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initialize.R
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initialize.R
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# auxilliary function for dPLN pdf
R = function(x){
return((1-pnorm(x,0,1))/dnorm(x,0,1))
}
initialize = function(distribution, para1 = NULL, para2 = NULL,
N, range = NULL, K=1000, S_size){
if(distribution == "Normal"){
# Mean of normal distribution
mu = para1
# Standard deviation of normal distribution
stdv = para2
# Interval of utility values to be considered
interval = c(0,0)
# Since the density out here is almost zero.
interval[1] = mu - 5.8*stdv
interval[2] = mu + 5.8*stdv
# Sample from the utility distribution
sample_uN = matrix(rnorm(S_size*(N), mean = mu, sd = stdv), ncol=N)
# density of utility distribution
f = function(u){
return(dnorm(u,mu,stdv))
}
# CDF of utility distribution
F = function(u){
return(pnorm(u,mu,stdv))
}
# quantile function
Qt = function(p){
return(qnorm(p, para1, para2))
}
sampler = function(n, p=NA, lower.tail=TRUE){
if (is.na(p))
return(rnorm(n, mu, stdv))
if (lower.tail){
vals = runif(n, min=0, max=p)
return(Qt(vals))
}
vals = runif(n, min=p, max=1)
return(Qt(vals))
}
limiting = 0
if (mu != 0){
limiting = uniroot(function(q){return(q-N*pnorm(-N* mu*q, mean=mu, sd=stdv))},
interval=c(0, 1))$root
}
}
if(distribution == "Beta"){
# parameters of Beta distribution
a = para1
b = para2
# change location and scale of the density
interval = range
location = interval[1]
scale = interval[2]-location
# Sample from the utility distribution
sample_uN = matrix(rpearsonI(S_size*(N),a = a,b=b,location = location, scale = scale), ncol=N)
# mean for Pearson Type 1
mu = (a / (a + b))*(scale) + location
# variance
var = ((a * b)*scale^2) / ((a + b)^2 * (a + b + 1))
# standard deviation
stdv = sqrt(var)
# density for u ~ PearsonI(a,b,l,s)
f = function(u)
{
return(dpearsonI(u,a,b,location,scale))
}
# CDF for u ~ PearsonI(a,b,l,s)
F = function(u)
{
return(ppearsonI(u,a,b,location,scale))
}
Qt = function(p){
return(bisection(function(x){ return(F(x) - p)},
lower=interval[1], upper=0, tolerance=.Machine$double.eps^0.75)$mid)
}
sampler = function(n, p=NA, lower.tail=TRUE){
if (is.na(p))
return(rpearsonI(n,a = a,b=b,location = location, scale = scale))
if (lower.tail){
vals = runif(n, min=0, max=p)
return(Qt(vals))
}
vals = runif(n, min=p, max=1)
return(Qt(vals))
}
limiting = -interval[1] / (mu * (N-1))
}
if(distribution == "Uniform"){
# sample from utility distribution
sample_uN = matrix(runif(S_size*(N), range[1],range[2]), ncol=N)
# bounds of uniform distribution
interval = range
# mean and standard deviation of uniform distribution
mu = .5 * (range[1] + range[2])
stdv = (range[2] - range[1]) / (sqrt(12))
# Uniform density
f = function(u){
if(u < range[1])
return(0)
if(u > range[2])
return(0)
return(dunif(u,range[1],range[2]))
}
# Uniform CDF
F = function(u){
if(u < range[1])
return(0)
if(u > range[2])
return(1)
return(punif(u,range[1],range[2]))
}
# quantile function
Qt = function(p){
return(qunif(p, range[1], range[2]))
}
sampler = function(n, p=NA, lower.tail=TRUE){
if (is.na(p))
return(runif(n, range[1],range[2]))
if (lower.tail){
vals = runif(n, min=0, max=p)
return(Qt(vals))
}
vals = runif(n, min=p, max=1)
return(Qt(vals))
}
limiting = -interval[1] / (mu * (N-1))
}
### Simulation of 2008 Gay Marriage vote in California assuming uniform mixture components
if(distribution == "Mar"){
