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Genetic analysis of twinning rate in Israeli Holstein cattle
M Ron, E Ezra, Ji Weller
To cite this version:
M Ron, E Ezra, Ji Weller. Genetic analysis of twinning rate in Israeli Holstein cattle. Genetics
Selection Evolution, BioMed Central, 1990, 22 (3), pp.349-359. �hal-00893849�
Original article
Genetic analysis of twinning rate
in Israeli Holstein cattle
M Ron* E Ezra, JI Weller
Agricultural
ResearchOrganization,
The YolcaniCenter,
Institute
of
AnimalScience,
BetDagan 50-250,
Israel(Received
12April 1989; accepted
15May 1990)
Summary - Second and third
parity twinning
rate of Israeli Holsteins wasanalyzed by
linear
(LM)
and threshold models(TM).
Data were 124 553calving
records ofdaughters
of 179 sires.
Twinning
rates were 4.8 and 6.9% for second and thirdparity, respectively.
Heritabilities,
as estimatedby
REML for the LManalysis,
and the counterpart of REML for the TManalysis,
were 2.2 and 10.1%. The correlation betwen LM and TM evaluationswas 0.98. Both distributions of sire evaluations were
positively skewed,
butonly
theLM distribution differed
significantly
fromnormality. Heritability
as estimated from the maternalgrandsire
effect ontwinning
rate, correlations between sire and maternalgrandsire evaluations,
intraclass correlations amonghalf-brothers,
and son-sireregressions
were all consistent with the
hypothesis
ofpolygenic
additive inheritance. Sire evaluations fortwinning
rate wereeconomically favorably
correlated with evaluations fordystocia.
Breeding
fortwinning
rate may be feasibleby
selection of sires withhigh repeatability evaluations,
and will not result insignificant
undesirable correlated responses.cattle
/
twinning/
thresholdmodel / selection /
additive inheritanceRésumé - Analyse génétique du taux de gémellité chez les bovins Holstein d’Israël.
Le taux de
gémellité
aux deuxième et troisièmevélages
de vaches Holstein d’Israél a étéanalysé
à l’aide du modèle linéaire(LM)
et du modèle à seuil(TM).
Les donnéesportent
sur
124 553 vélages
desfilles
de 179 taureaux. Le taux degémellité
estrespectivement
de.¢,8
et6,9%
au deuxième et au troisièmevélage.
L’héritabilité est estimée à2,2%
par la méthode du maximum de vraisemblance restreint(REML)
dansl’analyse
LM et à10,1%
par
l’équivalent
du REML dansl’analyse
TM. La corrélation entre les évaluations ZM et TM est de0,98.
Les distributions des évaluations despères
sont toutes 2dissymétriques (avec
uneplus longue
queue de distribution vers les valeursélevées),
mais seule ladistribution LM
di,ff’ère significativement
de la normalité. L’héritabilité estimée àpartir
des
effets
desgrands-pères
maternels sur le taux degémellité,
les corrélations entre les évaluations despères
et desgrands-pères maternels,
les corrélations intraclasse entre demi-frères
et lesrégressions père-fils étayent
toutesl’hypothèse
d’un déterminismepolygénique additif.
Sur leplan économique,
le taux degémellité
est liépositivement
avec lafacilité
du
vélage.
La sélection pour lagémellité
semblepossible
par un choix depères
dontl’évaluation est
répétable,
sans entraîner deréponses économiquement défavorables
surles autres caractères.
bovin / gémellité / modèle
àseuil / sélection
àseuil / modèle
additif*
Correspondence
andreprints
INTRODUCTION
The worldwide
surplus
of milk relative to beef has attracted attention to thegenetics
oftwinning
indairy
cattle. Incattle, twinning
may have both desirable and undesirable effects. Themajor
contribution oftwinning
would be an increasedcalf crop in both beef and
dairy
cattle(Bar-Anan
andBowman, 1974);
in the latteran increase in the number of
offspring
ofgenetically superior
females may also beimportant (Frey, 1959). However, increasing twinning
rate will also increase thefrequency
of freemartins(sterile
females born with a maletwin),
and may increasethe incidence of
premature calving
anddystocia,
andthereby indirectly
reduce thesubsequent conception
rate. There isconflicting
evidenceconcerning
the effect oftwinning
on milkproduction;
somereports
have indicated apositive
effect(Morris, 1984; Syrstad, 1984)
whereas others havereported
anegative
effect(Meadows
andLush, 1957; Frey, 1959).
