In the prisoner interviews, traffickers told us how they assess risks and adjust trafficking activity to
ameliorate those risks. Self-reports are subjective, of course, and prisoners may not be entirely truthful.
Therefore we also used statistical analysis to objectively estimate how traffickers responded to the threat
posed by interdiction. Specifically, we identified special counterdrug enforcement operations and events
in the source, transit and arrival zones, and we sought to learn whether those programs had a predictable
effect on two measures of drug trafficking:
- Illicit drug prices in the U.S., at both the wholesale and retail levels
- Displacement of drug trafficking activity from one transportation route and method to another
The analysis required several steps. The first step was to identify factors that might affect trafficking
behavior. Most important for our purposes, those factors were counterdrug activities that "turned on" and
then "turned off" during defined periods. We sought to identify the correlation between our measures of
drug trafficking and such periods of active enforcement. We examined a total of 21 counterdrug
enforcement operations and events for their effect on cocaine trafficking activity. These deterrent events
span the time period of 1991 to 1999 and represent:
- Interdiction operations in source, transit and arrival Zones
- Major adjustments to interdiction tactics (e.g., the implementation of a shoot-down/forcedown
policy in Peru and Colombia)
- Investigative operations (e.g., Zorro II); and
- The arrest or death of major drug traffickers
The deterrent events considered in this study (listed in Table 1) were identified through a review of public
and limited access materials. The proposed list of deterrent events (with operation start and end dates,
affected geographic areas, and affected transportation modes) was critiqued by points of contact at
Customs, Coast Guard and ONDCP.
|
Table 1
Deterrent Events
|
|
Event Name
|
Dates
|
Description
|
Arrival & Transit Zone Enforcement Operations:
|
Hard Line
Zorro II
Gateway
White Shark I
White Shark II
Frontier Shield
Border Shield
Gulf Shield
White Shark III
Brass Ring
River Sweep
Frontier Lance
Conjuntos I
Conjuntos II
Two Dozen
|
Feb 1995Jul 1997
Dec 1995May 1996
Mar 1996Feb 1998
Mar 1996Mar 1997
Sep 1996Oct 1996
Oct 1996Dec 1996
Mar 1997Ongoing
Mar 1997Ongoing
Jul 1997Sep 1997
Feb 1998Jul 1998
Feb 1998Ongoing
Mar 1998May 1998
Jun 1998
Dec 1998
Feb 1999
|
Interdiction operation targeting smuggling across the SWB
Investigative operation targeting organizations moving
drugs across SWB
Interdiction operation targeting all modes of smuggling
through Puerto Rico
Interdiction operation targeting vessels from Mexico to Gulf
coast of Texas
Interdiction operation targeting vessels from Mexico to Gulf
coast of Texas
Interdiction operation targeting vessels to Puerto Rico and
Eastern Caribbean
Interdiction operation targeting vessels from Mexico to S.
California
Interdiction operation targeting vessels from Mexico to Gulf
coast of Texas
Interdiction operation targeting vessels from Mexico to Gulf
coast of Texas
Interdiction operation targeting smuggling through SWB
ports of entry
Customs operation targeting Haitian freighters in Miami
River
Interdiction operation targeting vessels to Jamaica and
Hispanola
Land & sea interdiction operation off Panama's Caribbean
coast
Land & sea interdiction operation off Panama's Caribbean
coast
Interdiction operation targeting aircraft and vessels into the
Bahamas and Florida
|
Source Zone Enforcement Operations:
|
Support Justice III
Support Justice IV
Stand-down
Shoot-down
|
Nov 1991Apr 1992
Jan 1993Apr 1994
May 1994Dec 1994
Mar 1995Nov 1995
|
Early operation to suppress movement of coca products in
South America
Follow-on operation to SJ III
U.S. ceases radar support in South America pending legal
review of Peru's and Colombia's force-down policy
U.S. resumes radar support to Peru and Colombia. Peru
earnestly implements force down policy
|
Trafficker Arrests/Deaths:
|
Arrests/Deaths
Orejuela Brothers
|
Various
Jun 1995Aug 1995
|
Various arrests or deaths of major Colombian and Mexican
traffickers
Arrest of the Orejuela brothers
|
|
More than government-sponsored enforcement efforts affect trafficking decisions and illicit drug prices.
