J Seismol
https://doi.org/10.1007/s10950-017-9713-x
ORIGINAL ARTICLE
Risk-targeted maps for Romania
Radu Vacareanu & Florin Pavel & Ionut Craciun &
Veronica Coliba & Cristian Arion & Alexandru Aldea &
Cristian Neagu
Received: 14 February 2017 / Accepted: 3 November 2017
# Springer Science+Business Media B.V., part of Springer Nature 2017
Abstract Romania has one of the highest seismic hazard levels in Europe. The seismic hazard is due to a
combination of local crustal seismic sources, situated
mainly in the western part of the country and the
Vrancea intermediate-depth seismic source, which can
be found at the bend of the Carpathian Mountains.
Recent seismic hazard studies have shown that there
are consistent differences between the slopes of the
seismic hazard curves for sites situated in the fore-arc
and back-arc of the Carpathian Mountains. Consequently, in this study we extend this finding to the evaluation
of the probability of collapse of buildings and finally to
the development of uniform risk-targeted maps. The
main advantage of uniform risk approach is that the
target probability of collapse will be uniform throughout
the country. Finally, the results obtained are discussed in
the light of a recent study with the same focus performed
at European level using the hazard data from SHARE
project. The analyses performed in this study have
pointed out to a dominant influence of the quantile of
peak ground acceleration used for anchoring the fragility function. This parameter basically alters the shape of
the risk-targeted maps shifting the areas which have
higher collapse probabilities from eastern Romania to
western Romania, as its exceedance probability
R. Vacareanu : F. Pavel (*) : I. Craciun : V. Coliba :
C. Arion : A. Aldea : C. Neagu
Seismic Risk Assessment Research Center, Technical University
of Civil Engineering Bucharest, Bd. LaculTei, no. 122-124, Sector
2, 020396 Bucharest, Romania
e-mail: florin.pavel@utcb.ro
increases. Consequently, a uniform procedure for deriving risk-targeted maps appears as more than necessary.
Keywords Seismic hazard . Fragility curves .
Probability of collapse . Share . Uncertainty
1 Introduction
The Romanian seismic design code P100-1/2013 (2014),
enforced since January 2014, estimates the design peak
ground acceleration (for the life safety ultimate limit
state—ULS) for a mean return period of 225 years (20%
probability of exceedance in 50 years). This mean return
period represents an intermediary step before moving to
the mean return period of 475 years, recommended by EN
1998-1 (Eurocode 8). It also has to be emphasized the fact
that the mean return period associated with the design
peak ground acceleration has increased ever since the
1992 version of the Romanian seismic code. The 1992
version of the code had a mean return period of 50 years,
which increased to 100 years in the 2006 version of the
code before moving to 225 years in the current version.
Significant differences in terms of both seismic hazard levels and slopes for the seismic hazard curves (k
parameter in Eurocode 8) have been noticed between the
study of Pavel et al. (2016), denoted hereinafter as
BIGSEES model, and Woessner et al. (2015), denoted
hereinafter as SHARE model. The first main reason for
the observed differences are the different soil conditions
employed in the two models; while SHARE model uses
as reference rock conditions, the BIGSEES model
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employs as reference the soil conditions derived through
the topographic slope method proposed by Wald and
Allen (2007). The second reason is related to the different ground motion prediction equations (GMPEs) used
in the two studies. One of the two GMPEs used in the
SHARE model, namely the Lin and Lee (2008) GMPE,
was tested using a collection of ground motion recordings from Vrancea earthquakes and was found to consistently underestimate the observed ground motions
(Vacareanu et al. 2013). A third reason which might also
explain the differences is related to the SHARE modeling of the Vrancea subcrustal seismic source, which
covers an area roughly 15 times its actual size; in addition, the earthquake occurrence rates used in the
SHARE model underestimate the observed seismicity.
Concerns regarding the SHARE seismic source models
have also been raised by Zimmaro and Stewart (2017).