Twinning
is a discrete observation with a binomial distribution. Theheritability
of
twinning
has been estimated on observedfrequencies (Gaillard, 1969;
Bar-Ananand
Bowman, 1974)
and onprobit
and arcsine values(Dempster
andLerner, 1950;
Van
Vleck, 1972) leading
to an overall value of :3%.
The thresholdmodel,
whichassumes an
underlying
normaldistribution,
has beenapplied
to other dichotomous cattle traits such asdystocia
and calfmortality (Gianola
andFoulley, 1983;
Welleret
al, 1988; Weller
andGianola, 1989).
It would seem that this model should also beappropriate
foranalyzing twinning
rate.Observations of cows with an
exceptional
rate oftwinning
and of sires with anexceptional prepotency
fortwinning
have beenreported (Bar-Anan
andBowman, 1974; Maijala
andSyvajarvi, 1977; Morris, 1984).
These were followedby attempts
to select for
twinning
on the basis ofhigh
initialtwinning
rate of foundation dams and bulls(Morris, 1984).
In a recentexperiment,
the firstgeneration
ofdaughters
had a
twinning frequency
of12.8% (Foulley
etal, unpublished results, 1987).
The mode of inheritance of
twinning
in cattle has not been established. Tworeports hypothesized
that asingle
gene may beresponsible
fortwinning
in the NewZealand
milking
shorthorn(Morris
andDay, 1986)
and in the Israeli Friesian(Bar-
Anan and
Bowman, 1974). However,
in ananalysis
of one millioncalvings
indairy cattle, Syrstad (1984)
found no evidence tosupport
thishypothesis.
Insheep,
asingle
dominant gene was shown to affectfecundity (Davis
etal, 1982; Piper
andBindon, 1982).
The
objectives
of thisstudy
were toanalyze twinning
rate in the Israeli Holsteindairy population by
linear and thresholdmodels,
and toclarify
the mode ofinheritance of
twinning,
and thegenetic
associations oftwinning
rate with othertraits of economic
importance.
MATERIALS AND METHODS
Records of second and third
parity calvings
of Israeli Holsteins from 1980through
1987 were
analyzed.
Firstparity
records were deleted because of the low incidenceof twinning (Bar-Anan
andBowman, 1974).
Records were deleted from theanalysis
if:
1)
sire of cow or calf wasunknown; 2)
maternalgrandsire (MGS)
of the cow wasunknown; 3)
cow’sfreshening
date or birthdate wasunknown; 4)
sire of cow had< 100 valid
daughter records;
and5)
MGS of cow had < 100 validgranddaughter
records. The edited data set included 124 553
records,
of which 77 631(62%)
weresecond
parity calvings.
Meancalving
intervals between first andsecond,
and secondand third
parity
were 385 and 366d, respectively.
Basic statistics of the data setare
given
in table I.Variance
components
and sire evaluations werecomputed by
both linear model(LM)
and threshold model(TM) analyses (Gianola
andFoulley, 1983), using
thealgorithm
of Misztal et al(1989).
Variancecomponents
were estimatedby
REMLfor
LM,
andby
thecounterpart
of REML for the TManalysis.
Theanalysis
modelwas as follows:
where
5 i ;ki
is 0(single)
or 1(twin) calving
of the lth cow inparity i,
inherd-year-
season
j, daughter
of the kthsire; Pi
is the effect ofparity i(i
=2,3); HYS J
isthe effect
of jth herd-year-season; S k
is the effect of sirek;
and eijkl is the random residual associated with each record.HYS,
sire and residual effects wererandom,
while the effect ofparity
was fixed. Twocalving
seasons were defined within each year;calvings
from Marchthrough September,
andcalvings
from Octoberthrough February.
