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Determination of genetic diversity using 15 simple sequence repeats markers in long term selected Japanese quail lines.

INTRODUCTION

Domestic quails, derived from the Japanese quail (Coturnixjaponica), as laying, meat, and laboratoiy animals have produced a flourishing industry in the world (Charati et al., 2014). At present there are about 1,050 million quails worldwide (Chang et al., 2007). Due to their known properties, quails have been widely used for biological and genetic studies (Alkan et al., 2013). Also, quail are considered an economically important avian species and provide an alternative to the more common chicken (Farrag etal.,2011).

Determination of the genetic diversity of domestic flocks is a necessity for providing needed information for the conservation of useful genotypes against future uncertainties such as global warming, diseases and humanitarian needs. Continued genetic improvement of livestock is dependent on the fact that substantial genetic variation exists within individual breeds allowing them to respond to selection for different traits (Farrag et al., 2011). Quantitative assessment of genetic diversity within and between populations is an important tool for decision making in genetic conservation plans (Davila et al., 2009).

Currently, many molecular marker methods have been developed to estimate genetic relatedness within and between livestock species. Microsatellites or simple sequence repeats (SSR) have emerged as one of the most popular genetic markers for a wide range of applications in population genetics, conservation biology, and evolutionaiy biology (Abdelkrim et al., 2009) and occur in both coding and non-coding regions of DNA. SSRs have high mutation rates and simple Mendelian inheritance which make them particularly suitable for the study of fine population structure, mating systems and pedigrees (Abdelkrim et al., 2009). Also, they are easy to genotype and are densely distributed throughout eukaiyotic genomes, making them the preferred genetic marker for high resolution genetic mapping (Babar et al., 2012). Recent information in literature has revealed that microsatellite markers are not only useful in determining heterozygosity and estimating genetic distances among closely related species (Chen et al., 2004), but also are now one of the most widely used molecular markers, due to their relative ease of scoring and high levels of polymorphism (Gomes et al., 2013).

Anatolia is a natural habitat for quail and on the migration route of quail flocks. There are also commercial enterprises producing quail, especially Japanese quail. Quail eggs and meat are consumed extensively in Turkey and quails are also grown as ornamental animals. Although there are many studies on quail breeding and genetics, sufficient genetic information has not yet been obtained in Turkey. The objective of the present study was to investigate genetic differences among long term selected five Japanese quail lines using 15 microsatellite markers and discussion of selection effects.

MATERIALS AND METHODS

Five Japanese quail (C. coturnix japonica) lines were obtained from the same base population. High body weight 1 (HBW1), low body weight (LBW), and layer (L) lines were selected for 15 generations according to 5-week high body weight, 5-week low body weight and 120 days egg yield, respectively. HBW2 line had been selected for 4-week high body weight for 7 generations. To see if different selection criteria and different generation numbers made differences on body weight, the selection studies of HBW2 was started after eight generations selection of other quail lines. Unselected control line was generated at same time the selection lines. The lines were established by applying individual selection with 10% and 40% selection intensity for males and females, respectively. Mating was random to minimize inbreeding.

A total of 69 individual birds from C (13), L (12), LBW (15), HBW1 (14), and HBW2 (15) representing five lines were used in this study. Approximately, 2 ml of blood was drawn from jugular vein into tubes treated with K3-ethylenediaminetetraacetic acid. Isolation of DNA from each line was performed using DNA Kit (Bio Basic Inc-SK252, Markham, ON, Canada). Each of the DNA samples was controlled by NanoDrop (ND 100) for quality and quantity. A set of fifteen SSR loci (GUJ0006_13_ 23_27_31_33_36_37_52_54_55_63_71_87_97) (Kayang et al., 2002) were chosen based on their degree of polymorphism for this study.

DNA amplification at polymerase chain reaction involved initial denaturation at 94[degrees]C (5 min) followed by 30 cycles of denaturation at 94[degrees]C (15 s), annealing at 55[degrees]C (15 s), extension at 72[degrees]C (15 s) and final extension at 72[degrees]C (20 min). Avolume of 15 [micro]L of reaction mixtures was prepared using 50 ng genomic DNA, 0.35 pmol/[micro]L primer mix, Ix buffer, 25 [micro]M dNTPs, 2.0 mM MgCh, 0.04 U Taq DNA polymerase (Apphed Biosystems, Waltham, MA, USA). Amplified DNAs were diluted by 1/10. Then, 12 [micro]L formamide and 0.5 [micro]L size marker (500 bp) were added to per 1 [micro]L DNA sample taken from diluted samples. This mix was used to determine genotypes by automatic sequencer (ABI PRISMA 310, Lincoln Centie Drive, Foster City, CA, USA). GeneMapper 4.0 (Apphed Biosystems, USA) was used to calling of SSR alleles.