Recently, Silva et al. (2016) have developed risktargeted maps for Europe using the seismic hazard results obtained in the SHARE project. Their analysis
shows that most of Romania, namely the southern and
eastern parts (which are under the influence of the
Vrancea intermediate-depth seismic source), have a
quite low probability of collapse, similar with that from
countries with low seismicity, such as Sweden, Finland,
or Ireland. Consequently, the authors recommend a decrease of the seismic hazard levels for most of southern
and eastern Romania and an increase for the sites situated towards the western part of the country. It is not the
intention of the authors to compare per se the seismic
risk results based on the SHARE and BIGSEES seismic
models. The comparison with the results of Siva et al. is
made just in broad terms and trends, highlighting opposite general conclusions regarding the seismic risk in the
front and in the back of the Carpathian Mountains.
In this context, in the present study, risk-targeted
maps are developed for Romania using as reference
the seismic hazard results obtained by Pavel et al.
(2016). Among other studies which have applied the
same methodologies (albeit with different input values),
one should mention the papers of Luco et al. (2007) for
the conterminous US, Douglas et al. (2013) for mainland France, or Vanzi et al. (2015) for Italy.
2 Calculation of risk-targeted maps
The most recent probabilistic seismic hazard assessment
for Romania performed by Pavel et al. (2016) employed
a logic-tree approach in order to account for the epistemic uncertainties. Three GMPEs were used in the logic
tree for the crustal seismic sources in Romania and six
GMPEs were employed for the Vrancea intermediatedepth seismic source (three for the sites situated in the
fore-arc region and three for the sites in the back-arc
region). The delineation between the fore-arc and backarc region was considered to be along eastern and southern sides of the Carpathian Mountains. In addition, the
uncertainties regarding the focal depths, maximum magnitudes and seismic activities rates were also accounted
for. The most important result of this analysis is represented by the uniform seismic hazard map for a mean
return period of 475 years, shown in the paper of Pavel
et al. (2016). The noticeable difference in terms of
slopes of the seismic hazard curves between fore-arc
and back-arc sites is highlighted in Fig. 1. The four sites
have basically the same peak ground acceleration for a
mean return period of 475 years, yet the slope of the
hazard curve is totally different. This difference can be
attributed to the much higher seismic activity rate of the
Vrancea intermediate-depth seismic source which affects mostly fore-arc sites, as compared to the lower
seismic activity rates for the crustal seismic sources
which affect mainly back-arc sites (situated in the western part of Romania). Consequently, it is to be expected
that the seismic risk in terms of failure probabilities will
differ significantly between these two zones. The model
on which probabilistic seismic hazard analysis (PSHA)
was accomplished in BIGSEES model is based on the
following assumptions: the seismicity model grounded
on the earthquakes catalogs from Romania, Bulgaria,
and Serbia, the GMPEs on soil conditions purposely
developed for Vrancea intermediate-depth seismic
source or tested against the database of strong ground
motions recorded in Romania and a logic tree taking
into account the epistemic uncertainties in terms of
maximum magnitude, focal depth, and goodness-of-fit
of GMPEs. Consequently, the results of PSHA in terms
of PGAs or spectral accelerations (SAs) are for ground
types A, B, and C, as they are defined in EN 1998-1.
Because detailed geophysical and geotechnical information, as requested for the definition of ground types in
EN 1998-1, are not available for all sites in Romania, the
soil conditions in BIGSEES model were largely based
on topography and enhanced with local relevant information, where available. The Romanian seismic design
code P100-1/2013 defines the local soil conditions in
terms of control periods TB and TC of design response
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spectrum. The code-based control periods are obtained
from the envelope of values calculated from strong
ground motions recorded during large earthquakes in
Romania. This decision of the Romanian code drafters
is based on the larger reliability of the control periods
values arising from actual ground motions than of the
values obtained from empirical correlations with geophysical and geotechnical values.
There are four input data to be considered in the
calculations for risk-targeted maps: the mean return
period of the ground motion parameter selected for the
analysis, the corresponding value of the quantile of the
fragility function of buildings, the standard deviation of
the lognormal distribution describing the fragility function, and the target annual probability of collapse/failure. One has to mention that collapse/failure is defined
as the exceedance of a given design limit state.
