Estimation
of Genetic Parameters and Breeding Values of Milk Yield
Using Test Day Model with Cubic Splines and Legendre Polynomials in Chinese
Holstein Cattle
Wan Lv1,2†,
Gaozhan Cai1†, Yujiao Wang2, Xianguo Gu3,
Xiuxin Zhao1, Xiaotao Liu3, Rongling Li1, Minghai
Hou1 and Jianbin Li1*
1Dairy Cattle Research Center of Shandong Academy
of Agricultural Sciences, Jinan 250100, China
2Department of College of Life Sciences and Food
Engineering, Hebei University of Engineering, Handan 056001, China
3Ningbo Milk Group Co., Ltd, Ningbo, 315033, China
*For correspondence: msdljb@163.com
Received 01 September 2020;
Accepted 26 September 2020; Published 10 January 2021
†These authors contributed equally to this work.
Abstract
This study aimed to estimate the
genetic parameters and breeding values of milk yield traits of Holstein cows in
Shandong Province using the best model identified by a comparison between a
numbers of alternative random regression test day models (RRMs). The data included 585,702 test day
records of milk yield in the first lactation of 88,215 Holstein cows, covering
219 cattle farms in Shandong Province during the period from 2005 to 2016.
Different models were investigated, which differed in the number of knots of
Spline functions to improve the fitting of population lactation curve and in
orders (2, 3, or 4) of Legendre polynomials to fit additive genetic effect and
permanent environmental effect. The optimal test day model was screened out by
Akaike information criterion (AIC) and Bayesian information criterion (BIC)
criteria. Detailed analysis of genetic parameters and accuracy of
estimation of breeding values were performed using the optimal model. In the
results, the optimal model (Sp15-La4-Lp3) for analyzing the milk yield data was
the one with 15 knots of Splines, 4 orders of Legendre polynomials for additive
genetic effect and 3 orders of Legendre polynomials for permanent environmental
effect. Using the optimal model, estimates of additive genetic variances of
milk yield at different days in milk (DIM) during the whole lactation ranged
from 8.54 to 15.39, the permanent environmental variance ranged from 17.65 to
31.42. Correspondingly, the heritability ranged from 0.20 to 0.30, and repeatability
ranged from 0.43 to 0.54. Rank correlations between EBV of bull with different number of
daughters and the bull’s parent average ranged from 0.79 to 0.94, and the
correlations between EBV of bulls and the sire-maternal grandsire index ranged
from 0.48 to 0.86. In conclusion, Sp15-La4-Lp3
could be the optimal model for estimation of genetic parameters and prediction
of breeding values of milk in Shandong Holstein population. The amount of
progeny information is critical to the conventional genetic evaluation of
bulls. © 2021 Friends Science Publishers
Keywords: Genetic parameter; Holstein cattle; Milk yield;
Random regression model
Data for test day milk of dairy cows were
classically longitudinal or repeated measurements and there is a correlation
between the test day records of the same animals (White et al. 1999). The test day model (TDM) was an alternative to the
traditional genetic assessment model. The traditional genetic evaluation
model required the conversion of multiple test day records during a lactation
period to a standard milk yield of 305-d. The test day model could provide some
advantages compared to traditional models. The test day model directly took
each test day record into genetic evaluation, and does not need to convert it
into lactation record, which reduced the error in calculation of the cumulative
lactation record. In addition, the test day model allowed to account for the
difference of genes and gene effects on milk production in different lactation
periods. Thus, the test day model could improve the accuracy of genetic
evaluation. Several types of test day model had been proposed, such as
multiple-trait reduced rank model (Meseret et al. 2015), repeatability
model (Behzadi and Mehrpoor 2018), covariance function model (Kirkpatrick et
al. 1994) and random regression model (Schaeffer 1994).