POPGENE version 1.31 and CERVUS 3.0 (Kahnowski et al., 2007) package programs were used in the analysis of SSR genotypes data. Due to SSR markers showing co-dominant inheritance, a pattern counting method was used in the calculation of gene (allele) frequencies (Nei, 1987). Because allele number ([n.sub.a]), effective allele number ([n.sub.e]), observed heterozygosity ([H.sub.o]), expected heterozygosity ([H.sub.e]), polymorphism information content (PIC), F-statistics and genetic distance (D) are accepted as the standard in SSR studies, these were used in determination of genetic variation of quail lines. The molecular phylogenic tree (unweighted pair group method with arithmetic mean [UPGMA]) analysis was performed to estabhsh phylogenetic dendrogram. Genetic structure and the degree of admixture of quail lines were estimated using Bayesian clustering procedure of STRUCTURE 2.3 (Pritchard et al., 2000). First the program was run to assume the number of distinct populations defined as K. The analysis involved an admixture model with correlated allele frequencies. One hundred independent runs with 500,000 markov chain monte carlo iterations and a bum-in of 100,000 steps were performed for 2[less than or equal to]K[less than or equal to]8 (where K is the number of cluster to be tested) to estimate the most likely number of clusters present in the data set. The most plausible number of clusters was determined in the STRUCTURE HARVESTER (Earl and vonHoldt, 2012) by calculating the distribution of the [DELTA]K statistic as described by Evaimo et al. (2005). The clustering pattern was visuahsed using the software DISTRUCT I.I (Rosenberg, 2004).

RESULTS

All studied SSR loci were found to be polymorphic according to the results of the analysis over the quail genotypes used in this study. The lowest and highest Ho, He, and average heterozygosity (Ha) were estimated as 0.04 (GUJ0027) 0.64 (GUJ0087), 0.21 (GUJ0027), 0.84 (GUJ0037), and 0.20 (GUJ0027) 0.71 (GUJ0037), respectively (Supplementaiy Table SI, Supporting information). The [n.sub.a] were determined as 3.47 [+ or -] 1.06, 4.13 [+ or -] 1.60, 4.00 [+ or -] 1.20, 3.93 [+ or -] 1.33, and 3.97 [+ or -] 1.60 in C, L, LBW, HBW1, and HBW2, respectively, and the average of effective allele number ([n.sub.e]) was estimated as 3.26 [+ or -] 1.28 (Table 1). The average observed heterozygosity over all loci in the C was 0.33 [+ or -] 0.23 and found to be close to each other's (L, LBW, HBW1, and HBW2; Table 1). In this current study the PIC values ranged from 0.18 (GUJ0063) to 0.69 (GUJ0037) (Supplementaiy Table SI) and the average PIC values was calculated from overall loci as 0.50 [+ or -] 0.02 and ranged from 0.46 [+ or -] 0.20 (HBW2) to 0.52 [+ or -] 0.23 (L) (Table 1).

Average [F.sub.ST] (genetic divergence of subpopulations within the total population) value was estimated as 0.13 and varied between 0.06 (GUJ0027) and 0.20 (GUJ0023). Values of coefficient of inbreeding ([F.sub.IS]) were between 0.03 (GUJ0087) to 0.81 (GUJ0031), with an average of 0.43. The inbreeding coefficient ([F.sub.IT]) average 0.50 and varied between 0.08 (GUJ0087) and 0.83 (GUJ3I) in this study (Supplementaiy Table SI). [F.sub.is] values ranged from -0.171 to 1.000 for the loci within the quail lines. The [F.sub.is] values were calculated as relatively high positive and average [F.sub.is] values varied between 0.382 (HBW2) and 0.460 (LBW). Hardy-Weinberg test over all [F.sub.is] statistics demonstrated that the quail lines were not in equilibrium (Table 1). It can be understood that the homozygosity was increased due to selection pressure although there was random mating.

Genetic distance values (Table 2) were determined from 0.09 (between HBW1 and HBW2) to 0.33 (between C and L). UPGMA cluster analysis was also shown as a dendrogram in Figure 1. Lines of C, HBW1, and HBW2 completed the first main cluster, L and LBW lines completed the second cluster in this dendrogram.