Both EN 1998-1 (2004) and Romanian seismic design code P100-1/2013 (2014) consider two performance levels for structural design, namely the damage
limitation limit state (which is a serviceability limit
state) and the life safety limit state (which is an ultimate
limit state). Neither EN 1998-1/2004 nor P100-1/2013
makes an explicit check of the no-collapse performance
objective. Thus, the assessment of the associated probability of collapse (collapse means exceedance of a limit
state) is one of the key issues of the risk-targeted approach. Luco et al. (2007) have proposed a collapse
probability of 10% associated to a ground motion parameter with mean return period of 2475 years. Goulet
et al. (2007) has computed failure probabilities in the
range 2–7% for the same mean return period of the
seismic action as used by Luco et al. (2007).On the
contrary, Ulrich et al. (2014) assigned annual failure
probabilities of the order 10−5…10−7 depending on the
seismic zone in which the structure is situated (lower
failure probabilities are assigned to the buildings built in
the zones with the lower seismic hazard). Fajfar and
Dolšek (2012) have computed annual failure probabilities of the order 10−4…10−5. Vanzi et al. (2015) have
used the same failure probability as the one assigned by
EN 1990 (Eurocode 0) for gravity loads, namely
1.3·10−6.
The second major issue is the assessment of the
variability inherent to the fragility curves (logarithmic
standard deviation β). In this aspect, too, there are
significant differences between the values used by various researchers. For instance, Luco et al. (2007) use a β
value of 0.8, while Douglas et al. (2013) employ a value
of 0.5. Silva et al. (2016) consider a standard deviation
of 0.6, while Vanzi et al. (2015) use a value of 0.2, which
is by far the lowest value encountered in all the studies
with this focus.
With regard to the actual calculation of the mean
annual frequency (MAF) of exceeding a given limit
state, there are also several approaches. Doulgas et al.
(2012) use the classic convolution products for the
computation of the annual failure probability, given by
Kennedy (2011):
þ∞
P F ¼ ∫ H A ðaÞ⋅
0
þ∞
P F ¼ − ∫ P F ja ⋅
0
dP F ja
da
da
ð1Þ
dHa ðaÞ
da
da
ð2Þ
where PFla is the fragility function (conditional cumulative distribution function of the probability of failure
given a ground motion value) and Ha(a) is the hazard
curve. Silva et al. (2016) have computed the annual
failure probability by dividing both the fragility curve
and the seismic hazard curve into segments and then
numerically integrating the distribution. On the contrary,
Vanzi et al. (2015) employed an approach based on the
approximation of the seismic hazard curve with a line
(in log-log space) and then computing numerically the
risk convolution integral. Under the Poisson assumption, there is a negligible difference between the values
of annual probability of collapse and MAF, since we are
targeting very low values.
In this study, the MAF of exceeding the life safety
limit state (LS) is obtained in the same manner as in
Douglas et al. (2013), through the convolution product
between the fragility function (expressed as probability
density function, PDF) and the MAF of exceeding various values of peak ground acceleration (representing
actually the seismic hazard curve), using Eq. 1. Alternatively, the MAF of exceeding a given LS can be
obtained by the convolution product between the fragility function (expressed as cumulative distribution function, CDF) and the first derivative of the seismic hazard
curve, using Eq. 2. In both situations, the fragility function is conditional upon the values of PGA, and represents the conditional probability of exceeding the given
LS as a function of PGA values. The fragility functions
are expressed as lognormal distributions with two parameters: the median value of PGA and the logarithmic
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Fig. 1 Comparison of seismic
hazard curves for fore-arc and
back-arc sites
standard deviation of PGA (parameter β).Subsequently,
the peak ground acceleration for various mean return
periods are extracted from the seismic hazard curves for
the same 200 sites analyzed by Pavel et al. (2016). The
extracted peak ground accelerations shall be considered
as an inferior fractile (quantile) of the lognormal distribution, say p quantile. This means that there is a p
probability that the exceedance of the life safety LS is
encountered for PGA values lower than the design value, and 1-p probability that the exceedance will be
reached for higher PGA values. Considering the p value
of PGA quantile and using the properties of the lognormal distribution, we obtain the median value of PGA for
the fragility curve describing the probability of exceedance of life safety LS conditional upon PGA values.