For example, the attractiveness of certain vectors and conveyance mode combinations may vary with the
season. Our analyses introduced "control" variables to avoid confusing the effects of enforcement
operations with other factors, such as weather, seasonality, and so on. Specifically,
control factors considered include:
- Major weather events (e.g., hurricanes, tropical storms, and severe El Nino effects). These
are detailed in Appendix F.
- Seasonality
- Month-to-month correlation of price data
Deterrent event data were complemented with annual source and transit zone interdiction force laydown
data from Customs and Coast Guard. We were unable to obtain this type of information from the
Department of Defense, therefore, we used DoD annual interdiction funding levels as published in the
annual National Drug Control Strategies as an indicator of DoD interdiction force laydown trends.
The approach used to evaluate the effect of specific deterrent events varied depending upon the nature of
the event. For example, since source zone operations affect all transit and arrival zone routes and
transportation modes, it was not possible to consider them in the displacement analysis (which evaluates
whether interdiction operations displace drug trafficking activity from one transportation route/mode to another).
Effect of Deterrent Events on Cocaine Prices
The objective of this analytic approach is to identify the factors that affect cocaine prices in the U.S. We
are specifically interested in the impact of various types of counterdrug enforcement operations, but as
explained earlier, we control for a variety of other non enforcement-related factors. We used transfer
function models to conduct our analysis (details are provided in Appendix E). Put simply, the full price
effect of successful enforcement operations/events may unfold over months as markets adjust to higher
costs and shortages. Rather than assuming that successful enforcement is instantaneous, a transfer
function allows for more realistic incremental adjustments.
Approximating Cocaine Prices
We examined the effect of deterrent events on four levels of cocaine pricesnational retail, national
wholesale, southwest border retail and southwest border wholesale. The consideration of multiple levels
of prices allowed us to evaluate the possibility that different forms of enforcement operations will affect
different categories of prices. These price series are presented in Figures 2 and 3.
It is important to recognize that estimating cocaine prices is not a matter of simple algebra. First, the data
that supports analyses of cocaine prices (STRIDE) is not collected randomly. As such, there is a great
deal of bias in the raw data. How data analysts deal with this bias, if they do at all, has a large impact on
the resulting estimates. Secondly, the STRIDE data are wrought with grossly outlying values that may be
data entry errors (e.g., $1 million for 1 pure gram of cocaine). How analysts deal with such errors also
affects the resulting estimates.
Abt Associates has worked with the STRIDE data for over a decade, and we have had the benefit of
improving our methods over these years. The price-series used here is an adaptation of the price-series
recently provided to ONDCP. The basic methodology is reported in Johnston, Rhodes and Kling (2001).
That report provides a quarterly series. The adaptation used here provides a monthly series. The
southwest border prices do not appear in the price-series reports, but are based on applying a similar
methodology to cocaine purchases from Texas, Arizona, New Mexico and California.
Consistent with data about the purchasing habits of hardcore drug users, the retail price series is based on
purchases of $100 and less. Purchases of around $40 dominate this series. The wholesale price is a
construct consisting of purchases of over 100 pure grams, which averages to 417 pure grams at 82%
purity.
Methodology
We began our analysis by creating a baseline model for use in all price series evaluations. This baseline
model includes control variables representing month-to-month correlation in cocaine price data,
seasonality, weather9, and source and transit zone air and marine interdiction force laydown trends.
We then commenced the process of introducing the individual deterrent events into this baseline model.
Recognizing that there would be a delay in the effect of different types of operations/actions on cocaine prices in the U.S., model selection involved choosing both a deterrent event as well as its optimal (from a statistical standpoint) delay. Delay ranges considered were four to six months for the five source zone events, and zero to two months for all other deterrent events. Deterrent events meeting standard statistical criteria of significance were allowed into the model.
The results for each of the four price series are presented in Table 2. Specifically, for each price level, this table identifies whether a deterrent event had a statistically significant effect on cocaine prices in the
U.S. If so, the table indicates whether that effect was to increase prices (as indicated by a 'positive' entry) or to decrease prices (as would be indicated by a 'negative' entry). Deterrent events found to have no statistically significant effect are indicated with an entry of 'none'.
|
Table 2
Effect of Deterrent Events on Cocaine Prices in the U.S.