A random regression model (RRM)
with a polynomial or other simple function was increasingly being used by
animal breeders (Jamrozik and Schaeffer 1997; Meyer
and Hill 1997). When the lactation curve was fitted by random
regression model, the random effect part of the model usually adopted Legendre
polynomial as covariates (Kirkpatrick et al. 1994). According to Meyer
(2005), changed in variance along a continuous scale,
in general, could be well modeled by high-order Legendre polynomials, but these polynomials might have an over-fitting phenomenon
at the beginning and end of the trajectory. Segmented Polynomials (Splines)
could be used to replace higher order Legendre Polynomials. In
Spline regression model, lactation curve was described through a series of
specific points (knots). Each segment composed of node connections was part of
a low-order polynomial. Cubic smooth Splines could be inlaid in hybrid model frames (Lin
et al. 2020). Cubic Spline function was a smooth curve
formed by piecewise cubic interpolation multinomial. The
first and second derivatives on the curve were continuous (Wan et al.
2018).
In the study of RRM in dairy cattle, Legendre
Polynomials and Splines were rarely used to estimate additive genetic effects
and permanent environmental effects. Silvestre et al. (2005) estimated the genetic
parameters of milk, fat and protein yields of Portuguese cows by using a test
day model with uniform Spline of 12 knots. Pereira et al. (2012) compared RRM with Legendre
polynomial to that with linear Spline function based on milk yield records of
purebred dairy Gyr (Bos indicus) and hybrid cows (dairy Gyr × Holstein), and
found that the linear Spline function model with 6 knots has the best fitting
to the data. Pool and Meuwissen (1999) compared different
TDM for their ability to fit lactation curve of milk yield, the
result showed that the TDM with Legendre polynomial of order 5 was most
suitable for the evaluation of breeding value. Bohmanova et
al. (2008) compared four RRM based on either Legendre polynomials of order
4 or linear Splines of 4, 5, or 6 knots, and
concluded that those RRMs tended to be o overestimate the additive genetic
variance at both ends of the fitting trajectory. However, in the model inlaid
with Spline, the overestimation was smaller, and the Spline with 6 knots had
the best fitting to the data based on the model comparison criterion.
Lots of milk records have been collected in Chinese
dairy herds, so genetic parameters should be updated regularly and Genetic
evaluation should be performed timely. Moreover, it has not been found
investigating the impact of Spline founction on genetic evaluation in Chinese
Holstein population. This study was in order to compare RRMs with different
knots of cubic Spline function and different orders of Legendre polynomial for
estimation of genetic parameters and prediction of breeding value in Chinese
Holstein population, using test day records of milk yield.
Data were obtained from Dairy Cattle Research
Centre DHI Lab, Shandong Academy of Agricultural Sciences.
The
data included 585, 702 test day records of milk yield in the first lactation of
88, 215 Holstein cows, covering 219 cattle farms in Shandong Province during
the period from 2005 to 2016. Data quality control
was performed using criteria: DIM between 5 and 305, calving ages
from 22 to 38 months, daily milk yield from 5 to 80 kg and cows with at least 3
records. The pedigree was traced back 3
generations, resulting in a pedigree file containing 193,156 animals. The
general statistics of the data were shown in Table 1.
The data were analyzed using RRM embedded with
Legendre polynomials and cubic Spline functions. The fixed effects of the RRM
include Herd-Year-Season (HYS), days in milk and calving age. Random effects
include cubic Spline knots effect, additive genetic effect and permanent
environmental effect. The calving age was divided into four groups:
age ≤ 24 months, 24 < age ≤ 28 months, 28 < age ≤ 32
months, and age ≥ 32 months. Residual variances in different lactation
period were assumed to be heterogeneous with 10 classes of residual variances (5–34,
35–64, 65–94, 95–124, 125–154, 155–184, 185–214, 215–244, 245–274, and 275–305
DIM).