Then, we proceed to the calculation of the convolution
integral and we obtain the MAF of failure. If one considers that the probability distribution of failure is of
Poisson type (and this is reasonable since failure is a rare
and independent event for any given year), using the
values obtained for MAF we obtain the annual probability of failure. Conversely, one can impose a target
MAF of exceedance of life safety limit LS and then use
the convolution integral to iterate for the median value
of PGA that produce the appropriate fragility function.
Once the median value is obtained, using the properties
of the lognormal distribution of probability, one can
obtain the p quantile value of PGA that becomes the
design value for the site given the target MAF of exceedance of life safety LS.
The influence of the slope of the seismic hazard curve
on the annual probability of collapse is visually represented in Fig. 2. The two cities selected, Bucharest and
Timisoara, are mostly influenced by the Vrancea
intermediate-depth seismic source, respectively, by local
shallow seismic sources, producing more abrupt, respectively, less abrupt slopes. The area under the red curve in
Fig. 2 evaluates the annual probability of collapse and
one can notice that steeper the slope towards larger PGA
values, higher the area enclosed by the risk curve.
3 Results for Romania
The risk-targeted maps for Romania are developed
taking into consideration the combination of target annual collapse probabilities and standard deviations
proposed by both Luco et al. (2007) and Silva et al.
(2016). Several sets of maps were created in order to
evaluate the influence of three key input parameters,
namely the value of peak ground acceleration, the standard deviation β, and the quantile of the lognormal
distribution (describing the fragility function) to which
the peak ground acceleration was assigned to.
The first four maps presented in Fig. 3 (left and right)
and Fig. 4 (left and right) show the peak ground accelerations corresponding to a collapse probability of
2·10−4. The accelerations were computed for β = 0.6
and β = 0.8 and using a quantile of either 0.001 or 0.1
as used by Silva et al. (2016) and Luco et al. (2007). The
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Fig. 2 Calculation of convolution integral using relation (2) for Bucharest (left) and Timisoara (right)
main observations regarding the four abovementioned
figures are:
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The overall shape of the map does not appear to
change with either of the two variable parameters (β
and quantile);
The corresponding peak ground accelerations for a
given collapse probability increase with the value of
the standard deviation (this increase is more visible
in the case of 0.1 quantile);
Just by changing the quantile from 0.001 to 0.1, the
resulting peak ground accelerations increase by at
least three times (the change of β produces a variation of less than 20%);
The overall shape of the map does appear to resemble that of the uniform hazard map shown in Pavel
et al. (2016).
In the subsequent step of the analysis, we compute
the ratio between the peak ground accelerations for a
mean return period of 475 years (uniform hazard values)
and those corresponding to a collapse probability of
2·10−4, β = 0.8 and 0.1 or 0.001 quantiles. The resulting
maps are shown in Fig. 5 (left and right). It is to be noted
that the range of the computed ratios is generally below
0.5–0.6 for the 0.1 quantile, while in the case of the
0.001 quantile, the ratio is above unity, thus meaning
that the amplitudes resulting from the seismic hazard
analysis are superior to the ones based on the uniform
risk approach. The difference between the results produced by employing the two quantiles is again very
large.
Next, we evaluated the collapse probabilities corresponding to two mean return periods of the PGA, namely 475 and 2475 years. For both return periods, the
Fig. 3 Peak ground accelerations corresponding to a collapse probability = 2·10−4, β = 0.6 and 0.001 quantile (left) and PGA corresponding
to a collapse probability = 2·10−4, β = 0.8 and 0.001 quantile (right)
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Fig. 4 Peak ground accelerations corresponding to a collapse probability = 2·10−4, β = 0.6 and 0.1 quantile (left) and PGA corresponding to
a collapse probability = 2·10−4, β = 0.8 and 0.1 quantile (right)
standard deviation was taken as 0.6 and 0.8, while the
quantile values considered were 0.1 and 0.001. Figure 6
(left and right) shows the results for the 475 years mean
return period, while Fig. 7 (left and right) displays the
values obtained for the mean return period of 2475 years.