(delay of effect, in months, is in parenthesis)
|
|
|
National Retail
Prices
|
National
Wholesale
Prices
|
SWB Retail
Prices
|
SWB
Wholesale
Prices
|
Arrival & Transit Zone Events
|
Hard Line
Two Dozen
Zorro II
Gateway
Frontier Shield
Border/Gulf Shield**
Brass Ring
River Sweep
Frontier Lance
Conjuntos I
Conjuntos II
|
None
None
None
None
None
Positive (1)
None
None
None
None
None
|
None
None
None
None
None
Positive (2)
None
None
None
None
None
|
Positive (0)
None
None
None
None
None
None
None
None
None
Positive (1)
|
None
None
None
None
None
None
None
None
None
None
None
|
Source Zone Events
|
Support Justice III
Support Justice IV
Stand-down
Shoot-down
|
Positive (4)
None
None
Positive (6)
|
Positive (5)
None
None
Positive (6)
|
Positive (4)
None
None
None
|
Positive (5)
Positive (5)
None
None
|
Trafficker Arrests/Deaths
|
Arrests/Deaths***
Orejuela Brothers Arrest
|
None
Positive (1)
|
None
Positive (0)
|
Positive (1)
None
|
None
Positive (0)
|
|
** Due to the high collinearity between Gulf Shield and Border Shield, the two operations are represented in our model by one combined
variable.
*** The Arrests/Deaths variable for SWB prices includes only arrests or deaths of major Mexican traffickers
|
Effects on National Wholesale Prices
Four deterrent events were found to have statistically significant effects on national wholesale prices of
cocaine: Operation Support Justice III, Shoot Down, the arrest of the Orejuela brothers, and Operation
Border/Gulf Shield. The effect of the two source zone interdictions, Support Justice III and Shoot Down
was to increase wholesale prices by $3.53 per pure gram five to six months after initiation of the
operation. The effect of Orejuela arrests was to increase wholesale prices by $4.71 in the month of the
arrest, and the effect of long-active Border/Gulf Shield was to increase wholesale prices by $4.52 with a
delay of two months.
These effects are shown in the accompanying graphs (Figures 4 and 5). Figure 4 shows the effect of the
deterrent events only, while Figure 5 shows the final model (which takes into account the effect of
monthly correlation, time, and weather events). The continuous line represents wholesale prices. The
dashed line represents wholesale prices predicted from the model. The timing of deterrent events is
shown at the bottom of the graphs. The lower sequence shows the actual timing of the individual
deterrent events, while the upper sequence shifts these by the optimal delay estimated in the model. For
example, Support Justice IV actually started in January 1993, but its effect began five months later in
May 1993. Thus the interdiction response in the predicted (dashed) line is contemporaneous with Support
Justice IV shifted by five months. Also, note that although Shoot Down actually preceded Orejuela
arrests by three months, the effect of the latter was realized first. Indeed, wholesale prices were kept
elevated for 12 consecutive months, first by Orejuela arrests (three months) and then by Shoot Down
(nine months).
We identified a positive month-to-month correlation in the data (suggesting a momentum of prices) for
both national wholesale and national retail prices (discussed below), but no seasonal effect could be
detected in the final models. In addition, both wholesale and retail prices were affected by weather. Thus
wholesale prices in months with hurricanes every day (e.g., April, May and June 1997) are expected to be
$4 higher than months with no hurricanes (e.g., the four months preceding April 1997). Similarly, retail
prices are expected to be $17 higher in hurricane-saturated months than in hurricane-free months. The
effects of weather and month-to-month correlation are evident from the figures depicting the final models
for national wholesale and national retail prices. In particular, high prices in the spring of 1997 appear to
be largely attributable to the high frequency of hurricanes during that period.
National Retail Prices
The same deterrent events found to be significant in predicting national wholesale prices were similarly
found significant in predicting national retail prices. The effect of the two source zone operations,
Support Justice III and Shoot Down was to increase wholesale prices four and six months later by $30 per
pure gram and $26 respectively. The effect of the Orejuela arrests was to increase wholesale prices by
$33, and the effect of long active Border/Gulf Shield was to increase wholesale prices by $30. In both
latter cases, the delay was by one month.
These effects are depicted in Figures 6 and 7. For wholesale prices, the effects of Shoot Down and
Orejuela arrests were strictly adjacent, giving rise to two plateaus of elevated prices lasting 12 months.
For retail prices, in contrast, the two interdictions were additive for the month of September 1995, and
this combined effect appears to largely account for the unusually large spike in retail prices that month.