Since there were 7684HYS,
this effect wasabsorbed,
and its variancecomponent
could not be estimated. Therefore the HYS variancecomponent
wasarbitrarily
set as 0.1 of the residual variance.Twinning
rate wasanalyzed by
a secondmodel,
in which the sire effect wasreplaced
with the MGS effect. Sires and MGS were assumed to be unrelated in theanalyses.
Since no group of sire or MGS effects were included in theanalysis models,
theexpectation
of theevaluations
was 0 for allanalyses.
For
TM,
2 rounds ofFisher-scoring
iteration wereperformed prior
to variancecomponent
estimationby
a modification of theexpectation-maximization (EM) algorithm,
and between eachstep
of variancecomponent
estimation. Two rounds of EM iteration wereperformed
between eachstep
ofFisher-scoring
iteration.Estimation of LM variance
components
was alsoby
EM. Iteration was continued for both methods until thechange
in the ratio of residual to sire variances was<1%
of the
previous
value. At least 10 rounds ofFisher-scoring
iteration wereperformed
for the TM
analyses.
The
heritability
estimates fortwinning
rate werecomputed
as 4 times the sire variancecomponent
and 16 times thegrandsire
variancecomponent
dividedby
the
respective phenotypic
variances.Phenotypic
variances werecomputed
as thesum of the sire
(or MGS), HYS,
and residual variancecomponents.
Variancecomponents
and solutions from the TManalyses
are inarbitrary
units. To facilitatecomparisons
between the 2analyses,
units in the TManalysis
were set so that theresidual variance
component
would beequal
to the residual variancecomponent
of thecorresponding
LManalysis. Heritability
on theunderlying
scale(h’)
wasalso
estimated
by
thefollowing equation (Dempster
andLerner, 1950):
where
hr
is the estimate ofheritability
from the linear modelanalysis,
p is theproportion
of twins in the data setanalyzed,
and z is the normal ordinate for p.Repeatabilities
of sire evaluations from the LManalysis
werecomputed
as(Var
Sire -
PEV)/(Var Sire),
where Var Sire is the REML estimate of the sirecomponent
ofvariance,
and PEV is theprediction
errorvariance, computed
as thediagonal
element of the inverse of the coefficient matrix.
Repeatabilities
of MGS evaluationswere
computed
in ’a similar manner, with Var Sirereplaced by
the MGS variancecomponent.
The
Kolomogorov
D statistic was used to test the deviation of the distributions of evaluations fromnormality (Snedecor
andCochran, 1967)
and the gi statistic to test for skewness(Sokal
andRohlf, 1969).
Intraclass correlations(t)
of evaluations among half brothers and theregressions
of evaluations of sons on sires(b)
werecomputed.
Product moment correlations were
computed
between sire evaluations for twin-ning
rate and for annualizedmilk, fat,
andprotein production [365 (total
lactationyield/calving interval)],
fat andprotein percent, conception rate, dystocia,
and calfmortality.
Evaluations fordystocia
and calfmortality
werecomputed
both for thesire of the calf and the cow
calving. Only
firstparity single calvings
were includedin the
analyses,
withnegative
valuesindicating
low incidence ofdystocia.
The sireevaluations for these traits were
computed
as describedby
Bar-Anan et al(1987),
and Weller et ad
(1988),
and the data setsanalyzed
aregiven
in Weller and Ron(1989).
RESULTS
Table II
presents
the variancecomponent
andheritability
estimatesby
both thelinear
and threshold models for both the sire and MGSanalyses. Similarly
toprevious
results for dichotomoustraits, heritability
estimates were found to be several timeshigher by
the TManalyses,
ascompared
to the LManalyses (Weller
etal, 1988;
Weller andGianola, 1989).
The estimates ofheritability
on theunderlying scale,
derived from theequation
ofDempster
and Lerner(1950)
are listed inparentheses
after the TM estimates. These values areslightly
lower than the direct TMestimates,
andcorrespond
toprevious
results foranalysis
ofcalving
traits(Weller
etal, 1988).