The results obtained show a completely distinct pattern
of the computed collapse probability. In the case of the
0.001 quantile, the largest collapse probabilities are
encountered for the western part of the country which
is not under the direct influence of the Vrancea
intermediate-depth seismic source. On the contrary, in
the case of the 0.1 quantile, the largest collapse probabilities are encountered in the eastern part of Romania,
and more specifically in the area which has the highest
level of seismic hazard (area under the direct influence
of the Vrancea intermediate-depth seismic source). It is
intuitive to assume that the collapse probability is larger
for sites situated in the eastern part of the country and
thus the opposite results obtained when using a different
quantile raise some questions regarding the methodology. Similar contradictory results were also obtained for
Romania by Silva et al. (2016); however, this result was
not discussed in their paper.
The final analysis is performed for the following
combination of values of the input parameters: the value
of the logarithmic standard deviation β is 0.6, same as in
Luco et al. (2007) for conterminous US and in Silva
et al. (2016) for Europe; the PGA values from hazard
curves with 2% exceedance probability in 50 years (2%/
50 yrs.) are considered as 0.1 quantile of the lognormal
fragility curves. The target annual probability of
collapse/failure (i.e., the target annual probability of
exceedance of collapse prevention limit state), that is
associated with the hazard level expressed as 2%/
Fig. 5 Ratio between PGA for uniform seismic hazard (mean
return period of 475 years) and for uniform seismic risk (collapse
probability = 2·10−4, β = 0.8 and 0.1 quantile) (left) and ratio
between PGA for uniform seismic hazard (mean return period of
475 years) and for uniform seismic risk (collapse probability =
2·10−4, β = 0.8 and 0.001 quantile) (right)
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Fig. 6 Probability of collapse for the PGA corresponding to a mean return period of 475 years, β = 0.6 and 0.001 quantile (left) and
probability of collapse for the PGA corresponding to a mean return period of 475 years, β = 0.6 and 0.1 quantile (right)
50 years PGA values, is set to 2·10−4 (as in Luco et al.
2007) and 5·10−4. The reason for targeting 5·10−4annual
probability of collapse is to maintain, in the epicentral
area of Vrancea intermediate-depth seismic source, design values of PGA equal to the ones corresponding to
2%/50 years (see Fig. 8).
The uniform seismic hazard map for a mean return
period of 2475 years, corresponding to a probability of
exceedance of 2% in 50 years, is displayed in Fig. 8
(left) and that for a uniform risk (for a target annual
collapse probability of 5·10−4 associated with PGA
values with 2%/50 years) is displayed in Fig. 8 (right).
One can notice that the uniform risk based PGA values
are lower than the uniform hazard based PGA values, as
the influence of Vrancea intermediate-depth seismic
source is fading away and the crustal seismic sources
control the hazard.
In Figs. 9, 10, and 11, the ratios of PGA values with
225, 475, and 2475 years mean return periods to the
PGA values targeting either 2·10−4, or 5·10−4 annual
probability of collapse are represented for the main cities
of the 41 counties of Romania. One has to mention that
the PGA values with 225 years mean return period are
the ones from the current seismic design code in Romania. Consequently, the values with 225 years mean
return period are conventional, since they are assigned
based on the zonation map of the code; thus, differences
are encountered between the actual values with
225 years mean return period from the hazard curve
and the code-based values that are rounded up to the
value assigned to the equal hazard lines drawn in the
uniform seismic hazard map. The PGA values with 475
and 2475 years mean return periods are extracted from
the hazard curves. Looking at the ratios in Figs. 9, 10,
Fig. 7 Probability of collapse for the PGA corresponding to a mean return period of 2475 years, β = 0.6 and 0.001 quantile (left) and
probability of collapse for the PGA corresponding to a mean return period of 2475 years, β = 0.6 and 0.1 quantile (right)
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Fig. 8 PGA for uniform seismic hazard (mean return period of 2475 years) (left) and for uniform seismic risk (collapse probability = 5·10−4,
β = 0.6 and 0.1 quantile) (right)
and 11, the patterns of the values are different: higher
ratio values on the back-arc sites for mean return periods
of PGA of 225 and 2475 years, and higher ratio values
on the fore-arc sites for PGA values with 475 years
mean return period. The different pattern between the
ratios corresponding to 225 and 475 years mean return
periods PGA values is attributed mainly to the different
ways of obtaining the uniform hazard values (from the
seismic hazard map, respectively from the seismic hazard curve). On the other hand, the different pattern
between the ratios in Figs. 9 and 10 is due to the very
different slopes of the hazard curves (see Fig. 1), showing, for 2475 years mean return period much higher
PGA values on the back-arc sites, if compared to the
fore-arc sites, provided that the PGA values with
475 years mean return period are quasi-equal. Considering the ratios of Fig. 10 (left), one can notice that
targeting a uniform annual risk of 2·10−4 implies the
increase of the PGA values with 2475 years, on average,
by 30% in the fore-arc regions and by 10% in the backarc regions of Romania. On the other hand, the values in
Fig. 10 (right) show almost no increase on the fore-arc
sites and an average decrease of 30% on the back-arc
sites.