The final model predicts a still higher price because of the high hurricane percentage in August (48% or 15 days) and September (32% or 10 days), the effect of hurricanes in August on prices in September being explained by the positive month-to-month correlation.
Southwest Border Wholesale Prices
The model indicates that wholesale prices at the South West Border were influenced by the three
interdictions with the arrest of the Orejuela brothers having a dynamic effect10 with no delay, and the two
source zone interdictions having non-dynamic effects each with a five month delay.
The effect of Support Justice III and Support Justice IV was to increase wholesale prices five months later
by $5.47 per pure gram and $3.14 respectively. The effect of the Orejuela arrests was to increase
wholesale prices by $3.84 in the month of the arrest, $2.66 the next month, and $1.86 the following
month. Since the last Orejuela arrest was in August 1995, prices began an exponential decline towards
their original level starting in September 1995. These effects are shown in Figures 8 and 9.
South West Border Retail Prices
The arrest or death of major Mexican drug traffickers (January 1996, February 1997, and July 1997) and Operation Conjuntos II (December 1998) were found to increase South West Border retail prices one month later by $68 and $95 respectively. These effects are represented in Figures 10 and 11 by spikes in
the model at the appropriate months, and in three of the four cases, by coincident spikes in the data.
The effect of Support Justice III was to increase wholesale prices by $59 four months after initiation of
the operation, $34 in the next month, and $19 in the following month, approaching a total increase of
$137. However, what is more evident from the figure is the subsequent exponential decline starting in
September 1992.
Operation Hard Line had a similar dynamic effect while it was in full operation. The initial increase in
prices was about $6 approaching a total increase of $46, half of which would be achieved by the fifth
month. This effect was attenuated as Hard Line ramped up (February 1995 through December 1995) and
ramped down (September 1996 through July 1997). These effects induced an S-shape to the modeled
curve from February 1995 through July 1997.
Effect of Deterrent Events on Cocaine Movement
We argued above that successful enforcement efforts should increase cocaine prices, at least until cocaine
traffickers adapt. Demonstrating that prices are temporarily sensitive to interdiction events is important,
but that demonstration says nothing about how traffickers actual adapt to additional anti-drug operations.
This section provides some detail about those adaptations. The objective of this part of the analysis is to
determine whether or not traffickers respond to interdiction operations by altering how and where they
move drugs through the transit zone and across U.S. borders. Specifically, when a special interdiction
operation is focused on a specific vector and transportation mode for a defined period, we would expect two adjustments:
- Traffickers would reduce shipments through the targeted vector and by the targeted mode for
the period of operation; and
- They would increase shipments through other vectors and modes for the same period of
operation.
Characterizing Trafficker Behavior
Data from the interagency Consolidated Counterdrug Database (CCDB) was used as the indicator of
trafficker behavior in the transit zone. This database contains drug smuggling event data dating back to
1991 and supports two primary types of analyses: (1) evaluations of drug flow from areas of production
to consumption countries, and (2) assessments of the performance of counterdrug forces against that
movement11. For purposes of this study, we used those events, called known events, within the CCDB
that support counterdrug performance assessments. Known events are distinguished by (1) seizure or
observation of drugs; (2) observation of activity that could not be reasonably attributed to anything other
than drug smuggling; and/or (3) highly reliable intelligence. We chose to use known event data for our
study because it has been captured since 1991, while event data used to support flow assessments date
back to only 1996. Although using only known event data results in a large loss of data points, the value
gained by expanding the time span of the study to 1991 outweighs this loss.
Smuggling event data were grouped into ten movement vectors. The vector breakout is consistent with
that used by the Interagency Assessment of Cocaine Movement (IACM) and includes: Eastern Pacific,
Western Caribbean, Jamaica/Cuba/Bahamas, Hispanola, Puerto Rico/USVI, Lesser Antilles, Southeast
U.S., Northeast U.S., Southwest Border, and U.S. West coast. Arrival zone vectors (i.e., the last 4 listed)
include only those events where the event moved directly from South America into the U.S., by-passing
any transshipment countries. Figure 12 displays these vectors.
Events were further broken down into two modesnon-commercial air and marine movements.