It can be said that the 5 Japanese quail lines were separated clearly based on 15 microsatellite markers in Figure 2. However, they could not fully differentiated at the end of 15 generations of selection. It was understood from common colors in Figure 2 that quail lines still cany the same genomic structures from a common ancestor

DISCUSSION

When we examined the distribution of the alleles, we found that there were some differences in quail lines in terms of microsatellite alleles distribution. The average allele number over all loci was found to be 6.80 [+ or -] 2.21 (Table 1). This value could be informative for such studies according to Farrag et al. (2011) who suggested that the average number of alleles per locus in the genetic studies distances must be >4 to reduce the standard error in the estimation of genetic distances. Average allele number found in studies that were carried on different quail genotypes by Chang et al. (2007), Farrag et al. (2011), Tadano et al. (2014) and Bai et al. (2013) as 2.33 to 5.67, 5.39, 5.20, and 5.3, respectively. As clearly seen here we found a higher allele number The average of effective allele number ([n.sub.e]) was determined as 3.26 [+ or -] 1.28 in this study (Table 1). When the distribution of alleles belonging to entire microsatellite loci in quail lines was examined, it appears that differential breeding of these quail lines for 15 generations has favored some alleles of the microsatellite loci of interest while not favoring others.

If the mean [n.sub.e] is high, which is defined as the inverse of homozygosity (Nei, 1987), it is more likely to detect the possibility of any genetic variation. Theoretically when all existing allele frequencies in a population are the same, [n.sub.e] should be equal to the value of [n.sub.a]. But usually [n.sub.e] measure is estimated to be smaller than [n.sub.a]. In this study, effective number of alleles belonging to the locus of lines was found to be between 1.27 (GUJ0027) and 6.09 (GUJ0037). The number of effective alleles were reported between 1.O and 4.3 by Kayang et al. (2002), between 1.0 and 5.4 by Chang et al. (2007) and 4.03 by Bai et al. (2013).

When all of the working 15 microsatellite markers were analyzed, there were differences in expected and observed heterozygosity for some loci. It was found that expected and observed heterozygosity were lowest in loci GUJ002, but highest in GUJ0087 and GUJ0037 (Supplementary Table SI). Although the average observed heterozygosity values in all populations were lower than the average expected heterozygosity values (Table I), there was not a significant difference between the lines in terms of the average observed heterozygosity values.

In a study performed by Chang et al. (2007) they reported higher heterozygosis values than reported here except for one microsatellite locus. Kayang et al. (2002) declared that observed, expected and average heterozygosis were as 0.00, 0.95, and 0.42 in Japanese quail, respectively. Also, the mean Ho was 0.609 and ranged across loci from 0.00 to 0.967 whereas the mean He was 0.636 and ranged between 0.139 and 0.802 in three Japanese quail strains (Farrag et al., 2011). Four Japanese quail strains were studied by using eight SSR loci and the expected heterozygosis varied between 0.708 and 0.849 (Amirinia et al., 2007). [H.sub.o] and [H.sub.e] per locus ranged from 0.00 to 0.54, and 0.12 to 0.80 (Tadano et al., 2014) and found as 0.63 and 0.60 (Gruszczynska and Michalska, 2013), respectively. Also, expected heterozygosity was estimated as 0.73 in wild quail and 0.23 in Japanese quail (Ahmad et al., 2014).

When PIC values were examined, it was seen that a substantial portion of working locus markers provided information at a high level. When Table I was analyzed in terms of PIC value, it was observed that there was a difference among quail lines. This value could be stated as higher than 0.477 (Kayang et al., 2002), but lower than 0.57 (Chang et al., 2007), 0.64 (Farrag et al., 2011), and 0.69 (Bai et al., 2013). Also, Tadano et al. (2014) reported that of 49 polymorphic microsatellite markers, 55.1% were highly informative (PIC[greater than or equal to]0.50), 28.6% were reasonably informative (0.50>PIC>0.25) and 16.3% were slightly informative (PIC [less than or equal to]0.25) according to Botstein et al. (1980) criteria. Gruszczynska and Michalska (2013) also found mean PIC value as 0.54.