For both the TM and LManalyses,
theheritability
estimatesderived
by
the sire and MGSanalyses
were very similar.The distributions of sire evaluations are
given
infigure
1 for the LManalysis,
andin
figure
2 for the TManalysis.
The statistics for these distributions aregiven
intable III. The ranges and standard deviations
(SD)
of evaluations for TM weretwice the ranges and SD for the
corresponding
LManalyses,
eventhough
theTM evaluations were scaled to
equal
residual variances. Asexpected
from thepolygenic
additive model ofinheritance,
the ranges for the sire evaluations were more than twice aslarge
as thecorresponding
MGS ranges.Assuming
additivegenetic
inheritance andequal repeatabilities,
the SD of the sire evaluations should be twice that of thecorresponding
MGS evaluations. Infact,
the SD of the sireevaluations were more than twice the
corresponding
MGS evaluations. This is notsurprising,
since the meanrepeatability
of the sire evaluations wasnearly
twicethe mean
repeatability
of the MGS evaluations. The LM distributions werehighly skewed,
as evident both fromfigure
1 and the 91 statistics.Although
gi values werelower for the TM
analyses,
both werepositive,
and skewness wassignificant
for thesire distribution at p < 0.01. Skewness for the distribution of sires with
repeatability
>
65%
wasonly marginally
less. Both of the LM distributions deviatedsignificantly
from
normality,
as estimatedby
the Dstatistic,
but the TM distributions did not.The sire
Shafan,
No781,
had thehighest
sire evaluation fortwinning rate;
5.9%
and9.1%, by
the LM and TManalyses, respectively.
Thetwinning
rate of6112
calvings
ofdaughters by
Shafan was10.8% (repeatability
=95%),
and thetwinning
rate of hisgranddaughters
was6.7%.
His MGS evaluations were0.5%
and
0.8%,
for LM andTM, respectively,
but these evaluations are basedonly
on388
granddaughters (repeatability
=30%).
Thus it is evident that thisparticular
sire could be used to breed for increased
twinning
rate.The correlations among TM and LM sire and MGS evaluations are
presented
intable IV.
Similarly
toprevious
results forcalving
traits(Weller
etal., 1988;
Wellerand
Gianola, 1989),
correlations between TM and LM evaluations weregreater
than 0.95. The correlations between sires and MGS evaluations were 0.41-0.42.The
expectation
of these correlations for evaluations withcomplete repeatability
is0.5. Therefore the results obtained for evaluations with moderate
repeatability
isin accord with the
hypothesis
of additive inheritance.Coefficients of intraclass correlations and son-sire
regressions
of evaluationsare
presented
in table V. Both theregressions
and correlations were close to theexpected
values withcomplete repeatability.
These results alsosupport
thehypothesis
ofpolygenic
additive inheritance.Correlations between evaluations for
twinning
rate anddystocia
aregiven
intable VI. All other correlations between
twinning
and other traits of economicimportance
were within the range of -i to1,
and notsignificant.
Correlations between sire evaluations fortwinning
rate and the sire of cow evaluation ondystocia
were
significant
at P < 0.05. Asexpected,
the TM and LM evaluations had very similar correlations with bothdystocia
traits.Although
the correlation between the sire of calf evaluations fordystocia
andtwinning
rate wasslightly higher
than thecorrelation between the sire of cow evaluations for
dystocia
andtwinning rate, only
the latter was
significant,
because of thegreater
number of sires with evaluations.These correlations are in fact
positive
on the economicscale,
sincenegative
valuesare favorable for
dystocia.
DISCUSSION
The mean rate of
twinning
in thedairy
cattlepopulation
of Israel is5.6%, compared
with4.5%
in thispopulation
20 y ago(Bar-Anan
andBowman, 1974).
This may be due to a difference in data
recording
orediting. However,
within thisperiod
the milkyield
per cow in Israel has increasedby
>50% (Kalay, 1986).
The increase in
twinning frequency
may be due toimproved feeding, therapy
ofanoestrous cows, and selection for milk. A
positive genetic
correlation betweentwinning
rate and milkproduction
was found inprevious reports (Morris, 1984),
but not in this
study.