The model can be written as
Where was
the test day record ; was
the effect of Herd-Year-Season; was
the effect of days in milk; was
the effect of calving age, was
the random regression coefficient on cubic Splines to improve the fitting of
population lactation curve; and were the random regression coefficient of
additive genetic effect and permanent environmental effect, respectively; was
Legendre Polynomial; and were order of Legendre polynomials of
additive genetic effect and permanent environmental effect, respectively; and was
residual effect. In matrix notation:
Where was
the vector of observation; was
the vector of fixed effect; was
the vector of the random regression coefficient of additive genetic effect. s was the vector of cubic Spline random
regressions coefficient;was the vector of random regression
coefficient of permanent environmental effect; , T,
, and were
incidence matrices corresponding to fixed effect, additive genetic, and
permanent environmental effect, respectively; and e was the vector of residual effects.
The variance of , s, and was:
The additive genetic and permanent environmental
effects were fitted by Legendre polynomials, and the order of Legendre
polynomials is 2, 3 or 4. The random effects in the model also included cubic
Spline functions of ns knots that were evenly spaced
throughout the lactation period. Firstly, the model combines the cubic Splines of 20 knots with
Legendre polynomials of different orders for empirical
selection of optimal order of Legendre polynomials, so the model was
run 9 times for 9 order combinations (3 for additive genetics × 3 for permanent
environment) at the Splines of 20 knots. The best order combination of these
nine models was selected using AIC and BIC criterion.
Then the data were analyzed using the models with the best order combination
together with different (4, 5, 6, 7, 10, 15, 25, 30) knots for Spline
functions. These models were evaluated using AIC and BIC criterion
to obtain the model with best combination of number of knots for Spline
functions and number of orders for Legendre polynomials.
As mentioned above, the models with different
knots of Splines and different orders of Legendre polynomial were evaluated
using AIC and BIC.
Akaike
information criterion (AIC) (Akaike 1974):
Where L is the maximum of the restricted
likelihood function; P is the number of parameters in the model.
Bayesian
Information Criterion (BIC) (Schwarz 1978):
Where L is the maximum of the
restricted likelihood function; P is the number of parameters in the model; n is the degree of freedom of the residuals.
When the model converges, lower AIC and BIC are preferred.
Estimation of additive genetic and
permanent environmental variance:
Where G
is the covariance (COV) matrix between the random regression coefficients of
additive genetic effects; P is the
COV matrix between the random regression coefficients of permanent
environmental effects; is the
coefficient matrix of the Legendre polynomial. Different models were carried
out for the estimation of covariance components and prediction of breeding
values by the DMU package. Estimation of heritability:
,
Where is the
heritability of the i-th test day, is the
additive genetic variance of the i-th
test day, and is the permanent environmental variance of
the i-th test day. is the
residual variance of the i-th test day which is the residual variance of
the residual group the test day belongs to, and the range of i is i
= 5, 6, 7...305. Estimation of repeatability:
Where is
repeatability, that means ratio of permanent environment of variance to
phenotypic variance at i-th test day,
, and were
same as above. Estimation of breeding value:
Where EBV is the matrix of EBV for each individual
(row) at each test day (column), A
is the random regression coefficient matrix of each order (column) and each
individual (row) for additive genetic effect estimated by the above model and is the
transposed coefficient matrix of the Legendre polynomials of each order (row)
and each test day (column). The breeding value of lactation milk yield for each
individual can be obtained by adding up the EBV of each test day.
The importance of daughter records for accuracy of
bull EBV was assessed with correlation (r) between bull’s EBV of 305 d milk
yield (EBV305) and the pedigree index. The correlation is equivalent
to the ratio of accuracy of pedigree index to accuracy of bull EBV. The
contribution of daughter records to accuracy can be measured as (1-r)/r. In
this study, Spearman Rank Correlation (Zar 2004) was used.
Where, was rank correlation coefficient, was the rank difference of individual
breeding value and pedigree index, and was
the number of individual.