In our study the value of [F.sub.ST] was found as 0.13 within existing quail lines with respect to the microsatellite loci. According to definitions of Hartl and Clark (1997) this result can be interpreted as indicating a genetic differentiation among quail lines. There was 13% total genetic variation between quail lines and the remaining 87% genetic variation was due to differences within lines. [F.sub.ST] was estimated for per locus from 0.22 to 0.92 and between each pair of lines ranged from 0.3 to 0.83 (Tadano et al., 2014). Values of [F.sub.IS] were between 0.03 (GUJ0087) and 0.81 (GUJ003I), the average of which was 0.43. [F.sub.IS] values were estimated O.IO and 0.13 by Kim et al. (2007), 0.03 and 0.29 Chang et al. (2007). The inbreeding coefficient ([F.sub.IT]) was average 0.50 and varied between 0.08 (GUJ0087) and 0.83 (GUJ3I) in this study. Kim et al. (2007) reported similar Fn as 0.57 [+ or -] 0.33 in the I7th generation of inbred line using 14 microsatellite markers. HBWI and HBW2, which were selected in terms of higher body weight at 5 weeks for HBWI and at 4 weeks for HBW2, were in the same cluster with some exceptions. The lowest genetic distance was found as 0.09 between HBW1 and HBW2 (Table 2). Chang et al. (2007) reported lower genetic distances (0.01 to 0.04) than found in this study (0.09 to 0.33). In another study, genetic diversity was ranged from O.IO to 0.60 in 13 Japanese quail lines (Tadano et al., 2014).

The result of cluster analysis of 5 quail lines showed two main clusters (Figure 2). Cluster analysis largely realized our expectations regarding to genetic distance between quail lines. Namely, L line which were selected regarding to egg production was the most divergent one (Figure 2). HBW1 and HBW2 lines clustered on the same branch of the phylogenetic tree and these two lines can be evaluated as an indicator for the associated genes.

As expected, the number of clusters was found to be same as the number of the studied lines which was five as seen in Figure 2. Most of the individuals were visualized within their own clusters. However, it is clear that they still carry common genetic markers. Moreover, this genetic frame reflects what we found among the individuals genetic diversity. In a similar study, Tadano et al. (2014) demonstrated successful high genetic differentiation among 13 Japanese quail lines using Bayesian clustering (K = 13).

CONCLUSION

The selection made in different directions had separated the genotypes from each other to a certain extent. This result is consistent with the fact that the 5 quail lines studied here came from a common population and to obtain genetically unique lines selection needed to be applied for more generations and/or more markers must be used. However, this study would be helpful to support further selection studies using similar methodology. Also, we can say microsatellite markers can be effectively used for genetic characterization of selected quail lines.

CONFLICT OF INTEREST

We certify that there is no conflict of interest with any financial organization regarding the material discussed in the manuscript.

ACKNOWLEDGMENTS

Selection experiments and molecular studies were supported by Akdeniz University Scientific Research Project Coordination Unit and TUBITAK (The Scientific and Technological Research Council of Turkey), respectively.

http://dx.doi.org/10.5713/ajas. 15.0940

Submitted Nov. 19, 2015; Revised Feb. 15, 2016; Accepted Apr. 2, 2016

REFERENCES

Abdelkrim, J., B. C. Robertson, J. A. L. Stanton, and N. J. Gemmell. 2009. Fast, cost-effective development of species-specific microsatellite markers by genomic sequencing. Biotechniques 46:185-192.

Ahmad, A., 1. Zahoor, M. Akram, M. E. Babar, and A. Basheer 2014. Evaluation of genetic diversity within and between the quail breeds in Pakistan. Sci. Int. 26:1175-1179.

Alkan, S., T Karsli, K. Karabag, A. Galic, and M. S. Balcioglu. 2013. The effects of thermal manipulation during early and late embryogenesis on hatchability, hatching weight and body weight in Japanese quails (Cotumix cotumix japonica). Arc. Tierz. 56:789-796.

Amirinia, C., H. Emrani, M. A. R. Arbabe, R. V. Torshizi, and A. N. Javaremi. 2007. Evaluation of eight microsatellite loci polymorphism in four Japanese quail (Cotumixjaponica) strain in Iran. Pak. J. BioL Sci. 10:1195-1199.

Babar, M. E., A. Nadeem, T. Hussain, A. Wajid, S. A. Shah, A. Iqbal, Z. Sarfraz, and M. Akram. 2012. Microsatellite marker based genetic diversity among four varieties of Pakistan Aseel chicken. Pak. Vet. J. 32:237-241.