# mixture proportions
alpha1 = .616
alpha2 = .344
alpha3 = .033
alpha4 = .007
# against gay marriage
min_1 = -10000
max_1 = 0
# non-LGBT in favor of gay marriage
min_2 = 0
max_2 = 10000
# LGBT, single
min_3 = 5000
max_3 = 35000
# LGBT, couple
min_4 = 20000
max_4 = 180000
interval = c(1.5 * min_1, 1.5 * max_4)
# mean of utility distribution
mu = alpha1 * (.5 * (min_1 + max_1)) + alpha2 * (.5 * (min_2 + max_2)) + alpha3 * (.5 * (min_3 + max_3)) + alpha4 * (.5 * (min_4 + max_4))
# second moment of uniform distribution
sec_mom = function(a, b){
return((1/12) * (b - a)^2 + (.5 * (a + b))^2)
}
# mean squared
Mu2 = mu^2
# second moment of mixture
EX2 = alpha1 * sec_mom(min_1, max_1) + alpha2 * sec_mom(min_2, max_2) + alpha3 * sec_mom(min_3, max_3) + alpha4 * sec_mom(min_4, max_4)
# standard deviation of mixture
stdv = (EX2 - Mu2)^(1/2)
alphas = c(alpha1, alpha2, alpha3, alpha4)
mins = c(min_1, min_2, min_3, min_4)
maxs = c(max_1, max_2, max_3, max_4)
# draw from multinomial to get subpopulation counts
# in sample utility matrix
components = rmultinom(1, S_size * N, alphas)
# draw sample utility values
samp1 = runif(components[1],min_1, max_1)
samp2 = runif(components[2],min_2, max_2)
samp3 = runif(components[3],min_3, max_3)
samp4 = runif(components[4],min_4, max_4)
full_mat = c(samp1, samp2, samp3, samp4)
# jumble and store in matrix
sample_uN = matrix(sample(full_mat), ncol=N)
# CDF restricted to people against gay marriage
# used when adjusting movement in the discontinuity point
# between periods
F = function(x){
return(alpha1*punif(x, min_1, max_1))
}
# pdf restricted to people against gay marriage
# used when adjusting movement in the discontinuity point
# between periods
f = function(x){
return(alpha1*dunif(x, min_1, max_1))
}
# Quantile function
Qt = function(p){
return(bisection(function(x){ return(F(x) - p)},
lower=interval[1], upper=0, tolerance=.Machine$double.eps^0.75)$mid)
}
# function to sample from the distribution
sampler = function(n, p=NA, lower.tail=TRUE){
if (is.na(p)){
return(sample(full_mat, n, replace=TRUE))
}
# if there's a discontinuity then only sample from the extremist mass
if (lower.tail){
vals = runif(n, min=0, max=p)
return(Qt(vals))
}
return(sample(full_mat[full_mat > Qt(p)], n, replace=TRUE))
}
Limiting = -min_1 / (mu * (N-1))
}
### Simulation of 2008 Gay Marriage vote in California assuming dPLN distributed mixture components
if (distribution == "dPLN"){
# dPLN parameters fit to US Income Distribution
a = 3 # upper tail index
b = 1.43 # lower tail index
s = 0.45 # ~ sd of log-income
# Mixture proportions
# against
alpha1 = .52
# non-LGBT, in favor
alpha2 = .44
# LGBT, single
alpha3 = .033
# LGBT, couple
alpha4 = .007
alphas = c(alpha1, alpha2, alpha3, alpha4)
# mean willingness to pay for non-LGBT
mean1 = 5000
# mean for LGBT, single
mean2 = 20000
# mean for LGBT, couple
mean3 = 100000
m1=log(mean1)-log(((a*b)/((a-1)*(b+1))))-(s^2)/2 # parameter for voters for prop 8
m2=log(mean1)-log(((a*b)/((a-1)*(b+1))))-(s^2)/2 # parameter for non-LGBT against prop 8
m3=log(mean2)-log(((a*b)/((a-1)*(b+1))))-(s^2)/2 # parameter for LGBT, single
m4=log(mean3)-log(((a*b)/((a-1)*(b+1))))-(s^2)/2 # parameter for LGBT, couple
# vector of parameters
mvec=rep(0,4)
mvec[1] = m1
mvec[2] = m2
mvec[3] = m3
mvec[4] = m4
#pdf for double pareto log-normal of subpop n
f_dpln = function(w,n){
m=mvec[n]
if(n>1){
z=w
} else {
z=-w
}
z[z<=0] = 1
t1 = (a*b)/((a+b)*z)
t2 = dnorm((log(z)-m)/s,0,1)
