- Open Access
Genetic parameters for growth and faecal worm egg count following Haemonchus contortus experimental infestations using pedigree and molecular information
Genetics Selection Evolution volume 46, Article number: 13 (2014)
Haemonchosis is a parasitic disease that causes severe economic losses in sheep industry. In recent years, the increasing resistance of the parasite to anthelmintics has raised the need for alternative control strategies. Genetic selection is a promising alternative but its efficacy depends on the availability of genetic variation and on the occurrence of favourable genetic correlations between the traits included in the breeding goal. The objective of this study was twofold. First, to estimate both the heritability of and the genetic correlations between growth traits and parasite resistance traits, using bivariate linear mixed animal models, from the phenotypes and genotypes of 1004 backcross lambs (considered as a single population), which underwent two subsequent experimental infestations protocols with Haemonchus contortus. Second, to compare the precision of the estimates when using two different relationship matrices: including pedigree information only or including also SNP (single nucleotide polymorphism) information.
Heritabilities were low for average daily gain before infestation (0.10 to 0.15) and average daily gain during the first infestation (0.11 to 0.16), moderate for faecal egg counts during the first infestation (0.21 to 0.38) and faecal egg counts during the second infestation (0.48 to 0.55). Genetic correlations between both growth traits and faecal egg count during the naïve infestation were equal to zero but the genetic correlation between faecal egg count during the second infestation and growth was positive in a Haemonchus contortus free environment and negative in a contaminated environment. The standard errors of the estimates obtained by including SNP information were smaller than those obtained by including pedigree information only.
The genetic parameters estimates suggest that growth performance can be selected for independently of selection on resistance to naïve infestation. Selection for increased growth in a non-contaminated environment could lead to more susceptible animals with long-term exposure to the infestation but it could be possible to select for increased growth in a contaminated environment while also increasing resistance to the long-term exposure to the parasite. The use of molecular information increases the precision of the estimates.
Haemonchus contortus (H. contortus) is a nematode that feeds on blood through the abomasal mucosa of bovine, ovine and caprine species . The cost of H. contortus infection or haemonchosis for the production sectors of sheep farming in terms of anthelmintic treatments that are currently the most popular control strategy, and the resulting economic loss have been estimated in different countries to be in the order of several million dollars per year [2–7]. Furthermore, anthelmintics tend to select the parasite population under treatment for resistance to the anthelmintic itself [8, 9], which increases the cost of haemonchosis even more.
Both the long-term loss of efficacy and the growing public concern for the use of chemicals in food production fostered the research on alternative control strategies or combinations of them , among which genetic selection is one of the most promising approaches [11–25]. Simulation studies based on evolutionary genetics  predict a breeding plan’s long-term outcomes and also the efficacy of genetic selection as a control strategy. Since genetic improvement depends on the genetic parameters of the traits under selection, the estimates of these parameters must be as precise as possible for reliable long-term predictions. However, consistent estimates of the genetic correlation between production traits and parasite resistance traits have not been reported in the literature [27–33]. Since most of the estimates found in the literature are computed from observations in natural conditions, where it is not possible to precisely define neither the nutritional level of the diet nor the larval challenge on the pasture, the reason why no consistent estimates are available may be due to the interaction between these two factors .
The first objective of this study was to estimate the heritability of average daily gain and faecal egg count from experimental observations, together with the genetic correlations between them. We report the results of an analysis performed on 1004 phenotypic records of growth traits and faecal egg counts collected on genotyped (50 k SNPchip) back-cross lambs (25% Martinique black belly and 75% Romane), following two experimental infestations with H. contortus. The genetic parameters have been estimated both by using pedigree information only and pedigree and SNP (single nucleotide polymorphism) chip information jointly. Computing the relatedness between individuals using pedigree information only is based on expectation and results in an estimate corresponding to the average number of alleles shared by two individuals, for example: all the individuals belonging to the same full-sibs group would have a coefficient of 0.5 between each other, which means that it does not take into account the deviation from this average caused by segregation and recombination. However, including molecular information makes it possible to compute the relatedness between individuals by identifying on a relatively dense map the actual number of alleles they share, which provides a more detailed estimate of the relatedness between individuals . Since the observations used in this study were collected on four large groups of half-sibs, the second objective of the study was to test whether including SNP information could help reach more precise estimates than using pedigree information only when the pedigree of the population is poorly informative. Although previous studies have already explored the amount of genetic variability for parasite resistance traits, this study features several novelties: the genetic parameters reported here are estimated from phenotypes collected in experimental settings rather than natural infestation, the growth traits analysed are the average daily gains before infestation and during infestation rather than the body weights, and finally the estimates reported here also feature molecular information rather than pedigree information only.
