to adjust age at onset and age at onset was adjusted by HD repeats only; B. Model Two was used to adjust age at onset, and age at onset was adjusted by HD repeat, normal repeat and their interaction.

* The genetic distances are as indicated by the Marshfield linkage map [26]

Figure 1.

Figure 1

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Multipoint linkage results generated by MERLIN across six chromosome regions in followup study. The x-axis indicates genetic distance and the y-axis indicates LOD score. These data show the confirmed evidence for linkage to 6q23-24 using Model One age at onset adjustment.

Model One analysis in the Combined Sample yielded significant linkage at 6q23-24 (LOD = 4.05, p = 0.00001) and suggestive linkage at 4p16 (LOD = 1.94, p = 0.0014) and 18q22 (LOD = 1.78, p = 0.002). The 2q33 (LOD = 1.37, p = 0.006) and 6p22.3 (LOD = 1.14, p = 0.011) regions achieved a LOD score greater than 1.0. However, the LOD score at 5q31-32 dropped to 0.98 (p = 0.02). The Model Two analysis, adjusting for the expanded repeat, normal repeats and their interaction, generated higher LOD scores than Model One at 6q23-24 in all the three tested sample sets: the Original Sample (LOD = 3.5, p = 0.00003), Follow-up Samples (LOD = 2.27, p = 0.0006) and Combined Sample (LOD = 4.94, p < 10-6). All of the other analyses using Model Two produced LOD scores very similar to those of Model One. Epistatic analysis indicated that there is no interaction between 6q23-24 and five other loci.

Discussion

The purpose of this study was to replicate our original linkage findings for repeat adjusted age at onset in HD [8] in an expanded sample. A p value of 0.01 is needed to confirm evidence for linkage [16]. In this Follow-up study, strong evidence for linkage was observed at 6q23-24 (p = 0.002) and suggestive support for linkage was observed at 18q22 (p = 0.03). No evidence for linkage was observed in the Follow-up Sample at 2q33 (p = 0.2), 4p16 (p = 0.5), 5q31-32 (p = 0.2) and 6p22.3 (p = 0.4). The lack of confirmation for the latter four loci may indicate that these regions do not contain genes that modify the age at neurologic onset for HD or that this relatively small Follow-up study did not adequately sample families which carry modifier genes from these regions.

In the Combined Sample, the Model One analysis, adjusting only for the size of the expanded repeat, yielded significant linkage at 6q23-24 (LOD = 4.05, p = 0.00001). The Model Two analysis, adjusting for the expanded repeat, normal repeats and their interaction, generated higher LOD score than Model One at 6q23-24. The LOD scores of the Original Sample (LOD = 3.5, p = 0.00003), Follow-up Samples (LOD = 2.27, p = 0.0006) and Combined Sample (LOD = 4.94, p < 10-6) are highly significant using this second model. All of the other analyses using Model Two produced LOD scores very similar to those of Model One. We emphasize results from Model One because beta coefficients from Model Two show greater variability compared with those computed in the original scan [8]. Changes in the composition of the sample have modified the relationship of the repeat sizes to onset age from that seen in the original sample alone [8]. Although all three terms in the model (HD repeat, normal repeat and the interaction of these) are significant predictors of age at onset, the sign of the beta coefficients were opposite to those seen in the original scan [8] for the normal repeat and interaction terms. Consequently, the Model Two adjustment may be susceptible to as yet unidentified sample stratification effects or over-specification of the model.

The results of the Combined Sample are generally similar to those of the original genome scan (see Table 3). Significant evidence for linkage was observed at 6q23-24 in the Combined Sample (LOD = 4.05, p = 0.00001). We reported a LOD score of 2.28 at 6q23-24 in our original genome scan [8], while the same sample generates a LOD score of 3.5 (p = 0.00003) in the current study using the same model (Model Two). The difference is due to a modification of the method used to define the repeat adjusted age at onset. In the original genome scan only the 754 individuals were used to model the relationship of repeat size age at onset. In the present study, we used a sample of 1373 individuals, derived from the 836 in the combined sample, plus 234 locally studied HD affected persons and a sample of 303 brain specimens. While the local and brain samples do not represent sib-pairs that could be included in this linkage analysis, they provide additional randomly ascertained samples to more accurately model the relationship between age at onset and CAG repeat sizes. They also provide an increased sample size for subsequent fine-mapping association studies to assess candidate modifiers. The increased sample size provided a more accurate assessment of the relationship between repeat size and age at onset, yielding a residual that more accurately adjusts for the effect of repeat size on age at onset in HD.