In this section, we present the results of model
comparison. The abbreviations of different models had the form of Spx-Lay-Lpz,
where Spx is the number of Spline knots, Lay is the Legendre polynomial orders
to fit additive genetic effect, Lpz is Legendre polynomial orders to fit
permanent environmental effect.
Results of the models with the same 20 knots of
Spline and different Legendre polynomials orders were shown in Table 2, where Sp20-LA3-LP4 and Sp20-La4-Lp4 did not converge. Given the Spline with 20 knots and
different orders of Legendre polynomials, Sp20-La4-Lp3
had the smallest AIC and BIC values, compared to all other converged models,
indicating that this model had a better fit to the data than other models. It
suggested that Legendre polynomials of order 4 werer optimal for additive
genetic effect, and the Legendre polynomial of order 3 was optimal for
permanent environmental effect, given the Splines with 20 knots.
Table 3 present AIC and BIC for
models with different numbers of Spline knots and the selected optimal Legendre
polynomial orders, La4-Lp3. All the models in Table 3 converged, in
which Sp15-La4-Lp3 showed a minimum value of AIC and BIC, indicating
that this model fitted data better than other models. In other words, 15 knots
for Splines was the optimal, given La4-Lp3.
Fig. 1 shows a large difference in heritability of
test day milk yield between models with 20 Spline knots but different orders of
Legendre polynomials. It was observed that the heritabilities estimated by all
the models changed over DIM of lactation and appeared a curve with multiple
inflections. The number of inflection points of the
heritability curves increased with the order of Legendre polynomials, and thus
the inflection points on DIM were different in the heritability curve among the
different models. The curve amplitude of SP20-La4-Lp3
was smaller than the other model curves, indicating more smooth change in
estimated heritability over DIM. The heritabilities estimated using Sp20-La4-Lp3 ranged from 0.20 to 0.30.
The estimated heritabilities from the models with
the same order of Legendre polynomials (La4-Lp3) but different number of Spline
knots were almost the same in each DIM. The small difference was observed only
in the early
lactation period. The estimated heritabilities from Sp4-La4-Lp3 and SP5-La4-LP3 ranged from 0.19 to 0.30 and
those of the other models ranged from 0.20 to 0.30.
Table 1: Descriptive statistics of the test
day record data
Item |
Milk |
Min (kg) |
5.00 |
Max (kg) |
79.94 |
Number of Records |
585702 |
Average Yield (kg) |
24.37 |
Standard Deviation |
8.28 |
0.34 |
Table 2: AIC, BIC statistics of the models
with the same 20 knots of Splines and different orders of Legendre polynomials
Model |
Spl1 |
La |
Lp |
NP2 |
AIC |
BIC |
Converged |
Sp20-La2-Lp2 |
20 |
2 |
2 |
23 |
2499477.24 |
2499736.58 |
YES |
20-2-3 |
20 |
2 |
3 |
27 |
2494655.40 |
2494959.84 |
YES |
20-2-4 |
20 |
2 |
4 |
32 |
2492389.73 |
2492750.55 |
YES |
20-3-2 |
20 |
3 |
2 |
27 |
2494417.48 |
2494721.92 |
YES |
20-3-3 |
20 |
3 |
3 |
31 |
2494023.97 |
2494373.51 |
YES |
20-3-4 |
20 |
3 |
4 |
36 |
2491800.03 |
2492205.95 |
NO |
20-4-2 |
20 |
4 |
2 |
32 |
2492099.31 |
2492460.12 |
YES |
20-4-3 |