The population in which the observations were collected from resulted from a back-cross mating scheme between two pure-bred populations: Martinique Black Belly (MBB) and Romane (ROM). MBB is a tropical sheep breed, which is characterized by adaptation to heat-stress, to parasitism and to extensive raising conditions. The ROM sheep breed features good productive performances (both for meat production and prolificacy) and no selection for resistance to parasites. The pedigree used in the analysis (Figure 1) was three generations deep and counted a total of 3164 animals. Four F1 sires were produced by crossing MBB and ROM individuals. The sires were mated by intra-uterine artificial insemination to 829 pure-bred ROM dams in order to obtain 1265 back-cross offspring (BC), the number of animals used in this study from each group of half-sibs were 282, 251, 247 and 223, respectively. All animals were managed as a commercial flock, the experimental protocol complied to the European ethical policy and was approved by the ethical committee “comite d’ethique CIRAD-INRA”.
A total of 1044 animals among the population of the back-cross lambs and their four F1 sires were genotyped with the OvineSNP50 Beadchip (Illumina Inc., San Diego, CA). Quality control of the SNPs included the following tests: (1) 50 animals were genotyped twice in order to assess the technical reliability of the genotyping, which resulted in a value of 99.9%, (2) individuals with a call rate below 98% and SNPs with a call rate below 97% or with a minor allele frequency below 1% or featuring a deviation from expected heterozygosity or showing mendelian inconsistencies were discarded (p < 10-6) and (3) quality control of the genotypes resulted in 42 469 SNPs that comply with all quality checks. More details about the genomic information can be found in Sallé et al. .
Phenotypes on growth traits and parasite resistance traits were collected on the BC animals only by performing the following experimental protocol. The lambs were weaned around 64 or 45 days, depending whether their mother was either primiparous or not, and grew in a H. contortus free environment until the first experimental infestation was performed. During this period the animals were kept in an H. contortus free environment and were weighed twice: at weaning and at the end of the growing period. The growing period ended with the beginning of the following experimental infestation protocol, which also determined when the environment was to be contaminated with H. contortus larvae: at around 90 days of age, the lambs received an oral inoculation of 10 000 L3 larvae of H. contortus (ENVT strain ) and around 41 days after the infestation, they received an anthelmintic treatment (LEVAMISOLE 5%, Vibrac S.A., Carros, France, 7.5 mg/kg live weight). During the infestation, two faecal samples were collected, at 25 and 35 days after infestation, and the animals were weighed on the day of treatment. Then, they entered a recovery period of 8 days, at the end of which they were infested again with the same infestation protocol. During the second infestation, two faecal samples were collected as before but animals were not weighed. During the whole protocol, the animals were fed ad libitum on a diet that covered largely their requirements. The faecal egg count in each sample was measured by a modified McMaster procedure . The average of the two faecal egg count observations was computed for each infestation. The latter values were transformed by taking their fourth root in order to bring their distribution closer to normality. A further transformation was applied in order to scale the standard deviation to 1 and avoid zero values. The variables obtained were called: FEC1 (transformed faecal egg counts during the first infestation) and FEC2 (transformed faecal egg counts during the second infestation). The average daily gain from weaning to infestation (ADG0) and average daily gain during the first infestation (ADG1) were computed as follows: , where growth0 and time0 are the weight gain and the days running from the weaning day to the day of beginning of the first infestation, respectively; growth1 and time1 are the weight gain and the days running from the first day of the first infestation to the day of treatment of the first infestation, respectively.
A transformation for scaling the standard deviation to 1 and avoiding 0 s was applied on growth traits as well. The observations outside a range of 2.96 standard deviations around the average of each trait were considered atypical and excluded from the analysis. Finally, only the animals featuring a valid observation both on genotyping and on at least one trait were included in the analysis, which resulted in 40 animals being discarded and 1004 animals being included.
Estimation of the genetic parameters was performed by considering the back-cross population as a single breed population. The breed proportions are taken into account by the genetic relationship matrix in the model including SNP information but could not be taken into account in the model including pedigree information only due to convergence failure. The heritability of each trait and both the genetic correlation and phenotypic correlation between each pair of traits were estimated by bivariate animal mixed models, which were solved by the AIREML procedure implemented in AIRemlF90 software . This software features by default the correction for the change in the definition of the base population so that the estimates obtained when using pedigree information only were comparable to those obtained when including molecular information [40, 41]. The bivariate mixed model reads as follows:
where y 1 and y 2 are the vectors of observations of trait one and two, respectively, X 1 and X 2 are incidence matrices relating each observation to its respective set of fixed effects and b 1 and b 2 are the vectors of the fixed effects: weight at weaning (for ADG0 only) or weight at first infestation (for all the other traits), contemporary group (identified by year, season, weighting lot and infestation lot), sex and feeding mode (breast feeding or bottle feeding). a 1 and a 2 are the vectors of random animals breeding values, with the associated incidence matrices Z 1 and Z 2 . e 1 and e 2 are the vectors of random residuals. It is assumed that the random effects are normally distributed and feature the following variance-covariance structure:
where are the genetic variances and the genetic covariance between traits 1 and 2, are the residuals variances and the residuals covariance between traits 1 and 2, I is an identity matrix and T is the genetic relationship matrix between the animals.