Linear model
heritability
estimates fortwinning
based ondaughter
andgrand- daughter
groups are in accordance with many other studies(Morris, 1984).
The5-fold increase in
heritability
found in the threshold modelanalyses
agrees with results for other dichotomous traits(Weller
etal, 1988,
Weller andGianola, 1989).
The correlations between sires and MGS
evaluations,
the intraclasscorrelations,
and the son-sire
regressions
allsupport
thehypothesis
ofpolygenic
additive inher- itance. Thisgenetic
variation may be used for selection.Previous studies documented
exceptional
sires fortwinning; daughters
of thesires Zemed
(Bar-Anan
andBowman, 1974),
and Tahto(Maijala
andSyvajarvi, 1977)
had11%
and12.2% twinning, respectively.
Asegregating major
gene wasproposed
toexplain
these results. In the currentstudy
thetwinning
rate of 6 112daughters
of the sire Shafan was10.6%.
His evaluation fortwinning
rate was 4 SDunits above the mean in the LM
analysis,
butonly
3 SD unitsgreater
than themean in the TM
analysis.
Under the.assumption
ofnormality,
theprobability
ofobservations > 3 SD units is 0.0013. Thus in
sample
of 179sires,
theexpected frequency
of sires > 3SD
units is 0.0013(179)
= 0.27. Thus asingle
observation in this range is consistent with thehypothesis
ofpolygenic
additive inheritance.Although
skewness was lower for the TM than for the LM distribution ofevaluations,
both the TM distributions for allsires,
and forhigh repeatability
sireswere still
significantly
skewed. Deletion of Shafan reduced the gl value to0.3,
a value on the border ofsignificance.
Four otherhigh repeatability sires,
out of atotal of
51,
had evaluations > 2 SD units above the mean. These results are at variance with the threshold modelassumption
of anunderlying
normal distribution.Furthermore,
in theprevious analysis
ofcalving
traits in thispopulation,
none of the TM distributions weresignificantly skewed,
eventhough
the LM distributionswere
(Weller
etal, 1988).
Misztal et al(1988)
demonstrated that if the distribution of theunderlying
variable is notnormal,
solutions for fixed and random effects canstill be calculated as if
normality
held. Thus even in thepresent
case TM issuperior
to LM.The distribution of TM sire evaluations could be
explained by
asegregating
gene with a substitution effect of ! 1
genetic
SD unit andunequal
allelicfrequency.
Since all
analyses
were based on sire or MGSevaluations,
thepossibility
of amajor
recessive gene with a low
frequency
allele also cannot be excluded.Sire evaluations for
twinning
rate werefavorably
correlated with evaluations fordystocia,
in accordance withprevious
results on thispopulation (Bar-Anan, 1971).
Correlations between
twinning
rate andproduction
traits were notsignificant.
Because of low
heritability,
selection fortwinning
will not bepractical
on the sire-to-dam
path. However,
since sires of sires are often selected amonghigh-repeatability
proven
sires,
selection fortwinning
may bepractised
in the sire-to-sirepath.
Weller
(1989)
found that selection based on an indexincluding
milkproduction
and
fertility
could increaseconception
rateby 5%
in 10 y, but would result in an8%
reduction in the
genetic gain
foreconomically
fat-corrected milk.Using
the samemethod,
andassuming
the same reduction ingenetic gain
forproduction traits,
selection for
twinning
rate in the malepathways
would result in agenetic
increaseof
1.2%
over this timeperiod.
In
conclusion,
thepreponderance
of evidencesupports
thehypothesis
ofpoly- genic
additive inheritance fortwinning rate, although
thepossibility
ofsegregating major
genes cannot be excluded.Breeding
fortwinning
may be feasibleby
selec-tion of sires with
high repeatability evaluations,
and will not result insignificant
undesirable correlated responses.
ACKNOWLEDGMENTS
This
investigation
wassupported by
the US-Israel BinationalAgricultural
Re-search and
Development
Fund(BARD), Project
No US-805-84. We wish to thank I Misztal forproviding
the threshold modelcomputer
program used in thisanalysis,
and D Drori for useful
suggestions.
Thismanuscript
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1989
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