20 |
4 |
3 |
36 |
2491639.53 |
2492045.45 |
YES |
20-4-4 |
20 |
4 |
4 |
41 |
2491325.28 |
2491787.58 |
NO |
Define superscript 1 and 2
Table 3: AIC, BIC value of models with
different knots of Splines but the same order of Legendre polynomials
Model |
P1 |
AIC |
BIC |
Converged |
36 |
2492851.09 |
2493257.01 |
YES |
|
5-4-3 |
36 |
2492656.54 |
2493062.46 |
YES |
6-4-3 |
36 |
2492388.14 |
2492794.06 |
YES |
7-4-3 |
36 |
2492208.63 |
2492614.55 |
YES |
10-4-3 |
36 |
2491675.78 |
2492081.7 |
YES |
15-4-3 |
36 |
2491632.29 |
2492038.21 |
YES |
25-4-3 |
36 |
2491643.55 |
2492049.47 |
YES |
30-4-3 |
36 |
2491642.64 |
2492048.56 |
YES |
1P=number of parameters; AIC =
Akaike information criterion; BIC=Bayesian Information Criterion;
Converged=Model converge
Fig. 1: Heritabilities of milk yield at
different DIMs, estimated using the models with 20 knots of Splines and
different orders of Legendre polynomials
The additive genetic variances, permanent
environmental variances, phenotypic variances of test day milk yield estimated
by the optimal model are shown in Table 4. The additive genetic variance was higher at
DIM 5–65 and DIM 275–305 than the DIMs in the middle lactation. The permanent
environmental variance was higher at DIM 5(22.48) and DIM 305(31.42)
than the DIMs at the middle lactation. The phenotypic
variance was higher at DIM 5(51.67) and DIM 305(57.72) than the DIM at the
middle lactation. The estimated heritability was the highest (0.30) at DIM5 and
the lowest (0.20) at DIM 215. The estimated repeatbilities was the highest
(0.54) at DIM305 and the lowest (0.43) at DIM35.
Table 4: Additive genetic variance,
permanent environmental variance, phenotypic variance, heritability, and the
ratio of permanent variance to phenotypic variance at different DIMs, estimated
from the optimal model (Sp15-La4-Lp3) optimal model
DIM1 |
Milk |
||||
σa2 |
σPE2 |
σp2 |
h2 |
PE2 |
|
5 |
15.39 |
22.48 |
51.67 |
0.30 |
0.44 |
35 |
9.41 |
17.73 |
40.94 |
0.23 |
0.43 |
65 |
11.04 |
18.63 |
40.94 |
0.25 |
0.43 |
95 |
9.74 |
19.67 |
43.21 |
0.23 |
0.46 |
125 |
8.90 |
19.42 |
42.12 |
0.21 |
0.46 |
155 |
9.28 |
19.02 |
42.10 |
0.22 |
0.45 |
185 |
9.11 |
19.56 |
42.47 |
0.21 |
0.46 |
215 |
8.54 |
21.01 |
43.35 |
0.20 |
0.48 |
245 |
9.70 |
22.50 |
46.00 |
0.21 |
0.49 |
275 |
12.18 |
23.97 |
49.96 |
0.24 |
0.48 |
305 |
12.50 |
31.42 |
57.72 |
0.22 |
0.54 |
1DIM=Days in milk; AG=additive
genetic variance; PE=permanent environmental variance;
P=phenotypic variance; h2=heritability; REP =repeatability
Table 5: Genetic correlation (below
diagonal) and phenotypic correlation (above diagonal) between different DIM
milk yields
|
DIM |
5 |
30 |
60 |
90 |
120 |
150 |
180 |
210 |
240 |
270 |
305 |
|
5 |
… |
0.55 |
0.34 |
0.25 |
0.25 |
0.21 |
0.20 |
0.20 |
0.15 |
0.10 |
0.06 |
|
30 |
0.60 |
… |
0.61 |
0.53 |
0.44 |
0.36 |
0.30 |
0.27 |
0.25 |
0.22 |
0.14 |
|
60 |
0.16 |
0.87 |
… |
0.65 |
0.65 |
0.47 |
0.39 |
0.34 |
0.31 |
0.28 |
0.20 |
|
90 |
0.16 |
0.69 |
0.93 |
… |
0.65 |
0.65 |
0.50 |
0.50 |
0.37 |
0.32 |
0.25 |
|
120 |
0.01 |
0.69 |
0.71 |
0.91 |
… |
0.65 |
0.59 |
0.52 |
0.44 |
0.37 |
0.30 |
Milk |
150 |
0.01 |
0.24 |
0.47 |
0.74 |
0.95 |
… |
0.65 |
0.60 |
0.52 |
0.43 |
0.35 |
|
180 |
0.05 |
0.17 |
0.47 |