The genetic and phenotypic correlations between each couple of traits were computed using two different genetic relationship matrices: one computed by using pedigree information only (PED model) and one computed by including both SNP and pedigree information jointly (SNPED model). The T matrix used in the PED model was computed according to Quaas  and without using molecular information. The T matrix used in the SNPED model was computed according to VanRaden , using a three-generation deep pedigree and the following weights: T = 0.95G + 0.05A 22 , where A 22 is the relationship matrix between the genotyped animals computed by using the pedigree information only  and G is the genomic relationship matrix among genotyped animals. In the software package used for this study , the G matrix is computed by default as follows: G = WK− 1W,  where W is a rectangular matrix (number of animals by number of SNPs’ alleles) with elements: w ij = f ij − 2p j , where f ij is a scalar equal to the number of copies of one allele an animal i has at locus j, pj is the frequency of allele j in the population, K is the diagonal matrix of the scaling parameters with elements: K jj = 2 ∑ p j (1 − p j ). The weights of G and are used for bending the genetic relationship matrix and make it positive definite, as required for its inversion , this is similar to the bending procedure occurring in AIREML algorithms for keeping the variance covariance matrix positive definite .
The precision of the heritability and correlation estimates was computed by estimating their standard error according to the following formulas :
where is the standard error of the estimate of the heritability of trait i, and are the estimates of its genetic and phenotypic variances, respectively, , and are the variances of the estimated values and the covariance between the estimated values, respectively, obtained from the information matrix :
where SE(r g ) is the standard error of the estimate of the genetic correlation, r g is the estimated value of the genetic correlation; are the estimates of the genetic variance components described above and V(.) and C(..) are the variance of the estimates between parenthesis and the covariance between the estimates between parenthesis, respectively. The same formula was used to compute the standard error of the phenotypic correlation, but by filling in the entries concerning phenotypic variances and covariances.
The parameters under study are the ratio of two normally distributed variables (heritability) and the ratio between a gaussian variable over the square root of the product of two gaussian variables (correlations). The sampling distribution of heritability can be approximated to a gaussian distribution under certain specific conditions only . When these conditions are filled, the significance test for gaussian variables can be applied. However, the significance tests for the correlation coefficient can be developed by deriving its confidence interval according to Fisher's Z-transformation . Otherwise, both parameters can be tested by using a re-sampling procedure such as delete-d jackknife: where d is the number of observations randomly discarded from the dataset and n1/2 < d < n (n is the total number of observations in the dataset) . One thousand sub-samples of the whole dataset were created by randomly discarding 20% of the observations. Each parameter computed above was re-estimated from each sub-sample in order to build its empirical distribution. The empirical distribution of each parameter was used to compute the confidence interval of each parameter by taking its 2.5% quantile as the lower bound and its 97.5% quantile as the upper bound of each estimate. The null hypothesis “the estimate is not different from 0” was tested as follows: if the confidence interval of the estimate included 0, then the null hypothesis was not rejected, otherwise the alternative hypothesis “the estimate is different from 0” was accepted. In order to test whether the SNPED and SNP models converged to the same estimate, the distribution of the difference between the PED and SNPED estimates was built for each estimate as follows:
where Ped i is the vector containing the n realizations of the estimate obtained from the PED model, Snped i is the vector containing the n realizations of the estimate obtained from the SNPED model, d i the vector of the differences between and each element of Ped i and Snped i . The confidence interval of the distribution of the difference was computed as above. The null hypothesis “the difference between the estimate obtained from the PED model and the estimate obtained from the SNPED model is 0” was tested against the alternative hypothesis “the difference between the estimate obtained from the PED model and the estimate obtained from the SNPED model is not 0” as above as well.
Results and discussion
Table 1 shows the summary statistics of the variables analysed. The transformations applied to the raw faecal egg counts resulted in the profile of their distribution being closer to normality. The skewness and normalized kurtosis of FEC1 changed from 2.11 to −0.44 and from 6.56 to 0.53, respectively; the skewness and normalized kurtosis of FEC2 changed from 3.87 to 0.14 and from 23.92 to −0.74, respectively. The number of observations on each trait together with the average, standard deviation, minimum and maximum of the raw observations are in Table 1. ADG1 was significantly lower than ADG0 (p_value < 0.0001), indicating that infested animals had a slower growth than the parasite-free animals, as expected due to the infestation .
