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Genetic improvement of litter size in sheep. A
comparison of selection methods
M Pérez-Enciso, Jl Foulley, L Bodin, Jm Elsen, Jp Poivey
To cite this version:
Original
article
Genetic
improvement
of
litter size
in
sheep.
A
comparison
of selection
methods
M
Pérez-Enciso
1
JL
Foulley
L
Bodin
2
JM Elsen
JP
Poivey
2
1
Institut national de la recherche
agronomique,
station degénétique
quantitative
etappliqu6e, Jouy-en-Josas
78352cedex;
2Institut national de la recherche
agronomique,
station d’ameliorationgénétique
des animaux, BP27,
3i826 Castanet-Tolosancedex,
France(Received
22February 1994; accepted
1August
1994)
Summary - The
objectives
of this work were to examine the usefulness ofmeasuring
ovulation rate(OR)
in order toimprove genetic
progress of litter size(LS)
insheep
and tostudy
different selection criteriacombining
OR andprenatal
survival(ES)
performance.
Responses
to selection for 5generations
within apopulation
of 20 male and 600 femaleparents were
compared using
Monte-Carlo simulationtechniques
with 50replicates
perselection method. Two breeds with low
(Merino)
and medium(Lacaune)
prolificacy
wereconsidered. Records were
generated according
to a bivariate threshold model for OR and ES. Heritabilities of OR and ES in theunderlying
scale were assumed constant over breeds andequal
to 0.35 and 0.11,respectively,
with agenetic
correlation of -0.40 between thesetraits. Four methods of
genetic
evaluation werecompared:
univariate best linear unbiasedprediction
(BLUP)
using
LS recordsonly
(b-LS);
univariate BLUP on OR records(b-OR);
bivariate BLUPusing
OR and LS records(b-ORLS);
and a maximum a posterioripredictor
of ageneralised
linear modelwhereby
OR wasanalysed
as a continuous traitand ES as a
binary
threshold trait(t-ORES).
Response
in LS was very similar withb-LS,
b-ORLS and
t-ORES,
whereas it wassignificantly
lower with b-OR.Response
in OR wasmaximum with b-OR and minimum with b-LS. In contrast, response in ES was maximum
with b-LS. This
study
raised thequestion
as towhy
selection based on indicescombining
information from both OR and ES did notperform
better than selectionusing
LSonly.
litter size
/
ovulation rate/
prenatalsurvival / sheep /
threshold modelCorrespondence
andreprints: UdL-IRTA,
Area of AnimalProduction,
RoviraRoure, 177,
Résumé - Amélioration génétique de la taille de portée chez les ovins. Comparaison
de méthodes de sélection. Cet article discute l’intérêt du taux d’ovulation
(OR)
pouraccroître le
progrès génétique
sur la taille deportée
(LS)
et étudie à ceteffet
divers critères de sélection combinant OR et le taux de survieembryonnaire
(ES).
On a examinépar simulation les
réponses
à la sélection en 5générations
dans unepopulation
de 20 et600
reproducteurs
mâles etfemelles
avec 50réplications
par méthode. On a considéré2 races, de
prolificité
faible
(Mérinos)
et moyenne(Lacaune).
Lesperformances
ontété
générées
àpartir
d’un modèle bicaractère à seuils. Les héritabilitiés d’OR et ESont été
supposées
constantes sur l’échellesous-jacente
dans les 2 races etprises
égales
respectivement
à0,35
et0,11
avec une corrélationgénétique
entre ces 2 caractères de- 0,40.
Quatre
méthodes d’évaluationgénétiques
ont étécomparées :
i)
Blup
unicaractère basé sur LS(b-LS) ;
ii)
Blup
unicaractère basé sur OR(b-OR) ; iii)
Blup
bicaractère basé sur OR et LS(b-ORLS) ; iv)
Prédicteur du maximum aposteriori
bicaractère d’un modèle linéairegénéralisé
où OR est traité comme un caractère continu et ES comme un caractèreà seuils
(t-ORES).
Lesréponses
observées étaient très voisines avecb-LS,
b-ORLS ett-ORES,
alors que b-OR donne uneréponse significativement inférieure.