r1 = R(a*s - (log(z)-m)/s)
r2 = R(b*s + (log(z)-m)/s)
out = t1*t2*(r1+r2)
out[z==1] = 0
return(out)
}
#CDF for double pareto log-normal
F_dpln = function(w,n){
vv = w
vv[vv<=0] = 1
m=mvec[n]
t1 = pnorm((log(vv)-m)/s,0,1)
t2 = dnorm((log(vv)-m)/s,0,1)
x1 = a*s - (log(vv)-m)/s
x2 = b*s + (log(vv)-m)/s
t3 = (b*R(x1)-a*R(x2))/(a+b)
out = (t1-t2*t3)
out[w<=0] = 0
return(out)
}
##### appropriate proposal gamma distributions for each subpopulation
### parameters of gamma distribution
### same shape for those in favor of proposition 8 and non-LGBT opposed
al2 = 1.05
be2 = (al2-1)/2602.603
M2 = 9.7
### parameters of gamma distribution
### LGBT single voters
al3 = 1.025
be3 = (al3-1)/10410.41
M3 = 18
### parameters of gamma distribution
### LGBT couples
al4 = 1.025
be4 = (al4-1)/52052.05
M4 = 18
# vectors of parameters
alps = c(0,al2,al3,al4)
bets = c(0,be2,be3,be4)
Ms = c(0,M2,M3,M4)
### vectorized rejection sampling algorithm for dPLN
# bign is the number of observations to draw
# n is the subpopulation
# note the proposal distribution is less than the dPLN density at the far end of the
# fat tail. We sought to make the mass of that region sufficiently small to be
# negligible.
rejection = function(bign,n){
# for voters against gay marriage draw from the same
# distributions as moderates in favor, flip signs.
if(n==1){return(-rejection(bign,2))}
# valid values drawn so far
curr_samp = c()
# values still needed
vals_left = bign
# proposal distribution parameters
al = alps[n]
be = bets[n]
M = Ms[n]
# keep drawing until you get full sample of values
while(vals_left > 0){
u = runif(vals_left, 0, 1)
# draw from proposal distribution
g = rgamma(vals_left, al, be)
# get rescaled height under curve
M_vals = M * dgamma(g, al, be)
# get height under curve for dPLN
f_vals = f_dpln(g, n)
# keep if sampled point under the dPLN curve
accept = (u < (f_vals / M_vals))
# set all rejected values to 0
accept_samp = accept * g
# add accepted values to sample
curr_samp = c(curr_samp, accept_samp[accept_samp != 0])
vals_left = bign - length(curr_samp)
}
return(curr_samp)
}
# draw from multinomial to get subpopulation counts
# in sample utility matrix
components = rmultinom(1, S_size * N, alphas)
if ("sample_matrix_dpln.csv" %in% list.files()){
full_samp = as.vector(as.matrix(read.csv("sample_matrix_dpln.csv")))
full_samp = full_samp[1:(S_size * N)]
}
else{
# draw sample utility values
samp1 = rejection(components[1],1) # against prop 8
samp2 = rejection(components[2],2) # for prop 8 non-LGBT
samp3 = rejection(components[3],3) # LGBT single
samp4 = rejection(components[4],4) # LGBT couple
full_samp = c(samp1, samp2, samp3, samp4)
}
# mean for mixture
mu = (alpha2 - alpha1) * mean1 + alpha3 * mean2 + alpha4 * mean3
# variance
sigma2 = var(full_samp)
# estimated standard deviation
stdv = sqrt(sigma2)
# CDF restricted to people against gay marriage
# used when adjusting movement in the discontinuity point
# between periods
F = function(x){
return(alpha1*(1-F_dpln(-x,2)))
}
# pdf restricted to people against gay marriage
# used when adjusting movement in the discontinuity point
# between periods
f = function(x){
return(alpha1*(f_dpln(-x,2)))
}
# quantile for double pareto log-normal
Qt = function(p){
tf = function(y){return(F(y)-p)}
rt = bisection(tf,lower=-10^8, upper=0, tolerance=.Machine$double.eps^0.75)
return(rt$mid)
}
# bounds for utility grid
interval = c(1.05 * min(full_samp), 1.05 * max(full_samp))