0.63 |
0.88 |
0.98 |
… |
0.66 |
0.59 |
0.59 |
0.41 |
|
210 |
0.02 |
0.23 |
0.47 |
0.62 |
0.80 |
0.88 |
0.95 |
… |
0.66 |
0.61 |
0.49 |
|
240 |
-0.03 |
0.32 |
0.49 |
0.62 |
0.64 |
0.67 |
0.76 |
0.92 |
… |
0.69 |
0.57 |
|
270 |
-0.06 |
0.34 |
0.49 |
0.48 |
0.47 |
0.47 |
0.57 |
0.79 |
0.96 |
… |
0.67 |
|
305 |
0.03 |
0.15 |
0.15 |
0.27 |
0.35 |
0.43 |
0.55 |
0.73 |
0.85 |
0.90 |
… |
Table 6: Rank correlation of EBVs of bull
with parent average and bSire-MGS index
|
|
Coefficient of Rank Correlation |
|
Number of daughters |
Number of bulls |
Parent average |
Sire-MGS index |
1-10 |
899 |
0.94 |
0.86 |
11-20 |
179 |
0.88 |
0.74 |
21-30 |
105 |
0.86 |
0.68 |
31-50 |
145 |
0.88 |
0.70 |
51-100 |
147 |
0.87 |
0.69 |
101-200 |
80 |
0.79 |
0.48 |
201- |
61 |
0.82 |
0.51 |
The genetic and phenotypic
correlations among DIMs with an interval about 30 days are shown in Table 5,
which ranged from -0.06 to 0.98 and from 0.06 to 0.69, respectively.
The maximum value of genetic correlation coefficient was between DIM155 and
DIM185, and the minimum value was between DIM5 and DIM270. The maximum of
phenotypic correlation coefficient was between DIM240 and DIM270, and the
minimum value was between DIM5 and DIM305. The genetic and
phenotypic correlation of milk yield showed the same pattern, i.e., the
correlation coefficient decreased with the increase of DIM interval. The
smallest genetic correlation coefficient between two DIM with interval about 30 days was
0.60 at the beginning of lactation, and the highest was 0.98 in the middle
lactation. The phenotypic correlation coefficients between two DIM with
interval about 30 days were not big different in the whole lactation period,
ranging from 0.55 to 0.67.
The correlation between EBV305d of the
bulls and the pedigree index is a measure of the ratio of pedigree index
accuracy to bull EBV accuracy. As shown in Table 6, the rank correlations
between EBVs of the bulls with different daughters and the parent average
ranged from 0.79 to 0.94, indicating that the gains in accuracy from daughter
information ranged from
to , compared with parent average. The
correlations between bull EBV and the pedigree index calculated from sire and
maternal grand-sire (Sire-MGS index) ranged from 0.48 to 0.86, indicating that the gains in accuracy from
daughter information ranged from 16.3 to 108.3%, compared with Sire-MGS index.
The rank
correlation coefficient between EBVs of bulls and the bulls’ parent averages
was 0.94 for the bulls with less than 10 daughters, and the correlation
decreased to 0.82 when the number of daughters increased to more than 200. The
rank correlation coefficient between EBVs of the bulls and the Sire-MGS index
was 0.86 for the bulls with less than 10 daughters, and the
correlation decreased to 0.51 for the bulls with more than 200 daughters.
To improve breeding quality, optimize breeding and
increase milk yield, may factors, such as lactation curve (Boga et al. 2020; Kul 2020), exogenous
hormones (Murtaza et al. 2020), feeding management (Mobashar et al. 2018; Atasever et al. 2020;
Khan et al. 2020), body conditions
and characters (Kul et al. 2020),
genetics and diseases (Erdem and Okuyucu 2020; Kuropatwinska
et al. 2020) have been
studied.