Based on the results obtained in this study, it is of
paramount importance to establish a general procedure
for deriving risk-targeted maps. At this moment, based
on the results obtained, there are different opinions in
which part of Romania should the peak ground accelerations be increased based on the uniform risk approach.
Silva et al. (2016) propose a drastic decrease of seismic
hazard levels in the eastern part of the country and an
increase in the western part. However, in our opinion,
the decrease of seismic hazard in the eastern part of the
Fig. 9 Ratio between PGA for uniform seismic hazard (MRP of
225 years) and for uniform seismic risk (Pf = 2·10−4, β = 0.6 and
0.1 quantile) for all 41 counties (left) and ratio between PGA for
uniform seismic hazard (MRP of 225 years) and for uniform
seismic risk (Pf = 5·10−4, β = 0.6 and 0.1 quantile) for all 41
counties (right)
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Fig. 10 Ratio between PGA for uniform seismic hazard (MRP of
475 years) and for uniform seismic risk (Pf = 2·10−4, β = 0.6 and
0.1 quantile) for all 41 counties (left) and ratio between PGA for
uniform seismic hazard (MRP of 475 years) and for uniform
seismic risk (Pf = 5·10−4, β = 0.6 and 0.1 quantile) for all 41
counties (right)
country cannot be justified since this is the most seismically exposed area of Romania. Another key aspect of
this methodology is, in our opinion, the coupling with
past or present seismic design maps so as to ensure that a
future building will not have a reduced structural safety
as compared to a new one (due to proposed reduction of
peak ground accelerations obtained through risktargeted approach). Furthermore, one has to take into
account the fact that the results obtained by Silva et al.
(2016) were derived for rock conditions which can be
found only in few areas of Romania. Consequently,
from the point of view of structural design and in the
absence of site-dependent amplification factors, the results of Silva et al. (2016) are not directly applicable.
4 Conclusions
In this study, risk-targeted maps are developed for Romania based on the recent seismic hazard study of Pavel
et al. (2016). The approach used implies the evaluation of
the mean annual probability of failure by using the convolution product between the seismic hazard and fragility.
The same 200 sites whose seismic hazard was evaluated
in more detail in the study of Pavel et al. (2016) are also
investigated in this study, as well. Both the approach of
Luco et al. (2007) and Silva et al. (2016) were considered
in the analysis. The study aimed at evaluating the corresponding peak ground accelerations for a given annual collapse probability and to determine the collapse
Fig. 11 Ratio between PGA for uniform seismic hazard (MRP of
2475 years) and for uniform seismic risk (Pf = 2·10−4, β = 0.6 and
0.1 quantile) for all 41 counties (left) and ratio between PGA for
uniform seismic hazard (MRP of 2475 years) and for uniform
seismic risk (Pf = 5·10−4, β = 0.6 and 0.1 quantile) for all 41
counties (right)
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probability for a given peak ground acceleration which
corresponds to a specific mean return period of the seismic action. The obtained results have pointed out several
main issues raised in the application of the methodology:
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The influence of the standard deviation parameter β
is limited in the sense that it either decreases or
increases the values of the corresponding peak
ground accelerations or collapse probabilities.