Laréponse
surOR était maximum avec b-OR et minimum avec
b-LS,
tandis que laréponse
sur ES étaitmaximum avec b-LS. Cette étude pose la
question
de savoirpourquoi
la sélection basée surdes indices combinant OR et ES ne donne pas de résultats
significativement supérieurs
àla sélection sur LS.
modèle à seuils
/
ovins/
prolificité/
survie prénatale/
taux d’ovulationINTRODUCTION
Several studies
support
the conclusion that increasedreproductive performance
willimprove
economicefficiency
ofsheep
breeding
schemes(Nitter,
1987).
Litter size(LS)
is the traitreceiving
highest
relative economic value in theNorwegian
scheme(Olesen
etal,
submitted);
the British Meat and Livestock Commission(1987)
includes ewe
reproduction performance
in the selection indices in allexcept
terminal sirebreeds;
selection schemes toimprove
LS areimplemented
in most breeds in France. Recommended economic indices used in the Australian Merino should result in substantialgain
in number of lambsweaned,
according
to theoretical studies of Ponzoni(1986).
Litter size in
sheep
has been increasedby
direct selection(Hanrahan,
1990;
Schoenian and
Burfening,
1990)
but thegains
have not been verylarge
because of the lowheritability
of LS. The averagefigure reported
in the literature is 0.10(Bradford,
1985).
Thecategorical
nature of this traittogether
with apossible
physical
upper limit(uterine
capacity)
may also have hinderedgenetic
progress. Ovulation rate(OR)
is considered to be theprincipal
factorlimiting
litter size insheep
(Hanrahan,
1982;
Bradford,
1985).
Heritabilities of OR aretypically larger
than those of LS in mostspecies,
including sheep.
Further,
correlation between OR and LS inhigh
and there is anearly
linearrelationship
with LS at ovulation rates upto 4
(ie
Dodds etal,
1991).
These results led Hanrahan(1980)
to propose OR as an indirect criterion to select for LS. Before routine evaluation of OR isimplemented,
however,
itsadvantage
as selection criterion has to be assessedexperimentally.
1992)
and in Romanov(Lajous
etal, quoted
in Bodin etal,
1992)
but, despite
theoreticalexpectations,
most of response in OR did not result in an increase of LS. The samephenomenon
has been observed in mice(Bradford, 1969).
Inpigs,
OR was increasedby
selection but correlated response in LS was smaller thanexpected
(Cunningham
etal,
1979).
A second
possible
criterion of selection is an index that combines OR andprenatal
survival(ES).
Johnson et al(1984)
derived a linear index of OR and ES andthey predicted
that responseusing
the index would be about50%
larger
thanwith conventional direct selection on LS in
pigs.
Similarpredictions
aregiven
by
Bodin et al(1992)
insheep.
However,
selectionexperiments
have not confirmed theexpected advantage
of an index for LScomponents,
in mice(Gion
etal,
1990;
Kirby
andNielsen,
1993)
or inpigs
(Neal
etal,
1989),
whereas there is noexperimental
evidence insheep
yet.
In allspecies,
theapparent
reasonwhy
OR or an index was no better criterion than LS was a correlated decrease in ES.Cited
predictions
of response areimplicity
based on an infinitesimal model with a continuousnormally
distributed trait. This model can bejustified
for OR inpigs
or mice butcertainly
not forES,
which is a dichotomous trait. P6rez-Enciso et al(1994a)
examined theimplications
ofgenerating
OR
and ES recordsaccording
to a bivariate threshold model. In thismodel,
2underlying
(unobserved)
normalvariates which are
negatively
correlated and a set of fixed thresholds are assumed. The mainimplications
of a bivariate threshold model for litter sizecomponents
are:(i)
the existence of a non-linearantagonistic relationship
between OR andES,
iecorrelation between LS and OR decreases as OR
augments;
(ii)
as a consequence, a linear indexcombining
OR andES,
whichgives
a constantweight
to ES over all the range ofOR,
is not theoptimum
selection criterion to increase LS in allgenerations;
and(iii)
litter size behaves as a natural index close to theoptimum
selection criterion
combining
OR andES,
at least in the situationanalysed
(mass
selection and
equal
information oncandidates).
Points(ii)
and(iii)
areespecially
relevant because thetheory
based on a linearisation of the modelpredicted
anadvantage
of the index overLS,
which was notfully
achieved in the simulation. This isprecisely
the situation encountered in selectionexperiments,
where a linear index of OR and ES has notproved
to besignificantly
better than direct selection on LS(see
review of Blasco etal,
1993)
regardless
ofoptimistic
predictions.
