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Proc IEEE Int Symp Biomed Imaging. Author manuscript; available in PMC 2013 January 1.

Published in final edited form as:

Proc IEEE Int Symp Biomed Imaging. 2012 : 542–545.

doi: 10.1109/ISBI.2012.6235605PMCID: PMC3420975

NIHMSID: NIHMS393562

Neda Jahanshad,^{1} Derrek P. Hibar,^{1} April Ryles,^{1} Arthur W. Toga,^{1} Katie L. McMahon,^{2} Greig I. de Zubicaray,^{3} Narelle K. Hansell,^{4} Grant W. Montgomery,^{4} Nicholas G. Martin,^{4} Margaret J. Wright,^{4} and Paul M. Thompson^{1}

See other articles in PMC that cite the published article.

Human brain connectivity is disrupted in a wide range of disorders – from Alzheimer’s disease to autism – but little is known about which specific genes affect it. Here we conducted a genome-wide association for connectivity matrices that capture information on the density of fiber connections between 70 brain regions. We scanned a large twin cohort (N=366) with 4-Tesla high angular resolution diffusion imaging (105-gradient HARDI). Using whole brain HARDI tractography, we extracted a relatively sparse 70×70 matrix representing fiber density between all pairs of cortical regions automatically labeled in co-registered anatomical scans. Additive genetic factors accounted for 1–58% of the variance in connectivity between 90 (of 122) tested nodes. We discovered genome-wide significant associations between variants and connectivity. GWAS permutations at various levels of heritability, and split-sample replication, validated our genetic findings. The resulting genes may offer new leads for mechanisms influencing aberrant connectivity and neurodegeneration.

The human brain is a complex network of structural and functional interconnections, with diverse regions activated during functional tasks. Advanced diffusion imaging methods, which track the diffuson of water along the brain’s axons, can reveal dense microstructural fiber bundles connecting anatomically distinct cortical and subcortical regions. Such connections are remodeled throughout development [1] and deteriorate in diseases such as Alzheimer’s disease [2]. While initial investigations have examined the degree of genetic involvement in functional connectivity, genetic contributions to the brain’s structural connectivity, i.e. the proportions and densities of axonal fibers connecting cortical subregions, have yet to be explored.

The degree of genetic influence on a particular trait can be determined by studying twins. Twin studies have long been used to determine the heritability (proportion of variance explainable by genetic variation) of human traits. Some studies have begun to estimate the heritability of DTI-derived measures of fiber integrity and its asymmetry as well as other neuroimaging measures [3–6]. Proportions of variance due to genes versus environment can be inferred by fitting structural equation models (SEMs) to data from different types of twins--monozygotic (MZ) twins share all their genes while dizygotic (DZ) twins share, on average, half.

In a large family cohort comprised of 366 individuals from 223 families, we used high angular resolution diffusion imaging (HARDI) at high magnetic field (4 Tesla) along with anatomical MRI to delineate cortical regions into areas of known structure and functionality [7]. We also mapped out white matter fiber pathways using high angular-resolution HARDI tractography. In this work, we define connectivity as the proportion of total fibers traced in the brain that intersect a specific pair of cortical regions – this may include connections within or between hemispheres. The connectivities of all pairs of regions are compiled into symmetric matrices, in which each matrix element (*x,y*) is the proportion of fibers connecting brain regions *x* and *y*.

To determine the genetic influences contributing to the density of each cortical connection, we fitted a SEM to connectivity matrices extracted from 46 pairs of MZ and 64 pairs of DZ twins. If a connection was significantly influenced by genetic factors, we followed through with a genome-wide association test to identify specific genetic variants associated with the proportion of fiber densities at that connection. The sample was split in half to allow replication of discovered associations in non-overlapping samples.

Subjects included 92 young adult monozygotic (MZ) twins (46 pairs) and 128 dizygotic (DZ) twins (64 pairs) along with 146 non-twin siblings and unpaired twins with caucasian ancestry. In total, images from 366 right-handed young adults (mean age: 23.5 years, SD 2.0) were included, from a 5-year research project examining healthy young adult twins with MRI and DTI [8]. Genomic DNA was analyzed on the Human610-Quad BeadChip (Illumina) according to the manufacturers protocols (Infinium HD Assay; Super Protocol Guide; Rev. A, May 2008).