Bai, Y. J., Y. Z. Pang, S. J. Wu, M. Q. Yu, X. H. Zhang, S. J. Zhao, andH. W. Xu. 2013. Polymorphism Analysis of Chinese yellow quail using microsatellite markers. J. Anim. Plant Sci. 23:1072-1076.

Botstein, D., R. L. White, M. Skohiik, and R. W. Davis. 1980. Construction of a genetic linkage map in man using restriction fragment length polymorphisms. Am. J. Hum. Genet. 32:314-331.

Chang, G. B., H. Chang, X. P Liu, W. M. Zhao, D. J. Ji, Y. J. Mao, G. H. Song, and X. K. Shi. 2007. Genetic diversity of wild quail in China ascertained with microsatellite DNA markers. Asian Australas. J. Anim. Sci. 20:1783-1790.

Charati, H., A. E. Koshkoiyeh, R. J. Ori, H. Moradian, and A. A. Menrgardi. 2014. Detection of quantitative trait loci affecting carcass traits and internal organs on chromosome 3 in an F2 intercross of Japanese quail. Anim. Sci. Pap. Rep. 32:369-383.

Chen, G. H., X. S. Wu, D. Q. Wang, J. Qin, S. L. Wu, Q. L. Zhou, F. Xie, R. Cheng, Q. Xu, B. Liu, X. Y. Zhang, and O. Olowofeso. 2004. Cluster analysis of 12 Chinese native chicken populations using microsatellite markers. Asian Australas. J. Anim. Sci. 17:1047-1052.

Davila, S. G., M. G. Gil, P Resino-Talavan, and J. L. Campo. 2009. Evaluation of diversity between different Spanish chicken breeds, a tester line and a White Leghorn population based on microsatellite markers. Poult. Sci. 88:2518-2525.

Earl, D. A. and B. M. vonHoldt. 2012. STRUCTURE HARVESTER: A website and program for visualizing STRUCTURE output and implementing the Evanno method. Conserv Genet. Resour 4:359-361.

Evanno, G., S. Regnaut, and J. Goudet. 2005. Detecting the number of cluster of individuals using the software STRUCTURE: a simulation study. Mol. Ecol. 14:2611-2620.

Farrag, S. A., A. B. Tanatarov, M. E. Soltan, M. Ismail, and O. M. Zayed. 2011. Microsatellite analysis of genetic diversity in three populations of Japanese quail {Cotumix cotumix japonica) from Kazakhstan. J. Anim. Vet. Adv 10:2376-2383.

Gomes, M. L., T. Haranaka, W. N. deCampos, and A. P. Wasko. 2013. Assessing paternity in Japanese quails {Cotumix Japonica) using microsatellite markers-inferences for its mating system and reproductive success. Rev. Bras. Cienc. Avic. 15:329-338.

Gruszczynska, J. and E. Michalska. 2013. Application of chicken microsatellite markers to molecular monitoring of the experimental population of Japanese quail (Cotumix japonica). Anim. Sci. Pap. Rep. 31:73-84.

Hartl, D. L. and A. G. Clark. 1997. Principles of Population Genetics. 3rd edn. Sinauer Associates, Inc. Publishers, Sunderland, MA, USA.

Kalinowski, S. T, M. L. Taper, and T C. Marshall. 2007. Revising how to computer program CERVUS accommodates genotyping error increases success in paternity assignment. Mol. Ecol. 16:1099-1106.

Kayang, B. B., M. Inoue-Murayama. T. Hoshi, K. Matsuo, H. Takahashi, M. Minezawa, M. Mizutani, and S. Ito. 2002. Microsatellite loci in Japanese quail and cross-species amplification in chicken and guinea fowl. Genet. Sel. Evol. 34:233-253.

Kim, S. H., K. M. T. Cheng, C. Ritland, K. Ritland, and F. G. Silversides. 2007. Inbreeding in Japanese quail estimated by pedigree and microsatellite analyses. J. Hered. 98:378-381.

Nei, M. 1987. Molecular Evolutionary Genetics. Columbia University Press, NY, USA.

Pritchard, J. K., M. Stephens, and P Donnelly. 2000. Inference of population structure using multilocus genotype data. Genetics 155:945-959.

Rosenberg, N. A. 2004. Distruct: A program for the graphical display of population structure. Mol. Ecol. Notes 4:137-138.

Tadano, R., M. Nunome, M. Mizutani, R. Kawahara-Miki, A. Fujiwara, S. Takahashi, T. Kawashima, K. Nirasawa, T. Ono, T. Y. Kono, and Y. Matsuda. 2014. Cost-effective development of highly polymorphic microsatellite in Japanese quail facilitated by next-generation sequencing. Anim. Genet. 45:881-884.