The
objectives
of this work were:(i)
to examine in a more realistic situation than in aprevious
report
(P6rez-Enciso
etal,
1994a)
the usefulness ofmeasuring
OR inorder to
improve genetic
progress of LS insheep using
overlapping generations
and allfamily
information;
and(ii)
tostudy
different selection criteriacombining
OR and ESperformances.
The influence ofgenetic
correlation between OR and ES has also been considered. Work was carried outusing
stochasticcomputer
simulation.Records were
generated according
to a bivariate threshold model. Two breeds withMATERIALS AND METHODS
Selection scheme
A
population
of 600 dams and 20 sires was simulated. After eachbreeding
season, when new records from OR and LS wereavailable,
old and newborn animals were evaluatedaccording
to 1 of several methods described below. The worst 120 dams(20%)
and the worst 10 sires(50%)
were discarded andreplaced by
the best 120 newborn females and the best 10 newborn males.Only
1 female and 1 maleoffspring
per dam perbreeding
season were allowed and the maximum number of maleoffspring
to be selected from each sire was set to 3. A control line was simulated where sires and dams were chosen at random. Results wereexpressed
as deviations from the controlline,
in order to correct for the effectassigned
to eachbreeding
season. Fivecycles
of selection were simulated and 50replicates
for each selectionmethod were run.
Two
populations
wereconsidered,
a lowprolific
breed(Merino)
and a moreprolific
breed(Lacaune).
Phenotypic
means and variances are shown in table I fornulliparous
andnon-nulliparous
ewes of both breeds. Thesefigures
are based onperformances
in INRAexperimental
herds for Merino and on-farmrecording
for Lacaune. Ovulation rate and LS increased withparity
order even ifprenatal
survival was lower.Phenotypic
correlations between OR and ES were -0.56 and -0.38 in Merino andLacaune,
respectively.
Note thatpopulations
withhigher
means hadhigher
variances but that coefficient of variation remainedapproximately
constant,
as
commonly
observed(Nitter,
1987).
- .. - -.... - - . - .... , ..
Generation of records
Records of
OR,
ES and LS weregenerated
as described in detail in P6rez-Enciso et al(1994a).
Inshort,
both OR and ES werecategorical
variates assumed to be determinedby
a thresholdliability
process withnormally
distributedunderlying
from a Bernoulli distribution with
appropriate
parameters.
Litter size was the number ofembryos surviving.
Thresholds were set to match observedfrequencies
in each
category
of OR and ES. Heritabilities of OR and ES in theunderlying
scale were 0.35 and0.11,
respectively,
in both breeds.Repeatabilities
of OR andES were 0.70 and
0.22,
respectively.
Genetic correlation between OR and ES was - 0.40 in both breeds. Environmental correlations were -0.32 and -0.22 in Merino andLacaune, respectively.
Given that there existsuncertainty
about thegenetic
parameters,
especially
forgenetic
correlation between OR andES,
other correlations were considered in the Lacaune breed. The model used to simulate records includedanimal
plus
common environment as random effects. Fixed effects wereparity,
with 2levels,
first andfollowing
parities,
and year, with 5 levels. Values for the effect ofparity
in theunderlying
scale were chosen as to matchfigures
in table I. Theeffect of year was simulated such that maximum differences between the ’best’ and ’worst’ years were about
10%
in LS.Genetic evaluation
Four methods of
genetic
evaluation werecompared:
1)
univariate BLUPusing
LS recordsonly
(b-LS);
2)
univariate BLUP on OR records(b-OR); 3)
bivariate BLUPusing
OR and LS records(b-ORLS);
and4)
a bivariate non-linear modelwhereby
OR wasanalysed
as a continuous trait and ES as abinary
threshold trait(t-ORES;
Foulley
etal,
1983).
Hereequations
derivedby
Janss andFoulley
(1993)
wereadapted
to take into account that for each record of the ’continuous’ trait(OR),
there were as many observations of thebinary
trait(ES)
as number of ova shed(see
A
P
pendix).
Theoriginal
program(LLG
Janss,
personal
communication)
wasoptimised
to solve thesystem
ofequations
by
sparse matrix methodsusing
FSPAK(Perez-Enciso
etal,
1994b).
Inagreement
with thesimulation,
the statistical model in all methods includedparity
and year as fixedeffects,
and animal andpermanent
environmental effect as random effects. Criterion b-LS is thatcurrently implemented
wheresheep
are evaluated for theirreproductive performance
(Bolet
andBodin,
1992;
Olesen etal,
submitted),
whereas b-ORresponds
to Hanrahan’s(1980)
suggestion
ofusing
OR as indirect criterion to select for LS.Finally,
b-ORLS andt-ORES are different ways of
combining
OR and ESperformance.