In addition to the 6q23-24 peak, the Follow-up study supports evidence for linkage at 18q22 (LOD = 0.79, p = 0.03, Model One; LOD = 0.79, p = 0.02, Model Two). The Combined Sample provides suggestive evidence for linkage at this locus (LOD = 1.78, p = 0.002, Model One; LOD = 1.55, p = 0.004, Model Two). Suggestive linkage is still observed at 4p16 (LOD = 1.94, p = 0.0014, Model One; LOD = 1.9, p = 0.002, Model Two) in the Combined Sample, although, this locus was not confirmed in the Follow-up study and the LOD score is lower than that of the original scan (LOD = 2.19, p = 0.0007, Model One; LOD = 2.15, p = 0.0008, Model Two). The decreased LOD score at 4p16 may be a consequence of genetic heterogeneity, possibly reflecting the diverse ethnic background of the sample [17].

The epistatic analysis indicated that there is no interaction between 6q23-24 with five other loci. Therefore, we assumed that the potential modifiers are not members in a common pathway. The 1-LOD unit support interval (133 – 153 Mb) at 6q23-24 contains 128 known and predicted genes (Ensembl v27) [18]. Two genes of particular interest are serum and glucocorticoid regulated kinase (SGK, 135 Mb) and metabotropic glutamate receptor 1 (GRM1, 146 Mb). A recent study reported that SGK levels are increased in brains of HD patients; SGK phosphorylates huntingtin at serine 421, protecting striatal neurons against toxicity caused by a polyQ-huntingtin amino-terminal fragment [19]. SGK is a plausible candidate gene. GRM1 is located within 2 Mb of the peak marker (GATA184A08, 148 Mb) and is highly expressed in the cerebellum [20]. One prominent action of GRM1 is to protect neurons from apoptotic death [21]. In addition, several studies reported that GRIK2 is associated with early onset [22,23]. GRIK2 (6q16.3, 102 Mb) is about 30 Mb proximal to the 1-LOD interval on the confirmed 6q23-24 (133 – 153 Mb). However, the variance in onset age explained by GRIK2 is small and one would not expect that it would be detected by linkage. The 7-Mb 1-LOD unit support interval (50 – 57 Mb) at 18q22 contains 36 known genes, according to the Ensembl database (v27) [18]. Interesting candidate genes in this interval include NEDD4L (18q21, 54 Mb), which encodes a neural precursor cell expressed, developmentally down-regulated 4-like gene. NEDD4L is an ubiquitin ligase and contains WW domains. Yeast two-hybrid studies found that huntingtin binds to a group of genes with WW domains [24]. One of the interesting features of NEDD4L is that it may mediate degradation of the product of SGK, the above mentioned candidate gene located at 6q23 [25].

Conclusion

In conclusion, this replication study confirms evidence for linkage in the 6q23-24 region observed in our original genome scan. Although the other regions, particularly 18q22, may also contain genes that modify age at onset in HD, the 6q23-24 shows evidence for harboring one or more genetic modifiers that exceeds the level required for genome-wide statistical significance (LOD >3.6) [16]. In our approach, a genetic modifier of HD is a gene that is inherently capable of modifying the course of disease pathogenesis, thereby altering the observed age at onset. Consequently, identifying such genetic modifiers is a potential route to validated targets for therapeutic development aimed at delaying or preventing neurological onset in HD. We present evidence that the 6q23-24 region contains such a genetic modifier, which opens the way for its identification and eventual exploitation for treatment of this devastating disorder.

Abbreviations

HD: Huntington's disease

HD MAPS: Huntington's Disease Modifiers of Age at Onset in Pairs of Siblings

QTL: Quantitative Trait Loci

LOD: logarithm of the odds

Competing interests

The author(s) declare that they have no competing interests.

Authors' contributions

JL participated in the design of the study, performed the statistical analysis and drafted the manuscript. RP was responsible for the coordinating the study groups and sample collection. MRH, SCW, AD, PJM, MN, CAR, RLM, AR, FS, LF, EG, CAG, OS, MLK, RJT, EM, AN, MF, JSP, RJ, TA, AL, MHS, JJC, SMH, JBP, MBH, SLP, AZ, RKA, AJL, AD, KM, and PMC had ascertained the clinical status of the patients and provided the patient samples. JSM, TG, and MH were responsible for the genotyping. GX and LD participated in the data analysis. LAC, VCW, JFG and MEM participated in the study design, data generation, data analysis and manuscript preparation. RHM was responsible for study conception, design, and oversight and finalized the data analysis as well as manuscript preparation. All authors read and approved the final manuscript.