# merge together and shuffle up the utility values for each
# subpopulation. convert to a matrix.
sample_uN = matrix(full_samp, ncol=N)
# sample from distribution
sampler = function(n, p=NA, lower.tail=TRUE){
if (is.na(p)){
return(sample(full_samp, n, replace=TRUE))
}
if (lower.tail){
vals = runif(n, min=0, max=p)
return(Qt(vals))
}
return(sample(full_samp[full_samp > Qt(p)], n, replace=TRUE))
}
# limiting constant
k.k = (F(-1000000)/alpha1) / 1000000^-a
# constant / sqrt(N) for limiting
limiting = k.k^(1/(1 + a)) * ((1/mu) + (1/(mu*a)))^(a/(1+a)) / sqrt(N)
}
if (distribution == "uDPLN"){
# dPLN parameters fit to US Income Distribution
a = 3 # upper tail index
b = 1.43 # lower tail index
s = 0.45 # ~ sd of log-income
# uniform distribution parameters
range = c(-5000,0)
# Mixture proportions
# uniform
alpha1 = .5
# dPLN
alpha2 = .5
alphas = c(alpha1, alpha2)
# mean for dPLN
mean1 = (para1 - (alpha2 * -2500)) / alpha1
m1=log(mean1)-log(((a*b)/((a-1)*(b+1))))-(s^2)/2
#pdf for double pareto log-normal of subpop n
f_dpln = function(w){
m=m1
z=w
z[z<=0] = 1
t1 = (a*b)/((a+b)*z)
t2 = dnorm((log(z)-m)/s,0,1)
r1 = R(a*s - (log(z)-m)/s)
r2 = R(b*s + (log(z)-m)/s)
out = t1*t2*(r1+r2)
out[z==1] = 0
return(out)
}
#CDF for double pareto log-normal
F_dpln = function(w){
vv = w
vv[w<=0] = 1
m=m1
t1 = pnorm((log(vv)-m)/s,0,1)
t2 = dnorm((log(vv)-m)/s,0,1)
x1 = a*s - (log(vv)-m)/s
x2 = b*s + (log(vv)-m)/s
t3 = (b*R(x1)-a*R(x2))/(a+b)
out = t1-t2*t3
out[w<=0] = 0
return(out)
}
al1 = 1.05
be1 = (al1-1)/2602.603
# find multiplier of Gamma distribution that makes it twice as tall
# as DPLN at DPLN mode
modevals = optimize(function(x){return(-f_dpln(x))}, c(1, mean1))
M1 = -2 * modevals$objective / dgamma(modevals$minimum, al1, be1)
rejection = function(bign){
curr_samp = c()
# values still needed
vals_left = bign
# proposal distribution parameters
al = al1
be = be1
M = M1
# keep drawing until you get full sample of values
while(vals_left > 0){
u = runif(vals_left, 0, 1)
# draw from proposal distribution
g = rgamma(vals_left, al, be)
# get rescaled height under curve
M_vals = M * dgamma(g, al, be)
# get height under curve for dPLN
f_vals = f_dpln(g)
# keep if sampled point under the dPLN curve
accept = (u < (f_vals / M_vals))
# set all rejected values to 0
accept_samp = accept * g
# add accepted values to sample
curr_samp = c(curr_samp, accept_samp[accept_samp != 0])
vals_left = bign - length(curr_samp)
}
return(curr_samp)
}
# draw from multinomial to get subpopulation counts
# in sample utility matrix
components = rmultinom(1, S_size * N, alphas)