Inb-ORLS,
a direct estimation of thebreeding
values for LS isobtained,
whereas in t-ORES theestimated
breeding
values of OR and ES have to be combined in an index for LS. The index chosen was thatsuggested by
Wilton et al(1968),
ie for the ithanimal,
where
!OR,
thepredicted
ovulationperformance,
iswhere
h
ORI
andpoR,
are estimations(maximum
aposteriori,
MAP)
of first yearand first
parity
obtainedby solving
the t-ORESequations
and,
similarly,,a
OR
,
andeffect, respectively.
In[1],
thepredicted
ESprobability
isIn
equation
!3!,
h
ES
&dquo;
PES&dquo; aesi
andF
E
si
are MAPs obtained fromsolving
the t-ORESequations.
Note that because[1]
is a nonlinear indexgenetic
meritdepends
on levels of fixed effects. The index was chosen to maximise response in first
parity.
Alternatively,
aweighted
average of allparities
could also have beenapplied
(Foulley
andManfredi,
1991).
Methods were evaluated in terms of elicited response to selection but
goodness
offit,
assuggested by
P6rez-Enciso et al(1993),
was also studied. Correlations between observed and fitted records werecomputed.
For b-LS and b-ORLSmethods,
fitted LS records of ith animal in thejth
year and kthparity
were obtained fromwhere
!LS,
PLSk’ âLsi’
andF
L
si
are best linear unbiased estimate(BLUE)
and BLUP solutions to fixed and random effects obtained for the LS location param-eters. In the case oft-ORES,
fitted LS records werecomputed
from an expres-sion similar to[1]
except
thatcorresponding
year andparity
solutions were used. Ovulation records were fitted fromexpressions
similar to[2]
and ES records fromexpressions
similar to!3!.
Note that OR was treated in all cases as a continuous variate even
though
it was simulatedfollowing
a threshold model. There isevidence,
nonetheless,
that theadvantage
of a threshold model over a linear model forgenetic
evaluation diminishes veryquickly
for more than 1 threshold(Meijering
andGianola,
1985).
Genetic variances used for
genetic
evaluation were those in the observedscale,
except
for ES in t-ORES.They
were obtainedby
simulation from the definition ofbreeding
value in the observedscale,
ie meanphenotypic
value conditional ongenotype.
Heritabilities of LS were 0.14 and0.15,
and 0.23 and 0.30 for OR in Merino andLacaune, respectively.
Theheritability
of ES was 0.06 in both breeds.Genetic correlation between LS and OR was 0.83 and between LS and
ES,
0.17.RESULTS
Selection responses for LS in the first
generation
are shown in tables II and IIIfor Merino and
Lacaune,
respectively.
An increase in LS of about5-6%
of the mean was achieved in both breeds.Changes
wererelatively
moreimportant
in first than successiveparities. Response
in LS was very similar whether selection wasdirectly
on LS orusing
OR as indirect selection criterion.Considering
informationon both OR and LS
(or
equivalently
OR andES)
produced only
a small increase in response withrespect
to direct selection on LS. Performance of b-ORLS andt-ORES was almost identical. Even if index
[1]
was derived to maximise response in firstparity,
correlated response in successiveparities
was ashigh
as with linearmethods,
ieb-ORLS,
in whichweights
do notdepend
on locationparameters.
ThisSubindices refer to first
(1)
andfollowing parities
(>
1).
Maximumempirical
standarderrors were 0.02 for ALS and AOR and 0.004 for AES.
Subindices refer to first
(1)
andfollowing parities
(>
1).
Maximumempirical
standarderrors were 0.02 for ALS and AOR and 0.004 for AES.
and Manfredi
(1991,
equation
[62]),
whereby
predicted
performance
isweighted
according
tofrequencies
of the differentsubclasses, might
be robust to differentweights.
Changes
in LS wererelatively
similar across selection methods butthey
werenot for the
components,
OR and ES(tables
II andIII).