This study analyzed test day models
using RRM model with different knots of Splines and different orders of Legendre polynomial. The results showed that
Sp15-La4-Lp3 could be the optimal model for estimation of genetic parameters
and prediction of breeding values of milk yield in Shandong Holstein
population, cased on AIC and BIC statistics.
Additive genetic, permanent
environment and phenotypic variances showed concave curves with and moderate
oscillations throughout lactation period. This trend is consistent with
Silvestre et al. (2005) and Ren et
al. (2017). The
estimated heritabilities of the test day milk yield over the entire lactation
period ranged from 0.20 to 0.30, which was fallen between the estimates
reported by White et al. (1999), but higher than the estimates by Zaabza
et al. (2018) and Pelmus et al. (2016).
As expected, the genetic and phenotypic
correlation between milk yields at different DIMs decreased with the increase
of DIM interval, which is consistent with the results of Fazel et al. (2017) and Wang et al. (2017). The genetic and
phenotypic correlation coefficients between DIMs reported by Fazel et al. (2017) ranged from -0.035 to 0.98
and from 0.03 to 0.67, respectively, which were very similar to the results
obtained in this study. Wang (2011) studied the genetic parameters of Sanhe
cattle by random regression model and the results showed that the range of
genetic and phenotypic correlation of milk yield traits between DIMs in the
first lactation period was -0.50~0.94 and -0.13~0.73. However, the phenotypic correlations
of milk yield between DIMs reported by White et al. (1999); Silvestre et al. (2005) were 0.40~0.75 and
0.32~0.78, respectively. The results are somewhat different in
different studies, possibly due to the differences in environment, management
and genetic background of the populations as well as statistical model used.
Correlation between EBVs of the
bulls and the pedigree index reflected the contribution of daughter information
to bull EBV, the lower correlation, the larger contribution. As shown in this
study, both correlation between Bull EBV and parent average and correlation
between bull EBV and Sire-MGS index decreased with increasing number of
daughters. The rank correlation between EBVs for 305 d
milk yield predicted using 305 d milk yield records using Lactation Model and
EBVs for 305 milk yield estimated using test day RRM for bulls increased from
0.86 to 0.95 (Padilha et al. 2016). This indicates that
the larger number of daughters of the bull the greater the rank correlation
coefficient of the estimated breeding values between different models. The
results are consistent with those obtained in this study.
In all
models of this study, the order of Legendre polynomials had larger effect on
goodness of fit and the estimates of genetic parameters than the number of
Spline knots. Sp15-La4-Lp3 could be the optimal model for estimation of genetic
parameters and prediction of breeding values of milk yield in Shandong Holstein
population. With the increase of daughters of the bull, the
correlation coefficient between EBVs of bulls and the pedigree index decreased
and thus the accuracy of Bull EBV in relation to pedigree index increased, indicating the amount of progeny
information is critical to the genetic evaluation of bulls.
This work was supported by
Natural Science Foundation of Shandong Province (ZR2016CM37), Key Research and
Development Plan of Shandong Province (2018GNC113003), Agricultural improved
breed project of Shandong Province (2016LZGC027), China Agriculture Research
System (CARS-36), Breeding and demonstration of high yield and β-casein A2
dairy cows (2019B10018), Agricultural scientific and technological innovation
project of Shandong Academy of Agricultural Sciences (CXGC2016A04).
Jianbin Li
designed the experiment and guided the writing of the article, Wan Lv analyzed
the data, Wan Lv and Gaozhan Cai wrote this article,
Gaozhan Cai revised this article, Yujiao Wang, Xianguo Gu, Xiuxin Zhao, Xiaotao Liu, Rongling Li, Minghai Hou
analyzed and discussed results.
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