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Fig. S1 (a) Likelihood probabilities lnP(D) representing 10 independent runs for each examined number of assumed population clusters (K), analysed in STRUCTURE version 2.2 (Pritchard et al. 2000). (b) Subsequent statistical evaluation of the likelihood values for a given number of assumed population clusters (K) using the ad hoc statistic ΔK proposed by Evanno et al. (2005). (c) and (b) are analogous to (a) and (b) having derived from five independant runs using a null-allele-corrected dataset.

Fig. S2 Individual-based cluster representation based on Bayesian inference of population structure for two scenarios (a–d) K = 2 and (e–h) K = 4.

Fig. S3 Factorial component analysis representing the first three orthogonal axes of variation ranked by informativeness.

Fig. S4 Neighbour-joining (NJ) phenogram summarizing Cavalli-Sforza & Edwards’ (1967) DCE chord distances without null-allele correction among 12 invasive and three native populations.

Fig. S5 Box plot representation of local allelic richness (rarefacted number of alleles per locus) between European, North American and Asian locations.

Fig. S6 Box plot representation of mean allelic uniqueness for (a) the four markers deviating from HWE (AcrCT29, AcrCT53, AcrCT103, AcrCA102); and (b) three markers not deviating from HWE (AcrCT04, AcrCT27, AcrCT54).

Table S1 Allele counts and rarefacted allelic richness and diversity (n = 24 genes) as measured for all microsatellite loci.

Table S2 Unbiased expected (HE) and observed (HO) heterozygosities for single loci, including respective inbreeding coefficients (FIS) and probabilities (P) of exact tests for Hardy-Weinberg equilibrium for all locations.

Table S3 Measures of mitochondrial DNA diversity observed in cytochrome c oxidase subunit I (COI) of Anguillicola crassus from 16 locations in Europe, North America and putative source populations from East Asia. Haplotype gene diversity h and nucleotide diversity π contain standard deviations of each estimate.

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