Ovulation rate increased twice as much when selection was on OR than on LS.However,
only
about half ofthat increase
corresponded
to an increase in LS with b-OR(!LS/ !OR ::::i
0.50),
whereas the ratioALS/AOR
wasalways larger
than 0.80 with b-LS. Methodsb-ORLS and t-ORES induced
changes
in OR similar to b-OR. Correlatedchanges
in ES were also different
depending
on the method of selection. Selectionusing
b-LS wasaccompanied
by
an increase inprenatal
survival of about2%.
All othermethods,
especially b-OR,
resulted in lower ES.Response
of LS in thefollowing
generations
isplotted
infigure
l. Unlike results in tables II andIII,
it is evident that indirect selection on OR was thepoorest
method in thelong
term,
especially
in the moreprofilic
breed,
Lacaune. Direct selection on LS wasonly
slightly
worse than selection based on either b-ORLS or t-ORES.Responses
were notsignificantly
different among methods in anygeneration
with the soleexception
of b-OR.Figure
2 shows correlatedchanges
in ORphenotype.
Asexpected,
b-OR caused thelargest
increase in OR andb-LS,
the minimum. Methodsin-creased more in Lacaune than in Merino. Direct selection for LS in Merino induced no correlated
phenotypic change
in ES(except
in the firstgeneration),
whereassurvival increased
regularly
in Lacaune. InMerino,
phenotypic
trends werenegative
with b-ORLS and t-ORES in the first 2generations
but ES remained constant or increased thereafter. Thishighlights
that b-ORLS and t-ORES are nonlinear selection criteria withrespect
tounderlying
genotypes.
Selection on OR induced anegative
response in ES because of thenegative genetic
correlation between both traits.Correlations between observed and fitted records are shown in table IV for the traits studied. All methods were very close to each other
regarding
thedegree
of fit within trait.Previous results assumed a
genetic
correlation between OR andES(pg
oR
,
Es
)
of -0.4.Consequences
ofusing
different values of thegenetic
correlation were examined in Lacaune. Table V shows how differentparameters
are affectedby
achange
inp
9oR
,
ES
.
In all casesphenotypic
correlation and heritabilities of OR and ES wereconstant,
thus environmental correlation decreased asgenetic
correlationincreased. Genetic correlations and heritabilities were obtained
by
simulation. Genetic correlation between LS and itscomponents
increased withpg
oR
,
ES
,
but the increase was much more noticeable between LS and ES than between LS and OR. In the extreme case ofpg
oR
,
ES
=-!.9, genetic
correlation between LS and ESwas
less than zero. Thisnegative
genetic
correlation was confirmedby
a decrease in mean ESgenotype
when selection wasperformed
on b-LS(results
notshown).
However,
the ESphenotype
did notchange
(table VI)
perhaps
because of the small decrease in thebreeding
value of ES.Heritability
of LS decreased aspg
oR
,
ES
did.Thus a small
heritability
of LS could be due either to a lowheritability
of itscomponents
or to ahighly
negative genetic
correlation between them(equation !11!
in P6rez-Enciso etal,
1994a).
The effect of
genetic
correlation on response to selection is shown in table VI. Given the similar results between b-ORLS andt-ORES, only
b-ORLS wasstudied,
in addition to b-LS and b-OR. Method b-ORLS was chosen because of its lowerpg,
genetic correlation;
pe, environmentalcorrelation; OR,
ovulation rate;ES, prenatal
survival; LS,
littersize;
h
2
,
heritability
in the observedscale; figures
refer to Lacaune.Figures
refer to Lacaune.genetic
correlation increased. Methods b-LS and b-ORLS were notsignificantly
different for moderategenetic correlations,
whereas b-OR wasconsistently
lessefficient. The behaviour of the ratio
ALS/AOR
depended strongly
ongenetic
correlation. An increase in number of ova shed was followedclosely by larger
litter size for moderate correlations.However,
aspg
oR
,
ES
decreased so didALS/AOR.
DISCUSSION
The
resultspresented
here are inagreement
with simulation resultsreported
previously
(P6rez-Enciso
etal,
1994a)
where selection on OR or on an indexcombining
OR and ES did notproduce
asignificantly larger
response than direct selection on LS. Theslight advantage
of b-ORLS and t-ORES over b-LS in the firstbreeding
season did notpersist
overgenerations,
due to alarger
decrease in ES wheninformation from OR was included in the selection
criterion,
Methodsb-LS,
b-ORLS and t-ORES behaved verysimilarly
withrespect
to LS(fig 1),
butdifferently
withrespect
to OR and ES(fig
2 and3).