Technically, the marine category covers both commercial and non-commercial marine events. By
definition12, only those commercial (i.e., port-to-port) marine movements that are actionable at sea are
considered by the CCDB for performance evaluation purposes. Since this definition inherently excludes
certain forms of commercial marine movements (such as cargo containers), we felt that making a
distinction between commercial and non-commercial marine events would be somewhat misleading and
under-represent commercial marine smuggling events. To the extent we are modeling the effect that
marine interdiction operations have on marine smuggling activity in the transit zone, the general criteria
of 'actionable at sea' is adequate for our purposes.
Methodology
Our analysis tests whether or not interdiction operations displaced trafficking activity from those
vectors/modes against which the operation was targeted to other vectors/modes. To conduct this test, we
examined cocaine shipments (using the data set described earlier) through each of 10 vectors by two
transportation modes (maritime and air) monthly for the period 19911999 (108 months). Ostensibly, this
provided 2,160 data points, but in fact, there were no shipments through three of these vector/mode
combinations13. Therefore, analysis used 1,836 data points.
We considered counts of cocaine shipments in two ways. The first was to include all shipments known
through any combination of intelligence or observation by interdiction assets. The second was to consider
only those shipments for which there was intelligence (i.e., some form of corroborating information) on
the event. The second measurement is a subset of the first. Each measure has relative advantages and
disadvantages. The measure based on shipments identified through intelligence or observation is the
more comprehensive of the two. The disadvantage to this measure is that observations may be sensitive
to the level of interdiction actually conducted in a vector and targeted against the mode. That is,
interdiction activity can affect the measurement of drug movements, and thus, we might mistakenly infer
that shipments have changed when only the measurement process has changed.
The second method of identifying shipments avoids this measurement problem by limiting measurements
to shipments on which there was intelligence. This provides a measure that is relatively immune to
changes in interdiction activity levels in the various vector/mode combinations. The disadvantage to this
measure is that it is likely sensitive to changes in intelligence resource levels. Moreover, it excludes data
from what is already a sparse data set for some vector/mode combinations. Given the mixed advantages
and disadvantages of these two measurements, we repeated the analysis using both approaches.
As noted, our analysis attempts to explain the number of shipments through each vector, by each
transportation mode, for every period as a function of several variables including special interdiction
activities. To test our hypotheses, we used an estimation based on a Poisson distribution. Appendix E describes our analytic approach in detail.
We first sought to establish a baseline against which the effectiveness of interdiction could be measured. The baseline model includes variables that control for the following:
- The paucity of event data in certain vector/mode combinations
- Shifts in shipment frequency across vector/modes that are not related to special interdiction
operations
- Seasonality
There is strong evidence from these baseline models that shipments are cyclical, that the trends vary
across vectors and modes, and that the vector/mode combinations vary in the number of shipments that
are typical. More importantly for our purposes, there is evidence that the baseline model for shipments
with intelligence is void of any influence from interdiction operations. That suggests we are 'starting with a clean slate' when we begin to introduce specific interdiction operations into the model. As
expected, however, this is not the case with the baseline model for shipments based on intelligence and/or
observation.
Interdiction operations were represented by variables that were coded 1 for the vector/mode/time the
operation took place. Typically, this was a period of more than one month. For each of these periods, we
defined a complement variable coded 1 for every vector/mode that was not the target of the interdiction.
For example, during the period when Gateway was operational, the GATEWAY variable was coded 1 for
vector/mode combinations that were Gateway targets. During this same period, a variable NGATEWAY
was coded 1 for vector/mode combinations that were not Gateway targets. During periods when Gateway
was not operational, both GATEWAY and NGATEWAY were coded zero.
Continuing with the Operation Gateway illustration, we expected the variable GATEWAY to have a
negative correlation with the number of shipments. If shipments moved from vectors/modes that were
targeted by Gateway to those vector/modes that were not, then the parameter associated with GATEWAY
should be negative while the parameter associated with NGATEWAY should be positive. In fact,
because the model's controls for time trends is imperfect, we examine the difference between the
regression parameter associated with NGATEWAY and the regression parameter associated with
GATEWAY. If this difference is positive and statistically significant, then we infer that Gateway
probably caused smugglers to shift to alternative vectors and modes.
We proceeded to add individual interdiction operations to the baseline model to see whether they have an
appreciable effect on drug movements. For example, to examine the effects of Gateway, we add
GATEWAY and NGATEWAY to the baseline model and test to see if the differences between the
NGATEWAY and GATEWAY parameters are positive and statistically significant. We repeated this for
each of the border and transit zone interdictions. Operations indicating statistical significance
independently were included in a final regression model to ascertain their significance when examined
within the context of other operations. The results of these final models are presented in Table 3 below.