The influence of the quantile used for anchoring the
fragility function at a specified collapse probability
is dominant. By assigning a different value of the
quantile, the shape and aspect of the resulting map
changes dramatically. It was observed that by
changing the quantile values from 0.1 as
considered by Luco et al. (2007) to 0.001 as used
by Silva et al. (2016), the areas which correspond to
the largest collapse probabilities shift from eastern to
western Romania. This aspect was also noticed by
Silva et al. (2016), although it was not commented.
The issue of quantile is confusing since if one interprets the Bp^ quantile value of peak ground acceleration as the value for which the probability of exceeding the life safety limit state is B1-p^, then lower
the Bp^ value, more reliable the design seems to be.
Nevertheless, as Bp^ is decreasing, the value of
associated peak ground acceleration is decreasing
as well, reaching the conclusion that you might
increase the reliability of the design by decreasing
the value of peak ground acceleration. The confusion comes from the different interpretation of the
peak ground acceleration. When we search for the
probability of failure (direct approach), the peak
ground acceleration represents the capacity and the
fragility function is the cumulative distribution function of the capacity. Given the fact that peak ground
acceleration is the capacity, it is on the safe side to
choose a lower Bp^ value to increase the seismic
reliability of the structure. On the other hand, when
we search for the value of the peak ground acceleration for a target reliability level (indirect approach),
the ground motion parameter becomes a demand. In
order to be consistent with the direct approach when
using the indirect one, the value of peak ground
acceleration is associated with low Bp^ values, a
very uncommon situation from the structural reliability position. It is the authors’ opinion that the
decision of choosing the value of the quantile in
indirect approach is rather subjective. Moreover,
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the meaning of the fragility function as a cumulative
distribution function of the seismic capacity shall be
dropped.
The uniform risk-targeted maps are based on the
indirect approach. In this situation, there are three
knobs to be turned by the analyst: the target probability of failure, the logarithmic standard deviation
and the Bp^ values. For the first and second knob,
there is a broad consensus in the literature on the
values to be used. As for the third knob, the range of
Bp^ values used in the literature covers three orders
of magnitude. Given this fact, it is the opinion of the
authors that the third knob shall be turned until the
design values of peak ground acceleration obtained
from uniform risk maps equals the values obtained
from uniform hazard maps in areas where it is
proved that the uncertainties assessed from probabilistic seismic hazard assessment are the lowest. Further on, the results obtained from uniform risk maps
are used for fine tuning of the peak ground acceleration values in areas with higher uncertainties associated with probabilistic seismic hazard approach.
In the opinion of the authors, the most appropriate
and feasible approach for Romania is to use the
PGA values with 2% exceedance probability in
50 years as the 10% quantile of the fragility function
and to set the target annual probability of failure as
5·10−4 (providing uniform risk PGA values close to
PGA values with 2%/50 years, in epicentral area), or
2·10−4 (as for conterminous US, but providing
PGA values higher than 2%/50 years PGA).
Consequently, based on the abovementioned issues,
it is of critical importance to establish a uniform procedure for deriving risk-targeted maps. In addition, the
development of risk-targeted maps should be based on
seismic hazard results which take into account the
actual soil conditions, although in a simplified manner,
and not based on uniform soil conditions throughout a
country or continent. Moreover, this approach should
be coupled also with the previous uniform hazard maps
from seismic design codes of a country so that a future
building will not have a reduced structural safety as
compared to an existing one due to a decrease in the
seismic hazard levels obtained through a risk-targeted
approach.
Acknowledgements The first four authors gratefully acknowledge the financial support of the Romanian National Authority for
J Seismol
Scientific Research and Innovation, CNCS – UEFISCDI. The first
two authors are indebted to John Douglas (University of Strathclyde) for the very fruitful discussions that enabled them to acquire
a more comprehensive and in-depth understanding of the uniform
seismic risk maps issues and approaches. The authors deeply
acknowledge the valuable constructive comments and suggestions
from an anonymous reviewer that considerably enhanced the
quality of the manuscript.
Funding information This work was supported by a grant of the
Romanian National Authority for Scientific Research and Innovation, CNCS – UEFISCDI, project number PN-II-RU-TE-2014-40697.
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