Oddly enough, including
information from OR(a
trait of moderateheritability
andhighly
correlated withLS)
did not result in a muchhigher
response for LS but rather in a redistribution ofweights
given
to OR and ES. Selection pressure on ES decreased in bivariate methods(b-ORLS
and
t-ORES)
because correlation between OR and LS is muchhigher
than that between ES and LS(table V).
Phenotypic
differences in ES among lines were small(about
3%
between b-LS and b-ORLS inLacaune)
but it sufficed tocompensate
for different ovulationrates,
a difference ofapproximately
0.2 ova between lines selected with b-LS and b-ORLS. Infact,
one of thearguments
adduced in favour of OR as indirect selection criterion is thatphenotypic
differences between control and selected lines were muchlarger
in OR than in ES(Hanrahan, 1982).
However,
prenatal
survival cannot beneglected
even if its contribution to total variation ofLS in the base
population
issmall,
inparticular
whengenetic
correlation betweenOR and ES is
negative.
Using b-LS,
increase in litter sizecorresponded exactly
to the increase in OR forP90R,ES !
-0.4(ALS/AOR
= 1 in tableVI).
This can beinterpreted
as ifresponse to selection for LS were
completely explained
by
achange
in OR. Incontrast,
selectionusing
ORproduced
a smaller response in LS with a muchlarger
increase in OR(ALS/AOR
=0.48).
Thisphenomenon
was describedby
Bradford(1985)
as &dquo;astriking example
ofasymmetrical
correlatedresponse&dquo;
(underlining
isours).
It is evident from results in tableVI, however,
that thisapparent asymmetry
is due to a differentemphasis
on ES in the two criteria. It is currentopinion
amongsheep
breeders that selection pressure on ES should become moreimportant
as mean OR increases. The results in table Vhighlight
that this pressure alsodepends
on the value of/0gon !g -
As this correlation becomes morenegative,
selection pressureon OR relative to ES increases
dramatically,
especially
if information on OR is used.Then,
ifprenatal mortality
increases toomuch,
as a result of a correlatedchange
withOR,
decline in ES will offset the increase in OR. Forinstance,
forP
g
OR
,
ES
=
-!!9 response in LS wasslightly larger
with b-ORLS than with b-LS in the firstgeneration
(results
notshown)
but the reverse was true in the fifthgeneration
(table VI).
Matos
(1993)
reported
correlations between fitted and observed LS records about 0.65 in Rambouillet andFinnsheep using
linear models. Thesefigures
arerelatively
close to thosereported
here if we consider that in Matos’(1993)
study
variances had to be estimated from the same data set. In a similarstudy,
Olesen et al(1994)
reported
lower correlations between fitted and observed LS records ofNorwegian
terms of
goodness
of fit but the differences between methods were verysmall,
inagreement
with results in table IV.The
question
whether LS can be increased morerapidly by
using
information on itscomponents
rather thanby
direct selection remains open. Allexperiments
have failed in thisrespect
(Blasco
etal,
1993).
Alikely explanation
is that indicescombining
OR and ES(or
OR andLS)
have not beenoptimum. Only
linear indices with a constant
weight
to ES over all the range of OR have been testedexperimentally,
and these do not take into account the nonlinearphenotypic
relationship
among LS and itscomponents.
P6rez-Enciso et al(1994a)
have shownthat a
separate
index for each OR should be used. Nonlinear indicesmight
overcome some of thesehandicaps.
In thiswork,
asimple
nonlinear index(equation
[1])
was examined. The exactequation
is anintegral
thatimplies marginalization
withrespect
to alarge
number of variables. Theanalytical
solution to thisintegral
isunknown.
Equation
[1]
is a first-orderapproximation
which willonly
be close to theoptimal
criterion if the amount of information on each individual islarge
(Gianola
andFernando,
1986).
Resultsshowed, however,
that nonlinear indices(t-ORES)
did not elicit alarger
response in LS than linear indices(b-ORLS),
perhaps
because of the lack of information. Moreovergenetic
parameters
in the observed scale are assumed to be constant butthey depend
on thepopulation
mean, whichchanges
with selection. It should berecalled, nonetheless,
that OR could be used as anearly
predictor
forLS,
given
itshigh
correlation with LS and itshigh repeatability.
Measurement of OR would then allow us to decreasegeneration
interval and increase the accuracy ofgenetic
evaluation of young animals.Certainly,
the resultspresented
heredepend
crucially
on howlikely
a bivariate threshold modelis,
ie on the existence of 2underlying
continuous normal variates and a set of fixed thresholdpoints.