samp1 = rejection(components[1])
# estimated second moment of utility distribution for non-LGBT
secmom1 = var(samp1) + mean1^2
# sample from utility distribution
samp2 = runif(components[2], range[1],range[2])
# mean and standard deviation of uniform distribution
mean2 = .5 * (range[1] + range[2])
secmom2 = mean2^2 + (range[2] - range[1])^2 / 12
# mean for mixture
mu = alpha1 * mean1 + alpha2 * mean2
# estimated second moment for mixture
secmom = alpha1 * secmom1 + alpha2 * secmom2
stdv = sqrt(secmom - mu^2)
# Uniform density
f = function(u){
if(u < range[1])
return(0)
if(u > range[2])
return(0)
return(alpha1*dunif(u,range[1],range[2]))
}
# Uniform CDF
F = function(u){
if(u < range[1])
return(0)
if(u > range[2])
return(1)
return(alpha1*punif(u,range[1],range[2]))
}
# quantile function
Qt = function(p){
return(qunif(p / alpha1, range[1], range[2]))
}
min_1 = min(samp1)
max_1 = max(samp1)
# bounds for utility grid
interval = c(range[1], 1.05 * max(max_1, range[2]))
full_samp = c(samp1, samp2)
# merge together and shuffle up the utility values for each
# subpopulation. convert to a matrix.
sample_uN = matrix(sample(full_samp), ncol=N)
sampler = function(n, p=NA, lower.tail=TRUE){
if (is.na(p)){
return(sample(full_samp, n, replace=TRUE))
}
if (lower.tail){
vals = runif(n, min=0, max=p)
return(Qt(vals))
}
return(sample(full_samp[full_samp > Qt(p)], n, replace=TRUE))
}
limiting = -interval[1] / (mu * (N-1))
}
if (distribution == "DPLNu"){
a = para2
#a = 3 # upper tail index
b = 1.43 # lower tail index
s = 0.45 # ~ sd of log-income
# uniform distribution parameters
range = c(0,10000)
# Mixture proportions
# uniform
alpha1 = .5
# dPLN
alpha2 = .5
alphas = c(alpha1, alpha2)
# mean for dPLN
mean1 = (para1 - (alpha2 * 5000)) / alpha1
mmean1 = -mean1
m1=log(mmean1)-log(((a*b)/((a-1)*(b+1))))-(s^2)/2
#pdf for double pareto log-normal of subpop n
f_dpln = function(w){
m=m1
z=-w
z[z<=0] = 1
t1 = (a*b)/((a+b)*z)
t2 = dnorm((log(z)-m)/s,0,1)
r1 = R(a*s - (log(z)-m)/s)
r2 = R(b*s + (log(z)-m)/s)
out = t1*t2*(r1+r2)
out[z==1] = 0
return(out)
}
#CDF for double pareto log-normal
F_dpln = function(w){
vv = -w
vv[vv<=0] = 1
m=m1
t1 = pnorm((log(vv)-m)/s,0,1)
t2 = dnorm((log(vv)-m)/s,0,1)
x1 = a*s - (log(vv)-m)/s
x2 = b*s + (log(vv)-m)/s
t3 = (b*R(x1)-a*R(x2))/(a+b)
out = 1 - (t1-t2*t3)
out[vv<=0] = 0
return(out)
}
modevals = optimize(function(x){return(-f_dpln(x))}, c(mean1, -1))
al1 = 1.05
be1 = (al1-1)/2602.603
# find multiplier of Gamma distribution that makes it twice as tall
# as DPLN at DPLN mode
M1 = -2 * modevals$objective / dgamma(-modevals$minimum, al1, be1)