Pre-publication history

The pre-publication history for this paper can be accessed here:

http://www.biomedcentral.com/1471-2350/7/71/prepub

Acknowledgments

Acknowledgements

The study was supported by PHS Grant P50NS016367 (Huntington's Disease Center Without Walls), NS16375, NS32765, and the CIHR of Canada. We wish to thank the Huntington's Disease Society of America's "Coalition for the Cure", the Jerry McDonald Huntington's Disease Research Fund, and an Anonymous Donor for their support. A portion of this research was conducted using the Boston University Linux Cluster for Genetic Analysis (LinGA) funded by the NIH NCRR (National Center for Research Resources) Shared Instrumentation grant (1S10RR163736-01A1).

Contributor Information

Jian-Liang Li, Email: jlli@alum.bu.edu.

Michael R Hayden, Email: mrh@cmmt.ubc.ca.

Simon C Warby, Email: simon@cmmt.ubc.ca.

Alexandra Durr, Email: durr@moka.ccr.jussieu.fr.

Patrick J Morrison, Email: Patrick.Morrison@bch.n-i.nhs.uk.

Martha Nance, Email: nancem@parknicollet.com.

Christopher A Ross, Email: car@welchlink.welch.jhu.edu.

Russell L Margolis, Email: rmargoli@welchlink.welch.jhu.edu.

Adam Rosenblatt, Email: arosenba@jhmi.edu.

Ferdinando Squitieri, Email: neurogen@neuromed.it.

Luigi Frati, Email: luigi.frati@uniroma1.it.

Estrella Gómez-Tortosa, Email: EGomezT@fjd.es.

Carmen Ayuso García, Email: CAyuso@fjd.es.

Oksana Suchowersky, Email: osuchowe@ucalgary.ca.

Mary Lou Klimek, Email: klimek@ucalgary.ca.

Ronald JA Trent, Email: rtrent@med.usyd.edu.au.

Elizabeth McCusker, Email: elizabeth_mccusker@mail.wmi.usyd.edu.au.

Andrea Novelletto, Email: novelletto@bio.uniRoma2.it.

Marina Frontali, Email: marina.frontali@ims.rm.cnr.it.

Jane S Paulsen, Email: jane-paulsen@uiowa.edu.

Randi Jones, Email: randi852@mindspring.com.

Tetsuo Ashizawa, Email: tetsuoa@bcm.tmc.edu.

Alice Lazzarini, Email: lazzaral@optonline.net.

Vanessa C Wheeler, Email: wheeler@helix.mgh.harvard.edu.

Ranjana Prakash, Email: ranjana@bu.edu.

Gang Xu, Email: xugang05@gmail.com.

Luc Djoussé, Email: ldjousse@bu.edu.

Jayalakshmi Srinidhi Mysore, Email: srinidhi@helix.mgh.harvard.edu.

Tammy Gillis, Email: magencor@helix.mgh.harvard.edu.

Michael Hakky, Email: magencor@helix.mgh.harvard.edu.

L Adrienne Cupples, Email: adrienne@bu.edu.

Marie H Saint-Hilaire, Email: neuromsh@bu.edu.

Jang-Ho J Cha, Email: cha@helix.mgh.harvard.edu.

Steven M Hersch, Email: hersch@helix.mgh.harvard.edu.

John B Penney, Email: mghneurology@partners.org.

Madaline B Harrison, Email: MBH3Y@hscmail.mcc.virginia.edu.

Susan L Perlman, Email: sperlman@ucla.edu.

Andrea Zanko, Email: azanko@itsa.ucsf.edu.

Ruth K Abramson, Email: rka07@dmh.state.sc.us.

Anthony J Lechich, Email: alechich@chcsnet.org.

Ayana Duckett, Email: ad498@columbia.edu.

Karen Marder, Email: marderk@sergievsky.cpmc.columbia.edu.

P Michael Conneally, Email: pconneal@iupui.edu.

James F Gusella, Email: gusella@helix.mgh.harvard.edu.

Marcy E MacDonald, Email: macdonam@helix.mgh.harvard.edu.

Richard H Myers, Email: rmyers@bu.edu.

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