Because a statistical model isnecessarily
anoversimplification
ofreality,
these conditions will never be met with strictrigour.
Thereis, nonetheless,
considerable literature on theplausibility
andbiological
justification
of the thresholdmodel,
see reviewsby
Curnow and Smith(1975)
andFoulley
and Manfredi(1991).
Withrespect
toreproductive
traits,
there is acomplex
interaction between continuousvariates,
eg, hormonelevels,
and discretevariates,
ienumber of ova and survival
(Haresign, 1985).
A threshold-like mechanism has been advocated toexplain
embryo mortality
as a function of thedegree
ofasynchrony
between uterus andembryo
(Wilmut
etal,
1985).
In
addition,
covariation among LScomponents
and selectionexperiment
results can be used to check thevalidity
of the threshold model.First,
under the bivariate threshold model consideredhere,
thephenotypic probability
ofembryonic
survival at agiven
ovulation level isgiven
by
(P6rez-Enciso
etal,
1994a)
where p.
is theunderlying
mean, x is theunderlying
variable,
b is theregression
of xES on Rxo and p is the correlation between xES and xoR
.
Equation
[4]
allows us to describe adecreasing
correlation between OR and LS as ORincreases,
ascommonly
observed in real data(Hanrahan,
1982;
Dodds et al1990).
Further,
[4]
can be written as.1,O
)]
R
f
R -
o
<I>[a+,B(x
with /3
=b/(1-p
2
)
1
/
2
.
Nowon number of ova
(P6rez-Enciso
etal,
1994a),
or fromphenotypic
covariances and variances(table I),
assuming
that[4]
holds as well in the observed scale. With theparameters
usedhere,
values for!3
from theprobit regression
were -0.34 and - 0.25and,
fromphenotypic
covariances,
-0.37 and -0.18 for Merino andLacaune,
respectively. Agreement
seemsreasonable,
especially
for the lessprolific
breed.Secondly,
table Vemphasises
thatgenetic
parameters
forOR,
ES and LS are interrelated. Inparticular, heritability
of LS can beexpressed, approximately,
as(P6rez-Enciso
etal,
1994a),
where py is thephenotypic
mean;Varg(Covg)
thegenetic
variance(covariance)
in the observedscale;
andVary
thephenotypic
variance. It follows that for a
given
variability
of OR andES, heritability
ofLS is
inversely
related togenetic
correlation between OR and ES. Thusgiven
thephenotypic
parameters
in table I andprovided
heritabilities are moderate for OR and low for LS andES,
equation
[5]
allows us topredict
anegative
genetic
correlation between LScomponents.
Table VII shows how well[5]
predicted
heritabilities of LS in different studies
reporting
multivariate variance estimates ofOR,
LS and ES inpigs.
Agreement
betweenexpected
and estimated heritabilities was excellent inreported
estimates inpigs.
Note thatHaley
and Lee(1992)
found no additive variation for ES and that in this case the smallerheritability
of LS occurs due to the additional noise fromembryonic mortality.
Anegative genetic
correlation between OR and ES has also been evidencedby selecting
onOR,
which has beenaccompanied
by
a lower ES(Bradford,
1969;
Cunningham
etal, 1979;
Hanrahan,
1992).
Mostreported
estimates ofgenetic
covariances between OR and ES inpigs
and rabbits are alsonegative
(Blasco
etal,
1993).
Furthermore,
themagnitude
of this correlationgreatly
influences the ratio of response in LS relative to OR(R
=ALS/AOR).
The morenegative
thegenetic correlation,
thebigger
the difference in R between direct selection on LS and indirect selection on OR(table VI).
There isexperimental
evidencesupporting
that the ratio R islarger
fordirect selection than indirect selection on OR as
expected
from results in table VI. Forinstance,
R was 0.61using
direct selection in theGalway
breed(Hanrahan,
1990),
and 0.67 in Rambouillet(Schoenian
andBurfening,
1990),
whereas R wasonly
0.26 whenFinnsheep
were selected for OR(Hanrahan, 1992).
n, number of
records;
hL
S
,
expected heritability
of litter size(from
equation
[5]);
other abbreviations as in table V.Finally,
the most criticalimplication
of this model refers to the relativeadvantage
Using
massselection,
P6rez-Enciso et al(1994a)
found in a simulationstudy
that response in LS with an indexcombining
OR and ES was similar to direct selection.Both methods were better than indirect selection on OR. In this
study,
wherefamily
information wasused,
the same conclusionapplies.