Kemal Karabag *, Murat Soner Balcioglu (1) Taki Karli (1) and Sezai Alkan (2) Department of Agricultural Biotechnology, Faculty of Agriculture, Akdeniz University, Antalya 07058, Turkey (1) Department of Animal Science, Faculty of Agriculture, Akdeniz University, Antalya 07058, Turkey. (2) Department of Animal Science, Faculty of Agriculture, Ordu University, Ordu 52200, Turkey.

* Corresponding Author: Kemal Karabag. Tel: +90-242-3102506, Fax: +90-242-2274564, E-mail: karabag@akdeniz.edu.tr

Caption: Figure 1. Phylogenetic distance among the studied quail lines by neighbor-joining method.

Caption: Figure 2. Bayesian model-based clustering (K = 7) analyses of the studied quail individuals. Each individual was represented by a vertical bar. Each color corresponds to one cluster, and the length of the colored segment represents the individual's membership coefficient in the cluster according to cluster analysis the highest AK value (44.13) was obtained for Bayesian model-based clustering (K = 7) analyses of the studied quail individuals.
Table 1. Polymorphism information for all quail lines according to
studied SSR loci in this study

                     C                    L

N                    26                   24
[n.sub.a]    3.47 [+ or -] 1.06   4.13 [+ or -] 1.60
[n.sub.e]    2.46 [+ or -] 0.61   2.76 [+ or -] 1.27
PIC          0.50 [+ or -] 0.12   0.52 [+ or -] 0.23
[H.sub.o]    0.33 [+ or -] 0.23   0.30 [+ or -] 0.24
[H.sub.e]    0.57 [+ or -] 0.11   0.58 [+ or -] 0.24
[F.sub.is]         0.418                0.454
[P.sub.p]          100.00               93.33
[N.sub.p]            15                   14

                    LBW                  HBW1

N                    30                   28
[n.sub.a]    4.00 [+ or -] 1.20   3.93 [+ or -] 1.33
[n.sub.e]    2.75 [+ or -] 1.12   2.66 [+ or -] 0.93
PIC          0.50 [+ or -] 0.22   0.51 [+ or -] 0.20
[H.sub.o]    0.30 [+ or -] 0.20   0.32 [+ or -] 0.22
[H.sub.e]    0.58 [+ or -] 0.23   0.56 [+ or -] 0.21
[F.sub.is]         0.460                0.408
[P.sub.p]          100.00               100.00
[N.sub.p]            15                   15

                    HBW2                 Mean

N                    30                  27.6
[n.sub.a]    3.97 [+ or -] 1.60   6.80 [+ or -] 2.21
[n.sub.e]    2.40 [+ or -] 0.80   3.26 [+ or -] 1.28
PIC          0.46 [+ or -] 0.20   0.50 [+ or -] 0.02
[H.sub.o]    0.33 [+ or -] 0.20   0.32 [+ or -] 0.17
[H.sub.e]    0.52 [+ or -] 0.21   0.36 [+ or -] 0.19
[F.sub.is]         0.382                  -
[P.sub.p]          93.33                 100
[N.sub.p]            14                   15

SSR, simple sequence repeats; C, control; L, layer; LBW,
low body weight; HBW1, high body weight 1; HBW2, high body
weight 2; N, loci number; [n.sub.a], number of observed
alleles; [n.sub.e], effective allele number; PIC,
polymorphic information content; [H.sub.o], observed
heterozygosis; [H.sub.e], expected heterozygosis; [P.sub.p],
polymorphic loci ratio; [N.sub.p], the number of
polymorphic loci; [F.sub.is], coefficient of inbreeding.

Table 2. Similarities of the studied quail lines in the genetic
distance (lower diagonal)

        C      L     LBW    HBW1   HBW2

C             0.72   0.76   0.81   0.81
L      0.33          0.82   0.77   0.78
LBW    0.28   0.20          0.77   0.76
HBW1   0.21   0.26   0.26          0.92
HBW2   0.21   0.33   0.27   0.09

C, control; L, layer; LBW, low body weight; HBW1, high body weight 1;
HBW2, high body weight 2.
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Author:Karabag, Kemal; Balcioglu, Murat Soner; Karli, Taki; Alkan, Sezai
Publication:Asian - Australasian Journal of Animal Sciences
Article Type:Report
Date:Dec 1, 2016
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