Table 2 shows the estimate of the phenotypic correlations (below the diagonal) obtained from the two models for each pair of traits. Although the SNPED and PED models did not always converge on the same value, according to the significance tests described above, these estimates were not significantly different between the two models. The estimates of the phenotypic correlations between ADG0 and both FEC1 and FEC2 were not significantly different from 0: -0.01 (SE = 0.15) and 0.01 (SE = 0.18) for the PED model and 0.02 (SE = 0.11) and 0.04 (SE = 0.11) for the SNPED model. These results suggest that the phenotype for growth rate in a H. contortus free environment was unrelated to the parasite resistance phenotype. However, the estimates of both the phenotypic correlations between ADG1 and FEC1 and between ADG1 and FEC2 were negative: -0.24 (SE = 0.15) and −0.20 (SE = 0.19) for the PED model and −0.23 (SE = 0.11) and −0.19 (SE = 0.11) for the SNPED model. These results suggest an inverse proportionality between the growth rate and the parasite burden, in accordance with the finding that contaminated animals had a slower growth than non-contaminated animals. The average faecal egg count during the second infestation was significantly lower than the faecal egg count during the first infestation (p_value < 0.0001), which suggests that the development of a specific immune response was triggered by the first infestation, that enhanced the intrinsic resistance of the animals to subsequent infestations . Furthermore, the positive estimate of the phenotypic correlation between FEC1 and FEC2, 0.46 (SE = 0.43) for the PED model and 0.62 (SE = 0.20) for the SNPED model, shows that the animals featuring higher (or lower) than average FEC1 are likely to express higher (or lower) than average FEC2, and vice versa. This suggests that a repeatable variation in susceptibility occurs within the population.
Table 2 summarizes the estimates of the heritabilities of each trait (block diagonal) and the estimates of the genetic correlations (above the diagonal) between each pair of traits obtained with the PED and SNPED models, together with the standard error of each estimate (between brackets). Due to the pedigree structure that includes only four sires, both the standard errors and the 95% confidence intervals of the estimates were indeed large (in particular, those of the PED model), which led to no significant difference between the estimates obtained from the two models. The results obtained were in general coherent between models, except for the genetic correlation between ADG0 and FEC1, which was positive with the SNPED model and negative with the PED model. However, the latter estimate had a standard error as large as half the parameter space, which resulted in the confidence of the difference between the two estimates to include 0. The reason for this possible inconsistency cannot be defined by the data available for this study. We can only speculate that it could be the result of the segregation variance captured by the SNP chip, because the phenotypes analysed were collected on the back-cross offspring of only four sires. This pedigree structure is indeed poorly informative if the estimate is computed by using pedigree information only, which is clearly shown by the huge standard error obtained with the PED model. However, this does not explain why such a big difference in the estimates occurs between some pairs of traits only. The heritability of ADG0 was low for both models, 0.10 (SE = 0.08) for the PED model and 0.15 (SE = 0.07) for the SNPED model, and is close to the value 0.17 found in the review of Safari et al. . The heritability of ADG1 was low as well, 0.16 (SE = 0.04) and 0.11 (SE = 0.06) for the PED and the SNPED model respectively and no estimates were found in the literature for ADG1. The estimates for the heritabilities of both faecal egg counts were found higher than those obtained in previous studies [29–32]: FEC1 was 0.21 (SE = 0.06) and 0.38 (SE = 0.04) for the PED and the SNPED model, respectively; FEC2 was 0.55 (SE = 0.09) and 0.48 (SE = 0.06) for the PED and the SNPED model, respectively. The reason for finding a higher value than in previous studies could be twofold. First, it could be due to the fact that most of the estimates found in the literature are computed from observations in natural rather than experimental conditions, the latter of which allows controlling more strictly the environmental conditions and hence could reduce phenotypic variation. The second reason could be the occurrence of breed specific alleles that segregate within the back-cross population, which inflate the genetic variance compared to a pure breed population. These values confirm the availability of a moderate genetic potential in sheep that could be exploited to enhance resistance to parasites.
Concerning previous estimates of the genetic correlation between growth traits and faecal egg counts, no other estimations of these parameters based on experimental infestation were found in the literature. Furthermore, previous studies on similar traits based on natural infestations do not show consistency among them [29–32], which could be explained by the uncontrolled variation in the larval challenge, in the pathogenicity of the parasite in each population, in the feed intake and the interaction between these three factors .