These results arecompatible
withexperimental
evidence inpigs
and mice(Bradford,
1969;
Cunningham
etal,
1979;
Neal etal, 1989;
Gion etal, 1990;
Kirby
andNielsen,
1993)
where OR or an indexcombining
OR and ES has notproved
to besignificantly
better than directselection on LS.
Several
problems
with the infinitesimal threshold model remain nonetheless.First, major
genesaffecting
OR insheep
areknown,
the gene Fee B of the Booroola Merinobeing
the best documented case. The presence of amajor
gene per se does not invalidate a thresholdmodel,
since it can be considered as a fixed effect that shifts theunderlying
mean, but it doeschange
thedynamics
of thepopulation
under selection. Thuspredicted
or simulated responses under aninfinitesimal threshold model will be
quite
inaccurate. Genes with asignificant
effect on OR are alsobeing
identified in otherspecies
such as mice(Spearow
etal,
1991)
but evidence isconflicting
inpigs
(Mandonnet
etal,
1992;
Rathje
etal,
1993).
Withrespect
toembryonic survival,
a number of recessive genes thatcause
embryo lethality
in mice have been identified(Rossant
andJoyner,
1989).
As information on effects andfrequencies
of(aTLs affecting
litter sizeaccumulates,
theimplications
of an infinitesimal threshold model should be reconsidered. The existence ofmajor
chromosomal abnormalities as a cause ofembryonic
mortality
would also poseproblems
for the threshold model. In a recentreview,
Blasco et al(1993)
quoted
that lethal chromosome abnormalities are found in5-10%
ofearly
pig
and rabbitembryos,
anon-negligible
proportion.
Deleteriousreciprocal
translocations and
aneuploidies
have beenreported
insheep
but theproportion
ofembryo
deaths due to these abnormalities is uncertain(Bolet,
1986;
Wilmut etal,
1986).
CONCLUSIONS
The main conclusions can be summarised as follows:
(i)
A bivariate threshold model can bejustified
based on statistical andexperimental
evidence.
(ii)
Ovulation rate was an effective criterion of selection for litter size insheep only
in the very short term. Theadvantage
ofusing
OR as anearly
predictor
in orderto decrease
generation
interval should beinvestigated.
(iii)
The ratio of response in litter size relative to ovulation rate(ALS/AOR)
depends
strongly
ongenetic correlation;
the morenegative
thegenetic correlation,
thelarger
the difference in this ratio between direct selection for litter size and indirect selection on ovulation rate. Direct selection on litter size maximised the ratioALS/AOR.
(iv)
Using
information from both ovulation rate andembryonic
survival was notsignificantly
better than selectionusing
litter size recordsexclusively.
Selection withb-LS
puts
more pressure on survival than methodscombining
ovulation rate andSeveral unresolved
problems
can bequoted:
(i)
The extent to which these conclusionsapply
to other situations andspecies
such asmice,
rabbits andpigs.
(ii)
Theinterpretation
ofbreeding
value for litter size and how to combine information from ovulation rate andprenatal
survival in anoptimal
way.(iii)
Ananalytical approach
topredict
response to selection with this modelalong
the lines ofFoulley
(1992)
would behighly
desirable.(iv)
Theimplications
of more realisticgenetic models,
ie the influence of different distributions of gene effects andfrequencies
in a finite loci model.ACKNOWLEDGMENTS
We thank LLG Janss for
kindly providing
his program, and G Bolet and R Ponzoni foruseful comments. The senior author
gratefully acknowledges
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937-949APPENDIX
Genetic evaluation for 1 continuous and 1
binary
trait when there are several observations of thebinary
variable per record of the continuous traitSuppose
that the number of ova shed is nl+no,
with nlembryos
that survive(litter
size =n
l
)
and noembryos
that do not. Ovulation rate is considered as a continuous trait andprenatal
survival as a dichotomous trait. There are nl + no observations of thebinary
trait for each ovulation record.Breeding
values for ovulation rate andembryo
survival can be estimatedby solving
until convergence asystem
ofequations
identical to
equation
[18]
in Janss andFoulley
(1993)
where theweighting
vector W isreplaced by
if both ovulation rate and litter size are observed or
if
only
litter size is recorded. Aboveand
where c’ is the conditional residual variance of