Anatomical and 105-gradient (11 b_{0}, 94 direction) high angular resolution diffusion imaging (HARDI) whole-brain MRI scans were acquired on a high magnetic field (4T) Bruker Medspec MRI scanner. T1-weighted images were acquired with an inversion recovery rapid gradient echo sequence. For imaging parameters, please see [4].

NxN structural connectivity matrices were created as in [9] with a pipeline shown in Fig 1A. A covariance matrix *S _{g}* was obtained for every matrix element in the connection matrix within the pairs for each of the two types of twins (identical or fraternal). A structural equation model (SEM) was then fitted to compare the observed and expected covariances (under different degrees of heritability) to estimate the proportion of the variance attributable to additive genetic (A), shared environmental (C) and unique environmental (E) components of variance [10]:

a) NxN connectivity matrix design workflow; b) workflow for genetic association analysis in independent non-overlapping samples (for split-sample replication of genetic hits).

In SEM, the χ^{2} goodness of fit measure determines a *p*-value for all specified regions of interest (elements of the matrix) where the test was performed. This value indicates that the model is a good fit to the data if *p*>0.05 (this is the opposite of the usual convention that rejects models or hypotheses). To determine the significance of the the A or C factors, the χ^{2} goodness-of-fit values of the model are compared to those for a model excluding that factor (i.e., to a C/E model to determine the significance of the additional A factor; A/E model to determine the significance of C), giving:
$p(A)={\chi}_{1DF}^{{2}^{-1}}\left[{\chi}^{2}(\mathit{ACE})-{\chi}^{2}(CE)\right]$, where χ^{2}
_{IDF}^{−1} denotes the inverse of the cumulative distribution function for a chi-squared distributed variable with one degree of freedom. *p(C)* is computed analogously. In this case, low *p*-values express significant improvements when adding a factor. This is consistent with the more standard convention for *p*-values, and allows us to assess the resulting uncorrected *p*-value maps using the false discovery rate (FDR) method [11].

OpenMX software [12] was implemented in R (http://www.r-project.org/) for calculating the A/C/E parameters. The covariates sex, age, and total brain volume (TBV) were added to the model, and 95% CIs for the A term were computed.

Genome-wide associations were performed at each of the 90 valid (out of 122) matrix elements (after filtering out connections which are not heritable (a^{2} < 0.01) or not present in at least 95% of the subjects) using *emmaX* - a mixed model approach - controlling for age, sex, and TBV [13]. Connections with a heritability estimate of < 1% were excluded to limit the search region to connections where we can estimate some degree of genetic interation. EmmaX accounts for the familial relatedness between subjects through the use of a kinship matrix describing the genetic similarities between all pairs of subjects. Analysis was limited to those single nucleotide polymorphisms (SNPs) with a minor allele frequency (MAF) greater than 0.1. 428,287 SNPs were tested.

A significance threshold of 7×10^{−9} was established for genome-wide significance for reasons described below. We determined significance levels for association tests by first estimating the total number of independent tests performed. Linkage disequilibrium (LD) leads to correlation among the 428,287 SNPs and when two genotyped SNPs are in high LD, each test is not completely independent. By first estimating the effective number of independent tests we can avoid using an unduly conservative significance criterion. Due to linkage disequilibrium, the effective number (M* _{eff}*) of SNPs tested [14] was 214,578. The same logic can also be applied to the matrix elements tested. Clearly an off-diagonal element is not independent of the entries in the same row and column. For a matrix element, C(

At each of the 90 accepted nodes in the connectivity matrix, a GWAS was performed for the 220 twins used in the A/C/E structural equation model. To determine any potential differences in the null distributions with respect to the degree of the additive genetic component, GWAS was performed 1000 times on permuted matrices. When conducting these permutations, each subject’s covariates (age, sex, and TBV) remained true to its source, while the matrix elements were permuted in a manner that ensured preservation of family structure. Values for MZ twin pairs were only permuted with each other, while the DZ twin pairs were permuted separately. Within each permutation, within-twin pair rearrangements were also allowed to maximize permutations.