Concerning the genetic correlations between growth traits (ADG0 and ADG1) and parasite resistance during the naïve infestation (FEC1), the following picture can be drawn. In accordance with the estimates of the phenotypic correlation between ADG0 and FEC1, the genetic correlations between these traits were also not significantly different from 0: -0.52 (SE = 1.06) for the PED model and 0.11 (SE = 0.47) for the SNPED model. The same results were obtained with the estimate of the genetic correlations between ADG1 and FEC1 (although their phenotypic correlations were negative according to both models): -0.19 (SE = 0.80) for the PED model and −0.12 (SE = 0.58) for the SNPED model. These results suggest that during the naïve infestation, the genotype for growth (ADG0 and ADG1) could be expressed independently from the genotype for parasite resistance (FEC1).
The results obtained for the genetic correlations between growth traits and the long-term resistance (FEC2) were on the contrary significantly different from 0. On the one hand, the genetic correlation between ADG0 and FEC2 was positive but not significantly different from 0 according to the PED model (0.25, SE = 0.85) and positive (0.57, SE = 0.38) according to the SNPED model. According to the approximate standard errors, the positive estimate obtained with the SNPED model is more reliable and suggests that if animals were selected for growth in a parasite-free environment, a correlated selection response for lower long-term resistance to gastrointestinal parasites could occur as well. This estimate supports the hypothesis that enhancing growth traits could come to a cost to the sheep's long-term susceptibility to parasite infestations, and vice versa [49, 50]. On the other hand, the correlation between ADG1 and FEC2 was consistently negative between models: -0.48 (SE = 0.67) for the PED model and −0.54 (SE = 0.53) for the SNPED model, which suggests that growth during the naïve infestation can be enhanced together with long-term resistance to the infestation within a single purebred line.
The genetic correlation between FEC1 and FEC2 was 0.46 (SE = 0.43) and 0.62 (SE = 0.20) for the PED and SNPED models, respectively, which suggests that these traits have different determinisms. While FEC1 represents a measure of the parasite resistance expressed by a naïve lamb, FEC2 is a measure of the parasite resistance expressed by an immunized lamb, and indeed the mechanisms by which these types of animals respond to the infestation are different .
The estimate of genetic correlation between ADG0 and ADG1 was unstable due to its sensitivity to the starting values used for its estimation and is not reported.
Table 3 shows both the ratio of the standard errors of the estimates obtained from the PED model over the standards error obtained from the SNPED model, which ranged from 1.04 to 2.25 and also the ratio between the width of the confidence intervals of the estimates obtained from the PED model over the width of the confidence intervals obtained from the SNPED model, which spanned an interval between 0.93 and 4.21. According to the ratio of the standard errors, the SNPED model always converged to more precise values, while, according to the ratio of the width of the confidence intervals, the estimate of the phenotypic correlation between growth traits and FEC1 obtained from the PED model was slightly more precise.
The results obtained show that including SNP information in the computation of the relationship matrix between individuals can increase the precision of the genetic parameter estimates up to twice the precision obtained by using pedigree information only . The increase in precision can be explained by the fact that SNP information allows to compute more precisely than pedigree information what proportion of genome two individuals actually have in common. The pedigree structure in the data available for this study was not ideal to estimate genetic parameters by pedigree information only because all observations are recorded on a population of animals composed of four groups of half-sibs. Such a structure causes the pedigree-based relationship matrix to predict that within each group of half-sibs all animals share one quarter of the sire’s genome. Whereas, the marker-based relationship matrix allows capturing the segregation variance, which means capturing the random deviation of the proportion of genes shared by two individuals around the expected proportion of shared genes according to the pedigree .
According to the results obtained by the model including both pedigree and molecular information, the genotypes for growth and for resistance to naïve infestation can be selected for independently. However, the genetic correlations between long-term parasite resistance traits and growth traits were different from 0 and suggest that increasing growth performance in a H. contortus free environment could result in more susceptible animals, whereas growth performance in a contaminated environment can be increased while enhancing long-term resistance to H. contortus. The two results taken together can also be interpreted as an indication of genotype by environment interaction affecting growth expressed across the two environments . The model that includes pedigree information only converged to similar results, except for the genetic correlation between growth before infestation and faecal egg count during the first infestation which was affected by a very large standard error. The reason for this inconsistency needs further investigation.
This study shows that, when the pedigree is poorly informative using molecular information and pedigree information jointly result in more precise genetic parameters than using pedigree only.
Urquhart GM: Veterinary Parasitology. 1996, Oxford: Blackwell Science
Waller PJ, Chandrawathani P: Haemonchus contortus: parasite problem No. 1 from tropics-polar circle. Problems and prospects for control based on epidemiology. Trop Biomed. 2005, 22: 131-137.