rejection = function(bign){
# for voters against gay marriage draw from the same
# distributions as moderates in favor, flip signs.
# valid values drawn so far
curr_samp = c()
# values still needed
vals_left = bign
# proposal distribution parameters
al = al1
be = be1
M = M1
# keep drawing until you get full sample of values
while(vals_left > 0){
u = runif(vals_left, 0, 1)
# draw from proposal distribution
g = rgamma(vals_left, al, be)
# get rescaled height under curve
M_vals = M * dgamma(g, al, be)
# get height under curve for dPLN
f_vals = f_dpln(-g)
# keep if sampled point under the dPLN curve
accept = (u < (f_vals / M_vals))
# set all rejected values to 0
accept_samp = accept * g
# add accepted values to sample
curr_samp = c(curr_samp, accept_samp[accept_samp != 0])
vals_left = bign - length(curr_samp)
}
return(-curr_samp)
}
# draw from multinomial to get subpopulation counts
# in sample utility matrix
components = rmultinom(1, S_size * N, alphas)
samp1 = rejection(components[1])
# estimated second moment of utility distribution for non-LGBT
secmom1 = var(samp1) + mean1^2
# sample from utility distribution
samp2 = runif(components[2], range[1],range[2])
# mean and standard deviation of uniform distribution
mean2 = .5 * (range[1] + range[2])
secmom2 = mean2^2 + (range[2] - range[1])^2 / 12
# mean for mixture
mu = alpha1 * mean1 + alpha2 * mean2
# estimated second moment for mixture
secmom = alpha1 * secmom1 + alpha2 * secmom2
stdv = sqrt(secmom - mu^2)
# CDF restricted to people against gay marriage
# used when adjusting movement in the discontinuity point
# between periods
F = function(x){
return(alpha1*F_dpln(x))
}
# pdf restricted to people against gay marriage
# used when adjusting movement in the discontinuity point
# between periods
f = function(x){
return(alpha1*(f_dpln(x)))
}
# quantile for double pareto log-normal
Qt = function(p){
tf = function(y){return(F(y)-p)}
rt = bisection(tf,lower=-10^8, upper=0, tolerance=.Machine$double.eps^0.75)
return(rt$mid)
}
min_1 = min(samp1)
max_1 = max(samp1)
# bounds for utility grid
interval = c(1.05*min_1, 1.05*range[2])
full_samp = c(samp1, samp2)
# merge together and shuffle up the utility values for each
# subpopulation. convert to a matrix.
sample_uN = matrix(sample(full_samp), ncol=N)
sampler = function(n, p=NA, lower.tail=TRUE){
if (is.na(p)){
return(sample(full_samp, n, replace=TRUE))
}
if (lower.tail){
vals = runif(n, min=0, max=p)
return(Qt(vals))
}
return(sample(full_samp[full_samp > Qt(p)], n, replace=TRUE))
}
k.k = (F(-1000000)/alpha1) / 1000000^-a
# constant / sqrt(N) for limiting
limiting = k.k^(1/(1 + a)) * ((1/mu) + (1/(mu*a)))^(a/(1+a)) / sqrt(N)
}
if (distribution == "Laplace"){
m = para1
s = para2
# Mean of normal distribution
mu = para1
# Standard deviation of normal distribution
stdv = sqrt(2) * para2
# Interval of utility values to be considered
interval = c(0,0)