While all families are participants in the same study, each family is genetically unique, so we were able to split our large sample into two unique subgroups in order to provide a genetically independent sample for replicating the effect of any suggestive genetic variants on brain structural connectivity. A schematic workflow, of the processing and statistical pipeline, is presented in Fig 1B. The groups were split according to unique subject identification numbers. All members of the same family were assigned to the same group. No significant differences were seen between groups with respect to sex (*p* = 0.91) or TBV (*p* = 0.06). As the study was deliberately designed to sample young adults in the narrow age-range 21–30, although mean differences were minimal, there was a significant difference in age as calculated through a two-sided t-test of the populations (*p* = 1.2×10^{−18}; mean Group 1 = 24.4; mean Group 2 = 22.6).

Fig. 2 shows regions for which the A/C/E model was found to fit the data well and a^{2} >1% as well as CDF plots of describing the significance of ACE, and sub-models with respect to the E model. Fig 3 shows the null distribution of GWA statistics at 10 connections with increasing levels of heritability. We note in general that when preserving the family structure, as is done in this case, the choice of more highly heritable connections tended to produce permutations with on average lower p-values. Across all 1000 permutations of the 10 connections, 251 SNPs had a p-value falling below the 7×10^{−9} genome-wide significance threshold, which suggests that the expected number of false positives over all 90 regions in the group is on average is 90×0.0251 = 2.26 (where we found 4).

Genetic analysis of a sample of 46 monozygotic twin pairs and 64 dizygotic twin pairs, through the A/C/E structural equation model, breaks down the observed variance in structural neural connectivity into variance components describing the contribution **...**

At connections with increasing levels of heritability, from 1% to 58% (a–j), 1000 GWASs were conducted on permutations of the twin NxN matrices used for the A/C/E heritability analysis. The −log10 of the lowest 1000 p-values of each permutation **...**

Our GWAS of the connectivity in Group 1 showed a genome-wide significant (*p* = 3.23×10^{−9}) association within the *SPON1* gene. The contribution of this variant was then assessed in Group 2 at the same node. The association was replicated in the second group to again show significant (*p* = 0.0021) reductions (un-standardized slope of regression, *β _{Group1}* = −0.0022,

For exploratory purposes, we combined the two groups to perform a GWAS at all 90 nodes as before. With 331 genotyped subjects (out of 366 subjects overall with matrices computed), the statistical power for genetic association is greatly increased; however, we are no longer able to provide a sample for replication. 4 SNPs were found to be significant: 3 in *SPON1* and one in *DLGAP2*. A stronger association for the *SPON1* variants is presented in the full group for the same connection, with an additional variant in the *DLGAP2* gene showing significant associations with the proportion of fibers connecting the right superior parietal lobe and the right post-central region of the cortex. Manhattan plots for the 2 nodes where variants reached genome-wide significance are presented in Fig 5.

In this study, we used 94-direction HARDI in 366 individuals at 4 Tesla, to trace fiber tracts throughout the entire brain using an orientation distribution function (ODF) based tractography method [16]. We used automatically extracted cortical labels to compute cortical connectivity matrices based on the proportion of fiber counts. Expanding on a twin design, we conducted the first-ever genetic and genome-wide association analysis of the connectivity matrices.

The nodes where genome-wide significant associations were discovered include the connections between the left superior parietal lobe and the left posterior cingulate (*SPON1*) and those between the right superior parietal lobe and the right post-central cortex (*DLGAP2*). Through our A/C/E analysis, we were able to attribute 7.1% and 38.6% of the observed variance in these two connections, respectively, to additive genetic components. Our previous analysis as demonstrated the reliability of these matrices [17]. Variants found in this study may have particular significance to genetic mechanisms underlying physiological pathways, rather than affecting the global white matter fiber density. Corrections for performing a genome-wide search (and tests across each element of the *NxN* matrix) are also highlighted in this study.

This work was supported by NIH grant R01 HD050735 and NHMRC (Australia) grant 496682, R01 EB008281, and P41 RR013642, and NLM T15 LM07356.

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