Nieuwhof GJ, Bishop SC: Costs of the major endemic diseases of sheep in Great Britain and the potential benefits of reduction in disease impact. Anim Sci. 2005, 81: 23-29.
Sani RA, Gray GD, Baker RL: Worm Control for Small Ruminants in Tropical Asia. 2004, Canberra: ACIAR Monograph 113
Waller PJ, Dash KM, Barger IA, Le Jambre LF, Plant J: Anthelmintic resistance in nematode parasites of sheep: learning from the Australian experience. Vet Rec. 1995, 136: 411-413. 10.1136/vr.136.16.411.
McLeod RS: Costs of major parasites to the Australian livestock industries. Int J Parasitol. 1995, 25: 1363-1367. 10.1016/0020-7519(95)00071-9.
Vlassoff A, McKenna PB: Nematode parasites of economic importance in sheep in New Zealand. New Zeal J Zool. 1994, 21: 1-8. 10.1080/03014223.1994.9517971.
Kaplan RM: Drug resistance in nematodes of veterinary importance: a status report. Trends Parasitol. 2004, 20: 477-481. 10.1016/j.pt.2004.08.001.
Wolstenholme AJ, Fairweather I, Prichard R, Von Samson-Himmelstjerna G, Sangster NC: Drug resistance in veterinary helminths. Trends Parasitol. 2004, 20: 469-476. 10.1016/j.pt.2004.07.010.
Bernstein J, Cochrane N, Hasha G, Kelch D, Leetmaa S, Mitchell L, Morath T, Normile MA: The European Union’s Common Agricultural Policy: Pressures for Change.http://www.google.fr/url?sa=t&rct=j&q=&esrc=s&source=web&cd=1&ved=0CDcQFjAA&url=http%3A%2F%2Fers.usda.gov%2FersDownloadHandler.ashx%3Ffile%3D%2Fmedia%2F913260%2Fwrs992_002.pdf&ei=tmWpUsfpEqaI0AW_84HoBw&usg=AFQjCNFklKL3zU4mGHeab4sNzApX0n6UFA&bvm=bv.57967247,d.d2k&cad=rja,
Getachew T, Dorchies P, Jacquiet P: Trends and challenges in the effective and sustainable control of Haemonchus contortus infection in sheep. Review. Parasite. 2007, 14: 3-14. 10.1051/parasite/2007141003.
Torres-Acosta JFJ, Hoste H: Alternative or improved methods to limit gastro-intestinal parasitism in grazing sheep and goats. Small Ruminant Res. 2008, 77: 159-173. 10.1016/j.smallrumres.2008.03.009.
Smith WD, Zarlenga DS: Developments and hurdles in generating vaccines for controlling helminth parasites of grazing ruminants. Vet Parasitol. 2006, 139: 347-359. 10.1016/j.vetpar.2006.04.024.
Saul GR: Effects of two pasture systems on faecal nematode egg counts in breeding ewes. Aust Vet J. 1996, 74: 154-155. 10.1111/j.1751-0813.1996.tb14820.x.
Hoste H, Torres-Acosta JFJ: Non chemical control of helminths in ruminants: adapting solutions for changing worms in a changing world. Vet Parasitol. 2011, 180: 144-154. 10.1016/j.vetpar.2011.05.035.
Barger IA, Siale K, Banks DJ, Le Jambre LF: Rotational grazing for control of gastrointestinal nematodes of goats in a wet tropical environment. Vet Parasitol. 1994, 53: 109-116. 10.1016/0304-4017(94)90023-X.
Eysker M, Bakker N, Kooyman FNJ, van der Linden D, Schrama C, Ploeger HW: Consequences of the unusually warm and dry summer of 2003 in The Netherlands: poor development of free living stages, normal survival of infective larvae and long survival of adult gastrointestinal nematodes of sheep. Vet Parasitol. 2005, 133: 313-321. 10.1016/j.vetpar.2005.05.058.
González Garduño R, Cordero Ortega JC, Torres Hernández G, Arece García J, Mendoza de Gives P: Efecto del hipoclorito de sodio y extracto de cítricos en la reducción de la infestación con nematodos gastrointestinales resistentes a antihelmínticos en ovinos de pelo. Rev Mex Cienc Pecuarias. 2010, 1: 179-187.
Larsen M: Biological control of nematode parasites in sheep. J Anim Sci. 2006, 84: E133-E139.