# Since the density 3 standard deviations away is almost zero.
interval[1] = mu - 5.8*stdv
interval[2] = mu + 5.8*stdv
# Sample from the utility distribution
sample_uN = matrix(rlaplace(S_size*(N), m=m, s=s), ncol=N)
# density of utility distribution
f = function(u){
return(dlaplace(u,m,s))
}
# CDF of utility distribution
F = function(u){
return(plaplace(u,m,s))
}
# quantile function
Qt = function(p){
return(qlaplace(p, m, s))
}
sampler = function(n, p=NA, lower.tail=TRUE){
if (is.na(p))
return(rlaplace(n, m, s))
if (lower.tail){
vals = runif(n, min=0, max=p)
return(Qt(vals))
}
vals = runif(n, min=p, max=1)
return(Qt(vals))
}
# don't know what the limiting inefficiency is
limiting = 0
}
if (distribution == "DPLN2"){
a1 = para1
a2 = para2
as = c(a1,a2)
b = 1.43 # lower tail index
s = 0.45 # ~ sd of log-income
# Mixture proportions
# uniform
alpha1 = .5
# dPLN
alpha2 = .5
alphas = c(alpha1, alpha2)
# mean for dPLN
mean1 = -3000
mmean1 = -mean1
mean2 = 5000
m1=log(mmean1)-log(((a1*b)/((a1-1)*(b+1))))-(s^2)/2
m2=log(mean2)-log(((a2*b)/((a2-1)*(b+1))))-(s^2)/2
mvec = c(m1, m2)
#pdf for double pareto log-normal of subpop n
f_dpln = function(w, n){
m=mvec[n]
a=as[n]
if (n > 1){
z = w
}
else {
z = -w
}
z[z<=0] = 1
t1 = (a*b)/((a+b)*z)
t2 = dnorm((log(z)-m)/s,0,1)
r1 = R(a*s - (log(z)-m)/s)
r2 = R(b*s + (log(z)-m)/s)
out = t1*t2*(r1+r2)
out[z==1] = 0
return(out)
}
#CDF for double pareto log-normal
F_dpln = function(w, n){
if (n == 1){
vv = -w
}
else{
vv = w
}
vv[vv<=0] = 1
a = as[n]
m = mvec[n]
t1 = pnorm((log(vv)-m)/s,0,1)
t2 = dnorm((log(vv)-m)/s,0,1)
x1 = a*s - (log(vv)-m)/s
x2 = b*s + (log(vv)-m)/s
t3 = (b*R(x1)-a*R(x2))/(a+b)
out = (t1-t2*t3)
out[vv==1] = 0
if (n == 1)
return(1 - out)
return(out)
}
## find mode of density function. used to find appropriate
## multiplier for proposal gamma distribution.
modevals1 = optimize(function(x){return(-f_dpln(x, 1))}, c(mean1, -1))
al1 = 1.05
be1 = (al1-1)/2602.603
# M1 * gamma / dpln = 2 at mode
M1 = -2 * modevals1$objective / dgamma(-modevals1$minimum, al1, be1)
modevals2 = optimize(function(x){return(-f_dpln(x, 2))}, c(1, mean2))
al1 = 1.05
be1 = (al1-1)/2602.603
M2 = -2 * modevals2$objective / dgamma(modevals2$minimum, al1, be1)
Ms = c(M1, M2)
rejection = function(bign, n){
# valid values drawn so far
curr_samp = c()
# values still needed
vals_left = bign
# proposal distribution parameters
al = al1
be = be1
M = Ms[n]
# keep drawing until you get full sample of values
while(vals_left > 0){
u = runif(vals_left, 0, 1)
# draw from proposal distribution
g = rgamma(vals_left, al, be)
# get rescaled height under curve
M_vals = M * dgamma(g, al, be)
if(n == 1){
g=-g
}
# get height under curve for dPLN
f_vals = f_dpln(g, n)
# keep if sampled point under the dPLN curve
accept = (u < (f_vals / M_vals))
# set all rejected values to 0
accept_samp = accept * g
accept_samp[is.na(accept_samp)] = 0
# add accepted values to sample
curr_samp = c(curr_samp, accept_samp[accept_samp != 0])
vals_left = bign - length(curr_samp)
}
return(curr_samp)
}
# draw from multinomial to get subpopulation counts
# in sample utility matrix
components = rmultinom(1, S_size * N, alphas)
samp1 = rejection(components[1], 1)
samp2 = rejection(components[2], 2)
full_samp = c(samp1, samp2)
# mean for mixture
mu = alpha1 * mean1 + alpha2 * mean2
var_dpln = function(a, b, s, v){
p1 = (a * b * exp(2*v + s^2)) / ((a - 1)^2 * (b + 1)^2)
p2 = (((a - 1)^2 * (b + 1)^2) / ((a - 2) * (b + 2))) * exp(t^2)
p3 = a * b
return(p1 * (p2 - p3))