Based on this analysis, five of the border interdictions seem to cause traffickers to move shipments from
where the interdiction happened to where it did not. We note the apparent effectiveness of Hard Line,
Gulf Shield, Border Shield, White Shark III and River Sweep. Regarding transit zone interdiction,
Gateway appears to have been effective.
|
Table 3
Effect of Transit Zone and Border Operations on Displacing
Drug Smuggling Activity From Targeted Smuggling Routes and Methods
|
|
|
Geographic Vectors
Affected
|
Analysis Based on
Events With
Intelligence
|
Analysis Based on
All Movement
Events
|
Border Operations
|
Hard Line
Brass Ring
Gulf Shield
Border Shield
River Sweep
White Shark I
White Shark II
White Shark III
|
US Southwest Border
Western Caribbean
Eastern Pacific
US Southwest Border
Western Caribbean
Eastern Pacific
Southeast US
US West Coast
Southeast US
Hispanola
Southeast US
Southeast US
Southeast US
|
None
None
Positive
Positive
Positive
None
None
****
|
Positive
None
Positive
Positive
Positive
None
None
Positive
|
Transit Zone Operations
|
Two Dozen
Conjuntos (I and II)
Frontier Lance
Frontier Shield
Gateway
|
Southeast US
Jamaica/Cuba/Bahamas
Western Caribbean
Hispanola
Jamaica/Cuba/Bahamas
Puerto Rico/USVI
Lesser Antilles
Puerto Rico/USVI
|
None
None
None
None
Positive
|
Positive
None
None
None
Positive
|
|
**** Indicates that data were too sparse to test the significance of the operation.
"Positive"indicates that the operation had a statistically significant positive effect on displacing drug smuggling activity.
"Negative"indicates that the operation had a statistically significant negative effect on displacing drug smuggling activity.
"None"indicates that the operation had no statistically significant effect on drug smuggling activity.
|
Conclusions
Based on these analyses, source zone interdiction operations and the arrest or death of major drug
traffickers appear to have very significant effects on increasing cocaine prices in the U.S. The impact of
the source zone interdiction operations is likely due to success in temporarily reducing the supply of
cocaine to the United States. Since cocaine prices are expressed in terms of price per pure gram, the
increase in prices (particularly at retail level) are the result of increased 'cutting' by the dealers. This
would be a fairly quick and obvious way to deal with a temporary shortage in supply.
The positive effect of operations Hard Line, Border/Gulf Shield and Conjuntos II on cocaine prices
implies that these operations had a very real impact as well and either caused traffickers to increase their
fees and/or reduced the supply of cocaine to U.S. markets.
Although the remaining transit and arrival zone interdiction operations examined do not have a
statistically significant impact on cocaine prices in the U.S., many exhibit an impact on trafficker
behavior. Figures 13 14, 15, and 16 display all CCDB movement events for four periods during 1998, by
vector. The shading represents the total flow through each vector, and the pie charts represent the
distribution of this flow by conveyance14. The figures clearly show not only switches in geographic
vector, but mode of transportation.
This suggests that operations were effective enough to force smugglers to change their transportation
routes and/or methods. However, as the counterdrug community has long recognized, drug traffickers'
ability to get drugs from South America into the U.S. is limited only by their creativity. Accordingly, it
appears the ability of these operations to impact cocaine prices was ameliorated by the availability of
alternative transportation routes/methods.
9 A special weather variable including only those weather events effecting routes to the U.S. Southwest Border or
Mexico was created for use in modeling southwest border price series.
10 The existence of a 'dynamic' effect indicates the impact of an operation on prices occurs over the course of
several time periods, rather than all at once.
11 CCDB Users Guide
12 CCDB Users Guide
13 Vector/mode combinations for which no shipments were identified include: Southwest Border/marine; Northeast
U.S./non-commercial air; U.S. West Coast/non-commercial air. The absence of maritime movements across the
U.S./Mexico land border is expected for obvious reasons. Since we considered only direct shipments from
Colombia to transshipment or destination points, the lack of non-commercial air shipments in the Northeast
U.S. and U.S. West Coast vectors is not surprising.
14 It is important to note that these are not the data we used for analysis, as they include both ICPAWG and flow events.
Last Updated: March 4, 2002