Terrill TH, Larsen M, Samples O, Husted S, Miller JE, Kaplan RM, Gelaye S: Capability of the nematode-trapping fungus Duddingtonia flagrans to reduce infective larvae of gastrointestinal nematodes in goat feces in the southeastern United States: dose titration and dose time interval studies. Vet Parasitol. 2004, 120: 285-296. 10.1016/j.vetpar.2003.09.024.
Paraud C, Hoste H, Lefrileux Y, Pommaret A, Paolini V, Pors I, Chartier C: Administration of Duddingtonia flagrans chlamydospores to goats to control gastro-intestinal nematodes: dose trials. Vet Res. 2005, 36: 157-166. 10.1051/vetres:2004060.
Kloosterman A, Parmentier HK, Ploeger HW: Breeding cattle and sheep for resistance to gastrointestinal nematodes. Parasitol Today. 1992, 8: 330-335. 10.1016/0169-4758(92)90066-B.
Woolaston RR, Baker RL: Prospects of breeding small ruminants for resistance to internal parasites. Int J Parasitol. 1996, 26: 845-855.
Bisset SA, Morris CA, McEwan JC, Vlassof A: Breeding sheep in New Zealand that are less reliant on anthelmintics to maintain health and productivity. N Z Vet J. 2001, 49: 236-246. 10.1080/00480169.2001.36238.
Kemper KE, Elwin RL, Bishop SC, Goddard ME, Woolaston RR: Haemonchus contortus and Trichostrongylus colubriformis did not adapt to long-term exposure to sheep that were genetically resistant or susceptible to nematode infections. Int J Parasitol. 2009, 39: 607-614. 10.1016/j.ijpara.2008.08.013.
Lynch M, Walsh B: Genetics and Analysis of Quantitative Traits. 1998, Sunderland: Sinauer Associates
Safari E, Fogarty NM, Gilmour AR: A review of genetic parameter estimates for wool, growth, meat and reproduction traits in sheep. Livest Prod Sci. 2005, 92: 271-289. 10.1016/j.livprodsci.2004.09.003.
Bishop SC, Bairden K, McKellar QA, Park M, Stear MJ: Genetic parameters for faecal egg count following mixed, natural, predominantly Ostertagia circumcinta infection and relationships with live weight in young lambs. Anim Sci. 1996, 63: 423-428. 10.1017/S1357729800015319.
McEwan JC, Dodds KG, Greer GJ, Bain WE, Duncan SJ, Wheeler R, Knowler KJ, Reid PJ, Green RS, Douch PGC: Genetic estimates for parasite resistance traits in sheep and their correlations with production traits. Proceeding of the 23rd New Zealand Society for Parasitology Conference. NZ J Zool. 1995, 22-177.
Eady SJ, Woolaston RR, Ponzoni RW, Lewer RP, Raadsma HW, Swan AA: Resistance to nematode parasites in Merino sheep: correlation with production traits. Aust J Agric Res. 1998, 49: 1201-1211. 10.1071/A98069.
McEwan JC, Mason P, Baker RL, Clarke JN, Hickey SM, Turner K: Effect of selection for productive traits on internal parasite resistance in sheep. Proc New Zeal Soc Anim Prod. 1992, 52: 53-56.
Bisset SA, Vlassoff A, Morris CA, Southey BR, Baker RL, Parker AGH: Heritability and genetic correlations among faecal egg counts and productivity traits in Romney sheep. NZ J Agric Res. 1992, 35: 51-58. 10.1080/00288233.1992.10417701.
Morris CA, Vlassoff A, Bissett SA, Baker RL, Watson TG, West CJ, Wheeler M: Continued selection of Romney sheep for resistance or susceptibility to nematode infection: estimates of direct and correlated responses. Anim Sci. 2000, 70: 17-27.
Walkden-Brown SW, Eady SJ: Nutritional influences on the expression of genotypic resistance to gastrointestinal nematode infection in sheep. Aust J Exp Agric. 2003, 42: 1445-1454.
Lee SH, Goddard ME, Visscher PM, van der Werf JHJ: Using the realized relationship matrix to disentangle confounding factors for the estimation of genetic variance components of complex traits. Genet Sel Evol. 2010, 42: 22-10.1186/1297-9686-42-22.
Sallé G, Jacquiet P, Gruner L, Cortet J, Sauvé C, Prévot F, Grisez C, Bergeaud JP, Schibler L, Tircazes A, Francois D, Pery C, Bouvier F, Thouly JC, Brunel JC, Legarra A, Elsen JM, Bouix J, Rupp R, Moreno CR: A genome scan for QTL affecting resistance to Haemonchus contortus in sheep. J Anim Sci. 2012, 90: 4690-4705. 10.2527/jas.2012-5121.
Lacroux C, Nguyen THC, Andreoletti O, Prevot F, Grisez C, Bergeaud J, Gruner L, Brunel JC, Francois D, Dorchies P, Jacquiet P: Haemonchus contortus (Nematoda: Trichostrongylidae) infection in lambs elicits an unequivocal Th2 immune response. Vet Res. 2006, 37: 607-622. 10.1051/vetres:2006022.
Raynaud JP: Study of the efficiency of a quantitative coproscopic technic for the routine diagnosis and control of parasitic infestations of cattle, sheep, horses and swine. Ann Parasitol Hum Comp. 1970, 45: 321-342.
Misztal I: Complex models, more data: simpler programming?.https://journal.interbull.org/index.php/ib/article/view/470/468,
Christensen OF: Compatibility of pedigree-based and marker-based relationship matrices for single-step genetic evaluation. Genet Sel Evol. 2012, 44: 37-10.1186/1297-9686-44-37.
Vitezica ZG, Aguilar I, Misztal I, Legarra A: Bias in genomic predictions for populations under selection. Genet Res. 2011, 93: 357-366. 10.1017/S001667231100022X.
Quaas RL: Computing the diagonal elements and inverse of a large numerator relationship matrix. Biometrics. 1976, 32: 949-953. 10.2307/2529279.
VanRaden PM: Efficient methods to compute genomic predictions. J Dairy Sci. 2008, 91: 4414-4423. 10.3168/jds.2007-0980.
Klei B: Approximate variance for heritability estimates.http://nce.ads.uga.edu/html/projects/AI_SE_revised.pdf,
Diaz-Francés E, Rubio FJ: On the existence of a normal approximation to the distribution of the ratio of two independent normal random variables. Stat Pap. 2013, 54: 309-323. 10.1007/s00362-012-0429-2.
Fisher RA: Frequency distribution of the values of the correlation coefficient in samples of an indefinitely large population. Biometrika. 1915, 10: 507-521.
Efron B, Tibshirani RJ: An Introduction to Bootstrap. 1993, New York: Chapman & Hall
Tizard IR: Veterinary immunology: an introduction. 2012, St. Louis: Elsevier
Greer AW: Trade-offs and benefits: implications of promoting a strong immunity to gastrointestinal parasites in sheep. Parasite Immunol. 2008, 30: 123-132. 10.1111/j.1365-3024.2008.00998.x.
Liu SM, Smith TL, Briegel J, Murray A, Masters DG, Karlsson LJE, Palmer DG, Greeff JC, Besier RB, Gao SB: Comparing productive performance of nematode resistant Merino sheep with non-selected control. Livest Prod Sci. 2005, 97: 117-129. 10.1016/j.livprodsci.2005.03.006.
Veerkamp RF, Mulder HA, Thompson R, Calus MP: Genomic and pedigree-based genetic parameters for scarcely recorded traits when some animals are genotyped. J Dairy Sci. 2011, 94: 4189-4197. 10.3168/jds.2011-4223.
Pollott GE, Greeff JC: Genotype X environment interactions and genetic parameters for fecal egg count and production traits of Merino sheep. J Anim Sci. 2004, 82: 2840-2851.
The reviewers of this article are acknowledged for their constructive comments and helpful suggestions. Dr Stephen Bishop is also acknowledged for contributing to the language review. This study was funded by a Marie Curie grant within the “NEMATODE SYSTEM HEALTH” project (FP7-PEOPLE-2010-ITN-ID:264639). The data set was available thanks to the technical staff at the farm La Sapinière and at the Nouzilly experimental unit, LABOGENA, the French Region Centre, the Animal Genetics department division of INRA, ANR, and APISGENE (SheepSNPQTL project, Toulouse, France) and EU grants (FEOGA 024/m/1873, Osmoy, France).
The authors declare that they have no competing interests.
FA edited the observations on average daily gain, estimated the genetic parameters and their standard errors, interpreted the results and wrote the manuscript. CR supervised the PhD project, helped with performing the statistical analysis and with the interpretation of its results and revised the manuscript. JME, AL and CRG helped with performing the statistical analysis, interpreting its results and revising the manuscript. CC programmed the Jackknife procedure in parallel and helped with the interpretation of the results and manuscript review. GS performed the data editing of both the observations on faecal egg counts and of SNP data, of results interpretation and manuscript review. All authors read and approved the final manuscript.
About this article
Cite this article
Assenza, F., Elsen, JM., Legarra, A. et al. Genetic parameters for growth and faecal worm egg count following Haemonchus contortus experimental infestations using pedigree and molecular information. Genet Sel Evol 46, 13 (2014). https://doi.org/10.1186/1297-9686-46-13
- Genetic Correlation
- Phenotypic Correlation
- Genetic Parameter
- Growth Trait
- Average Daily Gain